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Does Working Overtime Under Different Culture Belief
Hurt the Labor Market? ∗
Yiqian Lu†
November, 2016
∗I am grateful to Neel Rao for his helpful comment and sincere help. Also I appreciate the commentfrom Mingliang Li, Goncalo Monteiro, Joanne Song Mclaughlin, Eric Nierenberg, Bibaswan Chatterjeeand Jinquan Gong. All errors are mine.
†Email: [email protected] Address: 415 Fronczak Hall, Buffalo, NY 14260. Department ofEconomics, State University of New York at Buffalo.
1
Abstract
In this paper we model the work-leisure equilibrium under different culture and
social norm influence. We build a two-sector general equilibrium model and use
Panel Study of Income Dynamics (PSID) data from 1975 to 1992 to test our the-
oretical predictions. Three major findings are reported. (1) A stronger preference
on social status will make employees substitute leisure with working hours. The
working hours will increase with respect to the relative exponential ratio between
labor and capital input. And the growth rate of the economy is higher. (2) On the
contrary, the individual self-identified utility level might be lower in such society
since everyone are extremely exhausted chasing high social ranks. (3) We find no
significant evidence that strong social preference and working overtime will lead to
an increasing unemployment level. This article contributes to the literature by ex-
amining labor market outcomes under various social status preference assumptions.
JEL Classification: J22, J31, E23
Keywords: Social Status Preference, Working Overtime, Labor Market Equilib-
rium, Ability Signal
2
1 Introduction
The allocation of time remains in the central topic of labor economics. Becker (1965)
pioneers the work of interpreting the time allocation decision between working and
other activities such as home production. It sheds the light for economists to study how
individuals behave in the labor market. Gronau (1976) revisits Becker’s famous result
and finds out that home production is affected differently by changes in socioeconomic
variables comparing to leisure decision. Men and women tend to obtain different specific
human capital training. For instance, married women tend to spend less effort in
the labor market competition since child care and housework carry an intensive effort
(Becker 1985). With technology progress and emancipation for the female from the
family sector, women is more willing to participate in the labor market. Consequently,
the participation rate for women increases from 21% in 1900 to 59% in 2009 (Bowen,
William G., and T. Aldrich Finegan 2015).
At the same time, we can never fail to notice that labor market behaviors vary with
ages. Young women, for instance, have the tendency to work part-time or reduce the
workload(Kunze, Astrid, and Kenneth R. Troske 2015) when entering the job market
since the duties of raising kids reduce their interests for working during the child-bearing
and child-raising age. Some young mummies even quit the labor market, which might be
temporary. However, most of them would like to return to the job market when children
grow up. This phenomenon could be explained as the domination of substitution effect
at the early stage of job market for young women. Traditionally it is believed that
homogeneous agent model ignores the heterogeneity (culture-based heterogeneity in
this paper), which could result in unreliable research conclusions. For some East Asian
countries, for example, young women enter the labor market more intensively, where
the culture could be distinct from the West (Yoon, Jayoung 2015). Particularly, the
childbearing age-cohort female labor participation rate remains at high level, displaying
a stronger income effect in Asian countries. It could be the direct result of observed
low fertility rate in the East Asian region, which could also be explained by the inverse
causal effect. In fact, the domination of income effect could be explained by low subsidy
to the childcare system or birth controlling policies (James Liang 2015, Fuxian Yi 2010).
3
Added worker effect is a plausible explanation in this situation. Female workers are
encouraged heavily by their husbands or families to join the labor market to support
the family income.
Culture and cross-industry difference is another crucial factor to explain the het-
erogeneity. Investment banks, for example, may push the employers to work 80 or 100
hours per week to satisfy the job requirement, especially for the entry-level analysts or
associates. These facts can be observed whenever you come across the Goldman Sachs
or Morgan Stanley’s offices in Manhattan. Also, most Chinese information technol-
ogy companies strongly encourage workers to follow a so-called ”996” working pattern,
which means each employers should work from 9 am to 9 pm each working day and 6
days a week. Any worker who fail to obtain such workload criteria might be considered
as ”low ability” or ”unsatisfied performance” so that she/he could be fired or lose the
promotion possibilities. It is summarized by JH Kang, JG Matusik, LA Barclay (2015)
and explained by culture difference that Asian culture requires more working effort.
HUAWEI1, the CISCO major competitor all over the world but USA, strongly
encourages every junior engineers to work and sleep in the office and never go home
but only pays them based on the 40 or 50 hours scheduled weekly working hours. In
this case, many engineers could work more than 100 hours a week but only report
40 or 50 working hours to the Taxation and Labor Department so as not to break the
worker-protection law. The co-called ”wolf-culture”, aka. working unreported overtime
with little compensation, is the key for HUAWEI to compete with CISCO. You might
wonder why the junior workers are willing to wait for 24/7 project assignments without
reasonable compensations. If a junior worker displays sufficient hard working and
loyalty by following such torturing job requirements, he/she would have a large chance
to be promoted and get an outstanding payment throughout the industry. Other under-
reported working overtime is the case in Japan. Junior workers are seldom allowed to
leave the office before their bosses, which displays disrespect in Japanese culture. Even
a low-rank employee finishes her/his job duties, she/he should wait until the direct
boss leaves (WB Schaufeli, A Shimazu, TW Taris 2009), which leads to, in a certain
extent, an excessive and compulsive working overtime. Also, coming home too early,
1you can raise a couple of other similar examples in the East Asian countries
4
say 7:30 pm, could be treated as a dangerous signal of potential unemployment, which
is particularly true for young men workers. Hence, each worker in such situation works
or pretends to work hard and leaves office later and later. (Samuel, Sidney W 2015)
This phenomenon enlightens the research that I propose in this paper. We are
going to answer the following three questions. (1) Since leisure is generally considered
as normal good, why do those workers wish to give up their precious leisure time to
work for the reported or unreported excess workload? Do they work overtime in order
to increase their promotion chances by sending signal of diligence or high ability? (2)
Does the culture affect the work-leisure choices in those East Asian countries? Does
such ”leaving after the boss” belief reduce the utility and market efficiency level? If so,
how does the culture bias influence the equilibrium? (3) If most people are willing to
work overtime, will the employer decrease the labor demand by recruiting less people
to fulfill the job tasks? Will the overtime-working lead to an increasing unemployment
rate?
We are going to build a heterogeneous agent model to answer the aforementioned
questions. After calibrating various social norm or regional culture with different utility
function, we would like to discuss how equilibrium shifts under various social norm.
Finally, we would like to use the Panel Study of Income Dynamics (PSID) data to
examine our theoretical findings.
The remaining parts of this article are organised as follows. Section 2 reviews the
existing literature on similar topics. Section 3 builds the standard model and discusses
the equilibrium under various social normal assumptions. Section 4 describes the data
we use and provides estimate for the theoretical results. Concluding remarks are made
in Section 5.
2 Literature Review
There are extensive literature discussing the working hour difference between various
regions. Even among OECD countries, the annual average working hour for a full-time
worker varies. (Mexico 2,228, South Korea 2,124, USA 1,436, Japan 1,729, Denmark
1,436, Germany 1,371) (2014 OECD report). In non-OECD regions, the annual working
5
hours also distinct a lot. Hong Kongers and Singaporeans, for example, have to work
approximately 2400 hours per year while less than 1500 in some less developed regions.
We can notice that the employers in some northwest European countries only work
two-thirds of Mexicans and Koreans. It is explained by different ethic standards like
Confucian ethics, where too much leisure is considered as laziness and immorality (JH
Kang, JG Matusik, LA Barclay 2015).
Akerlof (1976) pioneers the work that labor market equilibrium could result in
inefficient long hours. It is also noticed by the academia community (Blair-Loy 2004)
that firms might reserve the best jobs and opportunities for workers who can give
long hours to their employers with very limited family responsibilities. Gicheva (2013)
documents that 5 extra hours are associated with a 1% increase in annual wage growth
but the relationship is not presents when weekly working hour is below 47, which
displays the non-linear hour-wage relationship.
Mauss, Marcel (1923) describe the labor-wage contract as a kind of gift exchange
process, where wage-payers exchange a gift of a wage premium for the expected high
effort performance. By following this framework, if workers are willing to provide ex-
cess work, they should expect to receive high payoff currently or in the future, which
is the increasing promotion chances 2 . Akerlof, George A.(1982) uses a specific utility
function to mimic the workers’ effort. Each individual preference depends on her/his
attitude towards fairness . If the employee cares nothing about fairness, the market
equilibrium in this case will be the competitive equilibrium. If the fairness (altruism)
level is positive there will be positive improvement on the wage and employment. And
vice versa, which could also be a possible reason explaining the ubiquitously observed
cross-industry wage differences(Akerlof, George A., and Janet L. Yellen 1988). Invol-
untary unemployment could be a direct result of negative fairness preference. Workers
are discouraged to provide sufficient labor supply comparing to the competitive equilib-
rium with negative fairness preference. There would exist no involuntary unemployment
when all employers are neutral (Akerlof, George A., and Janet L. Yellen 1990, Fehr,
Ernst, and Klaus M. Schmidt 1999). The existence of non-monetary motivation in the
2Treating the chances of promotion as options, the employees write the option at the early stage. Ifthe employers could survive the challenging duties in the first period, the expected return of the optionwould be high. Otherwise, the option would expire in the second period and the option value is 0.
6
preference function is tested by Gneezy and Rustichini (2000a & 2000b) by examining
the performance of the parents in the daycare centers in Israel. They conclude there
indeed exists such selfish or altruism component in the utility function.
Also, there is alternative literature concluding that work-leisure choices are affected
by policies. Osuna, Victoria (2003) finds out the taxing overtime wage could greatly
reduce the observed excess overtime workings. They calibrate the model and conclude
a marginal 12% tax rate could reduce 8 hours a day (which is one hour excess work
each working day) to 7 hours 3. Nickell, Stephen, and Richard Layard (1999) discover
that union strength and social welfare system play pivotal roles in explaining the un-
willingness of working overtime for European societies. The stronger union protection
for workers and the better social welfare benefits, the less effort people would like to
supply in the labor market. They argue that increasing product market competition
could be a remedy to solve the negative influence of unions and social security, which
provides more incentive for employers to work hard.
There is an ongoing heated debate between pros and cons of working overtime. Some
scholars argue the workers who work overtime display an extraordinary effort and ef-
ficiency level comparing to those employees who do not (Machlowitz, 1980; Peiperl,
Jones, 2001). However, an opposite view is that workaholics increase the difficulties
level by themselves, adding unnecessary complexities for their colleagues (Oates, 1971,
Machlowitz, 1980, Porter, 2001), and therefore it could be problematic for the com-
panies. Especially when the accomplishment of projects relies heavily on cooperation,
such low-efficient performance could lead to excess workload to the co-workers and re-
sult a trouble-making working overtime culture. There is also some literature (Burke
2001, etc.) pointing out there is no relationship between the working overtime and the
efficiency level, contradicting the positive or negative ability signal hypothesis. The
positive outcomes could be an excess wage ratio for overtime workload while the neg-
ative could never be neglected at the same time. Researchers demonstrate there is a
negative association between working overtime and weak health level such as high levels
of stress, ill-health situation and strain (Sparks, Kate, et. al. 1997).
37-hour a day is the regular working schedule for some European countries but not for USA, Chinaand Japan
7
It could hardly be ignored that tenure structure influences the workers’ selection
on work-life balance. Robert A. Hart, Yue Ma (2013) test British plant and machine
operatives and discover workers with longer tenure are more fond of supplying excess
work. However, the marginal product during the over time is less than the wage pre-
mium, indicating potential low efficiency level when workers are fatigue. By noticing
such phenomenon, the employees could lower the base wage rate in order to set the
aggregate salary for the overtime-working staff the same level comparing to never over-
working peers. There is little evidence that demand side serves as the main driven force
for overtime working (Bell, David NF, and Robert A. Hart 2003). Usually speaking,
extensive-margin elasticities are supposed to be higher than intensive-margin predicted
by various macroeconomic models (Richard Rogerson 1988, Gary D. Hansen 1985,
Lars Ljungqvist and Thomas J. Sargent 2006). In a sense, it is the case that work-
ing overtime should not be widely observed since the intensive adjustment to a higher
compensation should be relatively small. However, recent literature(Chetty, Raj, et
al 2011) argues the intensive-margin elasticity are significantly underestimated by the
previous literature, which could possibly offer vigorous explanation for widely-existing
overtime working.
Overall speaking, there are various interpretations on the reason and influence of
overtime working and economists have not yet reached out a convincing conclusion.
3 Model Setup and General Equilibrium
3.1 Workers
We build a competitive equilibrium model in the section. Following Bakshi, Gurdip S.,
and Zhiwu Chen(1996)’s approach, we may assume a worker lives forever and maximizes
his/her lifetime utility.
max{Ct}∞t=0,{Lt}∞t=0
βtE0[U(Ct, Lt, St)] (1)
where β is the time preference parameter; U(Ct, Lt, St) denotes the utility function
of consumption level Ct, leisure Lt and social status level St. Assume U(., ., .) are
8
twice differentiable with each variable and UC ,UL > 0 , indicating that additional
consumption or leisure creates positive marginal utility. We cannot assume St have
the similar characteristics at this moment. If the agent has no preference on the social
status, i.e. US = 0, then U(., ., , ) has no relationship with S.
We maximize the target function subjected to the budget constraint 4,
at+1 − at = µtat − Ct + wt(St) (2)
where µt represents the return on capital in period t and wt(St) is the wage in
period t corresponding to the social status level St. at is the asset level.
In this model, the social status variables St are not direct choices variables for
workers. The status will be determined by the employees after observing workers’
labor effort and potential influential factors (for example luck). When t increases from
0 to infinity, we assume that the social status or the rank strictly increases. In other
word, {S = 1} ≺ {S = 2} ≺ {S = 3} ≺ ... ≺ {S = t} ≺ {S = t + 1} ≺ ... and at the
initial period S0 = 1. It is assumed S ∈ Z+ is discrete without loss of generality.
We attempt to use four different models with various representative’s preferences
to explain our findings.
Model 1. (No preference on social status).
The worker has no preference on social status. In other word, there is no discrimination
against various rank or social status. In this case, US = 0 and we have U(Ct, Lt, St) =
U(Ct, Lt). A Cobb-Douglas utility function is given by
U(Ct, Lt, St) =(Cρt L
1−ρt )1−γ
1− γ(3)
This assumption is consistent with M Lettau, H Uhlig (2000), as well as Rupert,
Peter, Richard Rogerson, and Randall Wright (2000). We use this utility function since
the marginal rate of substitution is a function of consumption and leisure.
MRSt+1 = β(Ct+1
Ct)ρ(1−γ)−1(
Lt+1
Lt)(1−γ)(1−ρ) (4)
4we first assume there is no stochastic term in the budget constraint
9
Typically it is more likely to observe the utility function with US = 0 in the most
developed economies such as United States. People have no discrimination taste.
Model 2. (Utility level depends on the social status)
The representative agent’s utility depends not only on consumption and leisure but
the social status as well in Model 2 .
U(Ct, Lt, St) =(Cρt L
1−ρt )1−γ
1− γSηt (5)
where η depicts the preference level on the social status. If η = 0, Model 2 shrinks
to Model 1 automatically. η > 0 indicates a positive preference on social status. A
higher social status may provide you more power and welfare such as travel benefits
and respects. It is widely observed in most Confucian-dominated countries such as
East Asia and Singapore that people have positive preference on social status. On
the contrary, η < 0 shows a negative preference, which might result from increasing
peer pressure and responsibility. η < 0 could be observed in some European countries
thanks to the well-developed social welfare system and religious influence.
Model 3. (Utility level depends on the ratio between individual social status and
its social average)
In this case, the utility function turns into the following format.
U(Ct, Lt, St) =(Cρt L
1−ρt )1−γ
1− γ(StS
)η (6)
where S represents the average social status. If St < S, the agent is in the bottom half
while St > S indicates an above average rank. If St = S, then the agent is exactly in
the median class. You could notice if we preset S as constant, then Model 3 is exactly
Model 2.
Model 4. (Utility depends on the self-identified social status level)
U(Ct, Lt, St) =(Cρt L
1−ρt )1−γ
1− γ(St − κS)η (7)
where κ > 0 is the worker’s self-identified anti-poverty “reservation” coefficient.
10
Notice when St − κS < 0, the utility function will collapse to a negative value. As a
result, a rational employer will never attempt choose a St level below κS by supplying
sufficient labor market efforts to win higher chances of reaching positive utility(although
sometimes could potentially result in a failure) . For instance, if we set κ = 12 , a
rational agent will find the bottom 50% social status intolerable. Definitely, κ relies
heavily on the parents’ social status and educational attainment. For instance, workers
from prestigious ivy league universities are supposed to self-identify a higher level of κ
comparing to high school dropouts. Because of the national constraint of κ, κ could
never exceed the ratio of self-selected social status and the community average, and
consequently it is somehow difficult for a lower-class worker to self-identify a high κ.
During the early age of the career, given the relative low opportunities being promoted
to higher ranks, self-identified κ should be no more than during the later stage of the
career. Therefore, κ might be time-variant. Model 2. is the particular case of Model
4 when κ = 0.
Model 1 to Model 4 are inspired by the spirit of Bakshi, Gurdip S., and Zhiwu
Chen (1996) and Campbell, John Y., and John H. Cochrane (1995).
3.2 Firms
We assume the only input is labor. The firm uses heterogeneous labor inputs with
different level to maximize its profit level. The only cost is wage expenditure.
π = max∏
∑Sj=i
Sj>0
(∑Sj=i
Sj)λi −
∑∑Sj=i
Sj>0
∑Sj=i
w(Sj) (8)
In other word,
π = max{∏i
(number of employers with rank i)λi
−∑i
number of employers with rank i ∗ w(S = i)}
where π is the profit level and λi denotes the corresponding exponent for social
status S = i. If we requires constant returns to scale technology,∑λi = 1 should hold.
However, at this moment constant returns to scale is not assumed. w(Sj) is the wage
11
function for workers in rank Sj , which is constant within each rank.
It is assumed that the wage for each worker only depends on their rank but not
working hours and experience. This compensation structure is typically observed in
most high-tech companies. Google, for instance, provides a fresh master junior em-
ployer with Level 2 class with a package of approximately $ 150,000 per year (base
salary+bonus+restricted stock units) while a fresh PhD junior employer with Level 3
class a with a package of approximately $200,000 per year.
In this model, however, high class workers could be treated as durable goods that
could hardly be replaced in the short run. Low class workers are considered to be non-
durable goods which could be substituted with other competitors on the job market
without difficulties. For instance, if there are only two classes (leader with rank 2 and
worker with rank 1) in the model, we can treat leader as capital good and worker as
labor input in the Cobb-Douglas form production function.
We also assume the relative output elasticities for class i and class j should only
relate to the distance between i and j (ie. |i− j|). In particular we have
λ1
λ2=λ2
λ3= ... = λ > 1 (say) (9)
As a result we can assume λi = λ−i,∀i ∈ Z+. If the number of classes goes to infinity
and constant returns to scale is assumed, we have λi = 12i, ∀i ∈ Z+.
Assume there are ni workers in class i. Under the First Order Conditions with
respect to rank i and rank i+ 1 in the profit function and assuming the aggregate wage
packages for each class being the same, we should have
ini(i+ 1)ni+1
=λiλi+1
=1
λ, ∀i ∈ Z+ (10)
Assuming equal aggregate wage packages is consistent with widely observed wage struc-
ture in high-tech companies. Microsoft, for instance, CEO Nadella earns approximately
100 million annually while Microsoft has approximately 2,000-4,000 lowest level employ-
ers with less than $ 50,000 compensation.
The following relationship between the number of workers in each classes is obtained
12
by solving (10).
ni = (1
λ)i−1 1
in1 ∀i ∈ Z+ (11)
We can easily identify that n1 ≥ n2 ≥ n3 ≥ ... ≥ nt ≥ ... ≥ 0. Assume the total number
of workers is fixed number N , there must exist a unique k ∈ Z+ such that nk > 0 and
nt = 0, ∀t > k.
Proposition 1. The overall number of classes k with the firm is decided by the
total worker number N and the relative output elasticities λ between adjacent classes.
It can be uniquely determined by solving the following simultaneous inequalities.
∑ki=1( 1
λ)i−1 1in1 = N
( 1λ)k−1 1
kn1 ≥ 1
( 1λ)k 1
k+1n1 < 1
(12)
The economic meaning of inequalities (12) is quite straightforward. The firm no
longer needs to set class k+1 to maximize the profit level. For instance, the prestigious
hedge fund Two Sigma has altogether 800 employees and 7 class level (T1 the lowest
class to T7 CEO). The following Proposition 2 is obtained the the proof is provided
in the appendix.
Proposition 2. The total number of class level k is a non-decreasing function with
respect to the total number of workers N and non-increasing function with respect to
the relative output elasticities λ between adjacent classes.
Proposition 2 is quite intuitive. The total class number should increase with the
number of employees. For instance, Baidu, the famous search engine company with
more than 20,000 staff in China, has a total 11 classes while Two sigma has 7 classes
with an approximate 800 staff. Also, it should decrease with respect to the promoting
difficulty level. Apple, with more challenging promotion criteria, has less ranking classes
comparing to Google with similar size but larger promotion chances and more classes.
We assume all workers enter the firm with S0 = 1. Outputs are hard to measure5.
5In Yang(2001), if the output are hard to measure for the firm, it is better to use the fixed wagerate for each class. For instance, research outcome is hard to measure in research universities in theshort run, so the wage rate is relatively fixed for tenure-track assistant professors, tenured associateprofessors and full professors. Research institutes will measure the publication quality to make the
13
Only working time could be observed by the firm to make the final promotion decision.
Also, it is rational to assume in each period a worker can be promoted up to one class
at most and no one could be downgraded(In other word, 0 ≤ St+1 − St ≤ 1, ∀t ∈
Z+). According to Central Limit Theorem, all workers’ working hours follow normal
distribution if they are independent. The firm uses Maximum Likelihood Estimate to
finish the promotion decision.
St+1(ω) =
St(ω) + 1, with prob.
∫ lt(ω)−∞
pc√2πσ2
exp(− (ξ−lc)22σ2 )dξ
St(ω), otherwise
(13)
where lc is the average working hour for all the staff in the class of St = c and lt(ω) is
the working hour choice of person ω, where lt(ω) = 1 − Lt(ω). By revisiting (10) we
obtain
0 ≤ pc =c
c+ 1
1
λ< 1 (14)
And by setting the base wage for level 1 at w1(w(Sj = 1) = w1) we conclude the
following wage equation.
wi = w(Sj = i) = iλi−1w1,∀i ≥ 1 (15)
3.3 Equilibrium
The Bellman Equation for the employees is as follows.
V (at, St) = maxCt,Lt{U(Ct, Lt, St) + βEoV (at+1, St+1)} (16)
subject to
Ct = (1 + µt)at + wt(St)− at+1 (17)
tenure decision within the tenure clock. However, if the outcomes are easy to measure, then piece ratewage is better than fixed wage. It is rational to make the assumption that wage rate only depends onthe class in this model.
14
We eliminate the choice variable Ct by rewriting the budget constraint and get the
following Bellman Equation with choice variables at+1, Lt, and state variables at, St.
V (at, St) = maxat+1,Lt
{U((1 + µt)at + wt(St)− at+1, Lt, St) + βE0V (at+1, St+1)} (18)
We have the following two First Order Conditions.
With respect to at+1:
−U tc + βV1(at+1, St+1) = 0 (19)
With respect to Lt:
U tL − βV1(at+1, St+1)∂at+1
∂lt− βV2(at+1, St+1)
∂St+1
∂lt= 0 (20)
Also we generate two Envelope Conditions.
With respect to at:
V1(at, St) = U tc(1 + µt) (21)
With respect to St:
V2(at, St) = U tc∂wt(St)
∂St+ U ts (22)
where
∂wt(St)
∂St= λSt−1w1(1 + St lnλ) (23)
We could reach the following Euler Equations.
U tc︸︷︷︸Marginal utility of consumption in period t
= β(1+µt) U t+1c︸ ︷︷ ︸
Marginal utility of consumption in period t+1
(24)
15
Notice ∂at+1
∂lt= 0 (next period’s initial wealth level is not affected by current labor input
level). We should have
U tL
= (1− p∗)β [
MU of consumption with labor︷ ︸︸ ︷U t+1c λSt−1(1 + St lnλ)w1 +
MU of status with labor︷ ︸︸ ︷U t+1S ]
StSt + 1
1
λ
1√2πσ2
exp(−(lt − ¯lSt)2
2σ2)︸ ︷︷ ︸
marginal utility of labor if not promoted
+ p∗β [U t+1c λSt(1 + (St + 1) lnλ)w1 + U t+1
S ]St
St + 1
1
λ
1√2πσ2
exp(−(lt − ¯lSt)2
2σ2)︸ ︷︷ ︸
marginal utility of labor if promoted
(25)
where the promotion probability p∗ is
p∗ =
∫ lt
−∞
StSt+1
1λ√
2πσ2exp(−(ξ − ¯lSt)
2
2σ2)dξ (26)
Briefly speaking, Euler Equation (25) shows the representative worker will increase the
labor effort until the marginal utility from the increasing chances of promotion being
equal to the marginal utility loss with respect to leisure when providing additional unit
of labor. We will discuss the different consumption and labor choices under Model 1
to Model 4 assumptions.
For Model 1., we evaluate Ct and Lt at their steady state and the following rela-
tionship between β and µt is summarized.
β(1 + µt) ≡ 1, ∀t ≥ 1 (27)
However, it is the usual case that the return on {µt}∞t=1 fluctuates around the steady
state. Generally, during the Great Moderation economists tend to believe that the long
term rate will approach to a constant since the volatility keeps decreasing. However,
the recent Great Recession breaks the illusion of economists and consequently, the
fluctuation of Ct and Lt could be the direct result from the variation of µt.
16
Also, from (25), we should have
Le = {peβρCe ρ−1λS
e−1w1[(1− pe)(1 + Se lnλ) + peλ(1 + (Se + 1) lnλ)]
1− ρ}−
1ρ (28)
where Ce, Se, Le are the steady state of Ct, St and Lt, where
pe =Se
2(Se + 1)λ(29)
The properties of the steady state could be derived without difficulties.
Proposition 3. ∂Le
∂β < 0. It indicates the steady state working level will be higher
if the worker have an increasing preference level on the future period, which could be
expected in the infinity period problems due to income effect.
Proposition 4. ∂Le
∂ρ < 0. If the preference for consumption over leisure is higher,
then the equilibrium working level should increase, which is also quite intuitive due to
substitution effect between consumption and leisure.
Proposition 5. ∂Le
∂Se < 0. That is to say, if the equilibrium social status increases,
the leisure level at the steady state will be lower. Obviously, it is due to substitution ef-
fect such that with higher class/social status the income will be higher, which generates
a higher utility level.
Proposition 6. ∂Le
∂Ce < 0. With higher equilibrium leisure, the consumption level
will be lower, which seems to be intuitive at first glance. Notice that the representative
agent will never choose any unnecessary additional working hour since the marginal
utility loss would be higher than the marginal utility gain from the potential promotion,
given the additional working hour could not significantly enhance the belief for the firm
that this worker is indeed working hard to be promoted. In short, ”lazy” people have
with less consumption.
Proposition 7. ∂Le
∂λ < 0.The working hour will increase with respect to the relative
output elasticities between adjacent classes λ. We should also notice that λ is positively
correlative to the difficulty of promotion and negatively correlative to the number of
classes. It could also be obtained that the more difficult for each promotion and the
less classes in the hierarchy systems, the equilibrium working level should be higher as
17
well as the consumption level. For instance, when we revisit the stories of Two Sigma
and Apple, it is widely-known that Apple has a relatively stricter promotion policy
than Two Sigma for coding and machine learning group. With Proposition 7 we
shall reach the conclusion that Apple is the priority choice for hard-workers comparing
to Two Sigma, which is exactly what we observed in reality when you come across the
parking lots for both companies during weekends.
For Model 2, we evaluate the Euler Equation with respect to consumption and
evaluate the consumption, class, leisure, interest rate at their corresponding steady
state. ( ie Ct = Ce, St = Se, Lt = Le µt = µ).
Seη = β(1 + µ)Se
2(Se + 1)λ(Se + 1)η + β(1 + µ)(1− Se
2(Se + 1)λ)Seη
= β(1 + µ)Seη + β(1 + µ)Se
2(Se + 1)λ
∞∑k=1
(η
k
)Se η−k
(30)
From (30) it can be found that β(1 +µ) < 1, which indicates the preference for current
consumption is higher in Model 2 comparing to Model 1.
Proposition 8. From the (30) we should have ∂Se
∂β < 0 when η < 56β(1 + µ).
Proof is provided in the appendix. We could conclude if the preference for current
period utility is high, the employee will tend to chase for a higher level of social status.
With very similar logic, the following proposition is obtained.
Proposition 9. ∂Se
∂µ < 0 when η < 56β(1 + µ).
It is straightforward if the return on asset is low, which is similar to the effect of a low
β, the preference for current period is higher and the corresponding feedback is to hunt
for a higher social level.
Then we repeat the same procedure and gain the following expression for the steady
state of leisure.
ALe −ρ +BLe 1−ρ = D (31)
where
A = 1− ρ > 0 (32)
B = −pe(1− pe)β Ceρη
(1− γ)Se− pe 2β
Ce ρη
(1− γ)Se< 0 if γ < 1 (33)
18
D = peβρCe ρ−1λSe−1w1[(1− pe)(1 + Se lnλ) + peλ(1 + (Se + 1) lnλ)] > 0 (34)
and
pe =Se
2(Se + 1)λ(35)
We have the following important result.
Proposition 10. ∂Le
∂η < 0 when γ ≤ 1 and ∂Le
∂η is ambiguous when γ > 1 . In
particular, when η = 0 Model 2 shrinks to Model 1. Consequently the steady state
leisure level under positive preference on the social status should be higher than no
preference case if the relative risk aversion level is small (γ ≤ 1), which is still higher
than the negative preference case.
The proof is not hard, which is included in the appendix.
With no preference on social status case η = 0 when the relative risk aversion level is
low, the worker simply chooses the optimal working level where marginal consumption
benefit from working equals marginal loss from sacrificing leisure. However, in positive
preference on social status case(η > 0), the working level is chosen at the point where
marginal utility loss from decreasing leisure equals marginal consumption benefit from
working plus marginal status gain from the increasing chances of promotion. Employee
tends to work more than no preference case since working provides additional benefit
6 in class enhancement besides consumption benefit. On the contrary, when η < 0
the preference for status is negative. The working level is selected at the point where
marginal benefit from consumption less the utility loss from a higher status equals
marginal loss from a diminishing leisure level, which leads to a higher leisure level
comparing to no preference case. But when the relative risk aversion ratio γ is high
enough, it might happen that the income effect dominates the substitution effect, which
leads to an ambiguous change in the labor input level 7.
For Model 3. S is calculated as the following expression.
S =
∫SdF (S) (36)
6It could be treated as a sort of additional substitution effect because of higher ”income” from socialstatus gain.
7See Chetty Raj 2005, if γ > 1.25 in his approach, the income effect might dominate substitutioneffect, leading a potential downward sloping labor supply curve.
19
where F (S) is the cumulative distribution function of S.
The general conclusion for Model 3 would not be significantly different from Model
2 where the workers care relative social status in Model 3 while focus on absolute
class in Model 2. If the skewness of F (S) is zero (for example normal distribution),
the optimum working-leisure choice decision function will be exactly the same as the
previous case. However, it is generally believed that the class structure is right skewed
(positive skewness with some extent of income inequality). In this case S will be greater
than the equilibrium social status. Therefore, the marginal utility gain from a higher
status with more labor input will be smaller in Model 3, which leads to a higher
equilibrium leisure level in this case. In a unlikely-to-be-true negative skewness case,
the equilibrium leisure will be less than Model 2 case, encouraging each worker to work
even harder and consumes less leisure. It is observed in some Korea-culture-dominate
corporations such as Samsung.
For Model 4, let S = S − κS. When we replace S with S in the Euler Equation
of Model 2, the Euler Equation for Model 4 is therefore obtained. If κ > 0 the
equilibrium status level must be higher.
The economic explanation for κ is that it represents the self-identified ambition
level. Clearly the well-educated worker tends to have a higher κ value, chasing a higher
position in the company. In this case, the equilibrium working hour will be longer
and the corresponding consumption level is enhanced. For instance, if in a particular
society a level 1 steady state class level in never tolerated, then κ will be intentionally
selected above 1/S. Any rational worker will never stay at S = 1 for very long time
since the utility level is negative no matter how much consumption the employee could
have.
Model 4 also provides groundbreaking evidence to explaining the asset return dif-
ference among various countries. Suppose we have two economies (type H and type
L with corresponding ambition level κH and κL where κH > κL) and the observed
average social status are the same for those two economies. In other word, SH = SL.
Since κH > κL, we get
SH − κH S = SH < SL = SL − κLL (37)
20
With Proposition 9 we can conclude the µH > µL, which indicates type H economy
would have a rate of return on asset (which is an exogenous variable in my model).
With the same logic and Proposition 8, we could also conclude a higher β should be
accompanied with a higher realized rate of return on asset. However, when higher κ
leads to advanced level of economic growth, we can fail to conclude that the correspond-
ing self-identified utility level is also high. Taking Japan as an example, Japanese care
greatly on the relative social status and seldom tolerate staying on the low class within
the company. Consequently the labor hour is very high and so is consumption level.
The self-identified utility level, however, might be the lowest among OECD countries
with the highest suicide rate. A high ambition level κ greatly reduces the utility level,
pushing everyone inside the economy chasing a higher rank with more labor input and
less leisure with heavy exhaustion.
One more thing to mention is the influence of the working hour standard deviation
σ8. If the worker are approximately homogeneous, then σ would be relatively small.
As a result, a few more hours can significantly increase the promotion probability,
increasing the utility for the worker sharply without much leisure loss. On the contrary,
if σ is high, only the employee who sacrifices a considerable amount of leisure is more
likely to be promoted. Therefore, unless the positive preference over social status is
high enough (for instance, a high κ or η), the employee will be reluctant to trade more
leisure for consumption and social status.
3.4 Stochastic Case and Risk Premium
In this part we consider the general asset pricing problem. Assume there are one risk-
free asset with return µ0 and M risky assets . The price of ith risky asset in period t
Pi,t satisfies the following Geometric Brownian Motion.
dPi,tPit
= µi,tdt+ σi,tdBPi,t,∀1 ≤ i ≤M, ∀t ∈ N (38)
where µit are the expected drifts and σi,t are standard deviation. BPi,t stands for stan-
dard Brownian Motion.
8See Storesletten, Kjetil, Chris I. Telmer, and Amir Yaron (2001), the standard deviation of USworking hour is quite stable comparing to non-financial income and consumption.
21
We assume the employee invests w0,t percentage of total investable asset on the
risk-free asset in period t while puts wi,t percentage on risky asset i. Definitely we
should haveM∑i=0
wi,t = 1,∀t ∈ N (39)
The new choice variables become {wi,t}Mt=0, at+1 and Lt in the original discounted utility
maximization function.
max{{wi,t}Mi=0,{Lt},{at+1}}∞t=0
βtE0[U(Ct, Lt, St)] (40)
subject to
at+1 − at = w0,tat +M∑i=1
µi,tat − Ct +M∑i=1
wi,tσi,tBPi,t (41)
Following the procedure of Bakshi, Gurdip S., and Zhiwu Chen (1996) and Grossman,
Sanford J., and Robert J. Shiller (1982), we obtain the following Euler Equation with
respect to the price of risky asset.
Pi,t = βEt{[Uc(Ct+1, Lt+1, St+1)
Uc(Ct, Lt, St)+Us(Ct+1, Lt+1, St+1)
Uc(Ct, Lt, St)]Pi,t+1} (42)
which are all evaluated on the optimal path Ct = C∗t , Ct+1 = C∗t+1, Lt = L∗t , Lt+1 =
L∗t+1, St = S∗t , St+1 = S∗t+1.
Notice when the worker has no preference on social status, the above Euler equation
(42) is exactly the same as Euler Equation (24)
We further assume Ct, Lt and St satisfy the following stochastic processes.
dCtCt
= µC,tdt+ σC,tdBCi,t (43)
dLtLt
= µL,tdt+ σL,tdBLi,t (44)
dStSt
= µS,tdt+ σS,tdBSi,t (45)
where µC,t, µL,t, µS,t are the expected drift and σC,t, σL,t, σS,t are the expected diffusion.
BCi,t, B
Li,t, B
Si,t are three different standard Brownian Motion.
22
By subtracting the risk-free component from the (42), we have
Et{[UC(C∗t+1, L
∗t+1, S
∗t+1)
UC(C∗t , L∗t , S∗t )
+US(C∗t+1, L
∗t+1, S
∗t+1)
UC(C∗t , L∗t , S∗t )
](dPi,tPi,t
− r0dt)} = 0 (46)
US(C∗t+1, L∗t+1, S
∗t+1) could be omitted when we use Taylor Series Approximation around
the point (C∗t+1, L∗t+1, S
∗t+1).
Et[(µi,t − r0)dt+dPi,tPi,t
][1 +UCCC
∗t
UC
dC∗tC∗t
+UCLL
∗t
UC
dL∗tL∗t
+UCSS
∗t
UC
dS∗tS∗t
] = 0 (47)
let
dBPi,tdB
Ci,t = VP,Cdt (48)
dBPi,tdB
Li,t = VP,Ldt (49)
dBPi,tdB
Si,t = VP,Sdt (50)
With Ito’s Lemma, we could calculate the following risk premium for Pi,t .
µi,t − r0 = −UCCVP,CUCPi,t
−UCLVP,LUCPi,t
−UCSVP,SUCPi,t
(51)
Fama-French three factor model (Fama, Eugene F., and Kenneth R. French 1993) states
that consumption risk should be compensated and included in the asset risk premium
while Zhang Lu q-Factor Model (Hou, Kewei, Chen Xue, and Lu Zhang 2015) states
investment risk should be the dominant component in the Capital Asset Pricing Model.
While in our approach, not only the consumption risk but the leisure risk and social
status risk should be compensated. For instance, if we assume ρ = 0 and η = 0 in
Model 2, our model should be very similar to the original CAPM approach. While we
only set η = 0 in Model 2, it becomes a two-factor model considering both consumption
and leisure risk. When you use the general assumption in Model 2, it turns out to
become a consumption-leisure-class CAPM approach, which definitely, deserves future
research.
23
3.5 Option Explanation
In this part, we attempt the explain the behavior of employee using an alternative
approach. Instead of the traditional Euler Equation approach, we treat the promotion
opportunity as a call option. For example, in the first period, all workers have the class
level 1 and are issued a call option with strike price ”S=2”. It is a binary call option9
with a positive probability of being promoted to the social status S = 2 through current
observed labor input l. We denote the price of such call option call(L, S = 1→ 2). At
the same time, being promoted class level 2 means the additional promotion probability
of being promoted to level 3 in the next period, which could be treated as a call on
call option. And so on. Consequently, the call option combination in period 1 not only
contains a call option of being promoted to level 2 in the next period, but contains a
call of a call option of being promoted to level 3 in the next two periods ,..., and so on.
So the overall value of such option combinations is calculated as follows.
P =∞∑i=2
1∏i−1j=1(1 + µj)
call(L, S = 1→ i) (52)
In Model 1, for example, the workers’ preference for the social status is 0. In this
case, all the benefit of promotion is pecuniary effect.
callModel 1(L, S = 1→ i) = ((i+ 1)λi − iλi−1)w1Pr(1→ i) (53)
where
Pr(1→ i) =i−1∏j=1
[1
λ
j
j + 1
∫ L
−∞
1√2πσ2
exp(−(L− L)2
2σ2)]
=1
λi−1i(
∫ L
−∞
1√2πσ2
exp(−(L− L)2
2σ2))i−1
(54)
Further if we assume µj ≡ µ, ∀j ∈ N , then the price of such option combination is
P = w1
∞∑i=2
1
(1 + µ)i−1[(i+ 1
iλ− 1)(
∫ L
−∞
1√2πσ2
exp(−(L− L)2
2σ2))i−1] (55)
9The payoff of this binary call option is either 0 or being promoted to class 2.
24
A worker will choose the when the Delta of this call option (∆P = ∂P∂L ) equals the
marginal utility of leisure.
Let us discuss the how parameters will influence the median worker’s option com-
bination value. Plug L = L into the expression of P and we can figure out
P = w1
∞∑i=2
1
(2(1 + µ))i−1((i+ 1
i)λ− 1)
= w1[−(1 + 2λµ) + 2λ(1 + µ)(1 + 2µ) ln(2+2µ
1+2µ)
1 + 2µ]
(56)
Clearly we should have ∂P∂λ > 0 and ∂P
∂µ < 0, which is consistent with the characteristics
of a call option that the Rho should be negative.
When we reconsider Model 2 to Model 4
callModel 2∼4(L, S = 1→ i) = [((i+ 1)λi − iλi−1) +MUS ]w1Pr(1→ i) (57)
where MUS is the additional marginal utility gain from the increasing of social sta-
tus, which is positive, negative or zero when the worker has positive, negative or no
preference on the social status. In this case
PModel 2∼4 >=<PModel 1 (58)
and
∆Model 2∼4P
>=<
∆Model 1P (59)
Consequently we have
LModel 2∼4 <=>LModel 1 (60)
when η>=<
0
25
4 Empirical Tests
4.1 Data Description
Obviously, we should use panel data to study the dynamic work-leisure behavior. In
this case, the Panel Study of Income Dynamics (PSID) data is selected to accomplish
our empirical test. The data range are from 1975 to 1992, which the same cohort
and their descendants are surveyed through phone call annually. The beginning year
1975 is selected in particular since it is the time points when reliable phone interviews
were used and the ending year 1992 is chosen since from 1993 computer techniques
are introduced into the survey. During this period the measurement errors could be
regarded as homogeneous.
We have approximately 7,000 effective observations for each year, where the sum-
mary statistics of age, education, hours working per year and annual before-tax income
for labor market participants are provided in Table 7. In our approach, a worker is
considered to be a labor market participant if his/her annual paid working hours are
no less than 200 and the age is between 25 and 70.
From Table 8 to Table 11 we summarize the age, education level, hours working per
year and nominal income for each year in 1975 to 1992. The educational level increases
steadily in those 18 years while the variance decreases significantly during 1984-1988.
A representative working employee increases the working hour during George H.W.
Bush presidential term. The nominal income increases sharply during 1980s. We can
notice the nominal average income for 1990 in PSID panel survey was almost 200%
of 1980, which could be majorly explained by the high inflation rate10 during that
period. Notwithstanding, the real inflation-adjusted average income is still growing
during Ronald Reagon’s presidency but becoming much slower, which is listed in Table
13.
The next very important thing in our model is to calibrate λ and the corresponding
number of classes. Since we use Cobb-Douglas form technology, we have better follow
Cobb-Douglas’s original approach (Charles Cobb, Paul Douglas & NBER 1927, Paul
Samuelson, Robert Solow 1976, Filipe, Jesus; Adams, F. Gerard 2005) to set λ = 3.
10The inflation rate during 1975-1992 is listed in Table 12
26
The effective response for each year is approximately 7,000, which leads to an estimated
7 classes altogether by following the decision rule in Proposition 2 by noticing
7∑i=1
3i−1i = 7, 108 (61)
We use the wage function to decide the class level approximately. By following (15),
the higher wage, the higher social status. By setting the living wage as the separation
line of class 1 and class 2 and following the spirit of equation (15) we use the following
rule to decide the social class level.
• class 1: if the hourly wage in year t ∈ (0, hourly wagetmax/64]
• class 2: if the hourly wage working hour in year t ∈ (hourly wagetmax/64, hourly
wagetmax/32]
• class 3: if the hourly wage in year t ∈ (hourly wagetmax/32, hourly wagetmax/16]
• class 4: if the hourly wage in year t ∈ (hourly wagetmax/16, hourly wagetmax/8]
• class 5: if the hourly wage in year t ∈ (hourly wagetmax/8, hourly wagetmax/4]
• class 6: if the hourly wage in year t ∈ (hourly wagetmax/4, hourly wagetmax/2]
• class 7: if the hourly wage in year t ∈ (hourly wagetmax/2, hourly wagetmax]
where hourly wagetmax represents the highest hourly wage in year t. It could be
found that the individual class status should be indifferent no matter if we use real
income level or not.
If the person’s observed status is increased, s/he is considered to be promoted in
our empirical analysis.
4.2 Basic Empirical Results
First, we have to test one of the most important assumption in our model, where
the promotion chances should be higher for those workaholics. We run the Linear
Probability Model, Probit Model and Logit Model separately to test the efficiency of
our assumption in Table (15).
27
In column 1 to column 3, we could find that all three models report positive in-
fluence of working hour towards to ratio of promotion. If we add education level into
our regression in column 4 to 6 , we could find out the coefficient of working hour
remain significantly positive while the effect of education, without any doubt, is posi-
tive. Finally, if we add linear and quadratic term of age into the regression, the t-stat
for working hours decreases but is still significantly positive while the rest coefficients
are exactly predicted by traditional Mincer earnings function. It is proved our general
assumption is reliable that working longer could help promotion. After considering
the age effect, an additional 1,000 working hours per year will increase the promotion
chances in the next year by 0.58%.
Then we run several Mincer-type earning equations to briefly overview the panel
data we have. The results are listed in Table 16. After controlling for the social status,
the working hour is still positively related to the hourly nominal wage . However, from
column (4) we find the effect of additional working hours on wage rate is insignificant if
we take into account the unemployment hours in the regression. We don’t run Heckman
correction in this table and the result does not depress us that much. We can only argue
that within those who suffer unemployment in one year the hardworking level has no
significant effect on wage rate. At the same time, the unemployment itself is reported
to have a negative effect on the wage ratio, which is consistent with our intuition since
unemployment could send bad signals to employers. When the real wage is used as
regressand, the working hour has a smaller positive influence on the real wage rate. We
could explain the difference of working hour effect in column (1) to (4) and column (5)
to (8) by the high inflation and the upward trend of working hours in the 1980s. That is
to say, working more time will compensate a larger nominal hourly wage increase but a
relatively smaller real wage enhancement measuring by dollars in 1975. Meanwhile, we
could never fail to notice the return on education in column (6) and (7) are significantly
negative, which could be the result of controlling for various status. Suppose person
P1 and person P2 are in the same class level C but P1 has a relatively higher education
level than P2, the education itself might send weaker signal of person P1 comparing to
P2 since the effort for P2 to reach level C is much more challenging than P1 with a low
starting point. An additional 1,000 hours per year could increase the inflation-adjusted
28
hourly compensation by 0.18 dollars measuring in 1975 dollars. The preliminary result
is subject to endogeneity challenge but still pretty useful to understand the hour-wage
relationship.
We also report the influence of working hour effect in Table (17) by using Heckman
Correction. The independent variables we use in the first step Probit selection model are
education, age (or experience), type of income and relationship to the head of the family.
The very similar result are reported in Table (16) whether we use Heckman Correction
or not, suggesting the self-selected labor market participation decision (which is decided
by education, age, type of income and family condition linearly in our approach) would
not have a significant influence on the wage ratio. Also the standard robustness check
are done by replacing age with working experience (exp) by using the following equation
exp = age− edu− 7 (62)
The result shows that although the coefficients of age and experience slightly differ,
the sign does not change. The coefficient for working hours decreases only 2 % when
the age variable is replaced by experience, indicating a strong positive effect of working
hour on the wage ratio.
4.3 Calibration for the social preference
The next step is to calibrate the parameters β, γ, η and κ. First we use only the
equation (24) to determine β and γ. First we use the Federal fund rate from 1975
to 1993 as the risk-free return on asset µt, which is appended in Table 18. With the
lack of individual consumption data in PSID, we make a plausible assumption that the
proportion of consumption in current income is steady between two continuous years.
Although there is permanent income hypothesis claiming a person’s consumption at a
point is determined not just by their current income but also by their expected income
in the future. Campbell, John Y., and N. Gregory Mankiw (1991) finds that the
fraction of income accrues to individuals who consume their current income instead of
their permanent income by testing the postwar data of US till 1990, which is consistent
with our settings and data period. In this case, we could use inter-temporal relative
29
income as a good proxy of inter-temporal relative consumption. Also, we assume the
leisure each year is calculated by the following equation by excluding 8 hours per day
resting hour from the total allocatable time. Notice 5840 = 16 ∗ 365.
leisure = 5840− working hour (63)
By using Euler Equation of consumption we can calibrate ρ and γ.
The instruments we use here in the Generalized Method of Moments is the one-
year lag risk-free interest rate and social status, which by no means correlate with the
variable we use in calibrating ρ and γ.
E[U tc − β(1 + µt)Ut+1c |rt−1] = 0 (64)
and
E[U tc − β(1 + µt)Ut+1c |St−1] = 0 (65)
Table 1: Calibration Results by Consumption EE in Model 1
GMM weight matrix: HAC Bartlett 4
Coeff. Std. Err. z p > |z| [95% confidence interval]
β 0.95 literature value
γ .2553133 .0732329 3.49 0.000 [ .1117794, .3988471 ]
ρ .9756675 .1100314 8.87 0.000 [ .76001,1.191325 ]
We could find that λ < 1. According to Raj Chetty (2005), the substitution effect
dominates income effect as λ < 1.25 threshold point, indicating a upward sloping labor
supply curve for the PSID data from 1975-1992. The existing literature suggests λ
could vary from 0.15 to 1.45, indicating no out of expectation λ value. The ρ value
here, however, is least important since the absolute weight of leisure could change with
different unit measure of relative consumption and leisure.
Then we reestimate the value of γ and ρ by taking into account the social status
influence. For Model 1, equation (28) are included in the simultaneous equations.
30
One-year and two-year lag risk-free interest rates are used as proxies for (28) to obtain
two more moment conditions. And we should decide the w1 first. We calibrate w1 in
each year from 1975 to 1992 by using the average income of the workers in first class,
just as the original setting in the firm sector .
Table 2: w1 used from 1975 to 1992w1 value for each year 1975-1992
1975 1976 1977 1978 1979 1980 1981 1982 1983
2250.141 1652.54 1551.471 2412.876 2011.671 4092.228 5017.307 4753.249 2696.743
1984 1985 1986 1987 1988 1989 1990 1991 1992
3364.369 9606.21 3295.947 5163.282 8860.022 12709.87 9515.766 7315.009 6855.409
The results obtained by the Generalized Method of Moments are
Table 3: Calibration Results by Consumption and Social Status EE in Model 1
GMM weight matrix: HAC Bartlett 4
Coeff. Std. Err. z p > |z| [95% confidence interval]
β 0.95 literature value
γ .627034 .0082546 75.96 0.000 [ .6108553 .6432128 ]
ρ .4222069 .0287144 14.70 0.000 [ .3659278 .478486 ]
Notice after we considering the embedded promotion option in equation (28), the
calibrated relative risk aversion rate will increase a lot, but still less than 1.25 threshold
indicated by Raj Chetty (2005), which points out that the substitution effect still
dominates income effect even taking into account the promotion option value but a little
bit weaker. In other word, the labor supply curve becomes even steeper, which could
have a high slope than tradition belief. It could be the case that the standard expected
utility function without promotion setup could fail to explain a higher relative risk
aversion, which is consistent with Browning, Hansen, and Heckman (1999) suggesting
λ as high as 4.
Then we shift to estimate the η in Model 2. Focusing on equation (31),
ALe −ρ +BLe 1−ρ = D (66)
Notice ALe −ρ << D and ALe −ρ << BLe 1−ρ, we should have the approximate
31
equation
BLe 1−ρ = D (67)
Together with the equation (24), we reach out the following calibration values by using
the Generalized Method of Moment. In our model here, we use the one-period lagged
interest rate, two-period lagged interest rate and one-period lagged promotion rate
as instruments for equation (64) while the one-period lagged interest rate, two-period
lagged interest rate and status are used as instruments for equation (24).
Table 4: Calibration Results Model 2GMM weight matrix: HAC Bartlett 4
Coeff. Std. Err. z p > |z| [95% confidence interval]
β 0.95 literature value
γ 1.610928 .1203562 13.38 0.000 [ 1.375034 1.846821 ]
ρ .9760741 .012142 80.39 0.000 [ .9522762 .999872 ]
ln ηγ−1 1.478234 .1202525 12.29 0.000 [ 1.242543 1.713924 ]
In this case, the estimated preference level of social status is exp(1.478234)∗(1.610928−
1) = 2.679. Interestingly we find the relative risk aversion ratio γ is quite large in this
calibrated model, which contradicts the traditional belief that γ < 1.25 in most labor
economics literature. However, the large γ does not generate a downward sloping labor
supply curve in Model 2 since there is additional utility gain from social status which
provides more incentive to substitute leisure with working hours. We could still ar-
gue the labor supply curve is upward sloping, being consistent with standard textbook
conclusion. And with the inclusion of promotion variable, the relative risk aversion
ratio could be higher than the standard assumption, which is exactly what some non-
expected-utility theories argue.(Chew and MacCrimmon 1979, Tversky and Kahneman
1992).
In the next step we calibrate η for each year during 1975 to 1992 to help us under-
stand the change of preference on social status during these two decades. The method
we use is similar but in this part each year’s data are treated as cross-sectional rather
than panel.
32
Table 5: η calibration value for each year 1975-19921975 1976 1977 1978 1979 1980 1981 1982 1983
2.425 2.301 2.268 2.472 2.701 2.736 2.708 2.799 2.808
1984 1985 1986 1987 1988 1989 1990 1991 1992
2.831 2.972 2.862 2.825 2.909 2.990 2.909 2.871 2.950
The preference on the social status varies from 2.2 to 3.0 during 1975 to 1992,
showing a relative high preference towards social status, which might contradict the
general belief. In the next figure we show the relative relationship between η and annual
working hours, nominal wage, inflation rate, real wage, respectively.
Figure 1: The relative relationship between η and annual working hours, nominal wage,inflation rate, real wage
And the correlation matrix is listed as follows.
We could find when the preference for social status increases, the annual working
hours also increases, which is consistent with our conclusion in Proposition 10. Mean-
while, the nominal wage rate increases while the real wage decreases at the same time.
33
Table 6: The correlation matrix of η, annual working hours, nominal wage, inflationrate and real wage
correlation η annual working hours nominal wage inflation real wage
η 1.0000
annual working hours 0.2995 1.0000
nominal wage 0.8952 0.5481 1.0000
inflation -0.3992 -0.3201 -0.6303 1.0000
real wage -0.0094 0.5478 0.0888 -0.2515 1.0000
It might give us hint the preference for social status would increase just because of the
high inflation. The employers are pushed to have a higher preference on status to catch
up the inflation speed during the high inflation era. The relationship between inflation
and social status preference could be a challenging research topic that deserves future
works.
It should be pointed out the approximation in equation (65) guarantees γ should be
no less than 1, indicating a higher than usual risk aversion level in the utility function.
However, it does not lead to a downward sloping labor supply curve with high γ since
in our approach the positive taste for social status generates additional incentive for
employees to work more. The existing literature in labor economics literature suggest-
ing a low risk aversion ratio could be less convincing without taking into account other
utility gains besides consumption and leisure. For instance, a higher rank in the soci-
ety/corporation may provide a employee a first-class business trip, a special assistant
and/or security service, which is never generally considered as personal consumption
and is not recorded by the standard database like PSID.
4.4 Unemployment Influence
The final thing in this section is to examine whether hard-working hurts the labor
market by generating more unemployment. It could be expected that increasing work-
ing hours could decrease a person’s unemployment time automatically. From Table
(19) and Table (20) we could indeed confirm this conclusion. However, if we run the
regression by each social class respectively, the statement that working more hours
could significantly reduce unemployment time is true only for low-rank classes but not
for high-rank employees. It might be explained that employees rely heavily on the
34
working-hour as tools of making hiring decisions for junior workers while for seniors
the self-selected hardworking level could not affect the unemployment level. That is
to say, the assumption in my approach assuming self-selecting working hour as ability
signal might not remain valid for high-rank employees. We might use other assump-
tions to depict the hiring decisions for high-rank employees and the matching model
for entrepreneurs could differ a lot.
Meanwhile we examine whether the working hour has a significant influence on
the unemployment the year after. The result is reported in Table (20) and Table
(21). Instead of the real working hour, current year’s unemployment hour could be
a good predictor of next year’s unemployment situation, which gives us hint that the
unemployment could be lasting. The rest of the result is quite similar to Table (18) and
Table (19). Therefore, we could reach an educated guess that working overtime under
various preference on social status might not increase the unemployment, which could
be inconsistent with our naive expected results. The social status preference, however,
influences the intensive margin greater than extensive margin more significantly.
4.5 Discussion of the PSID data
The biggest advantage of using PSID dataset is that it could be used as panel tracking
on the same cohort for a long time. In this case, it is possible for us the depict the
social status preference consistently. However, we could still fail to neglect the potential
weakness of using PSID database.
The first weakness is that PSID does not record the aggregate level of consumption.
It adds additional difficulty when we have to estimate the consumption in aggregation
level, which creates additional measurement errors. The first treatment is to use food
consumption/garbage generation (A Savov 2011) in some particular years as proxies of
overall consumption. However, the Engel Coefficients/garbage generation between the
poor and the rich, the person who has a high social preference and the the person with
a lower one could be totally different, which makes the consumption level estimates
unconvincing. Also PSID does not record the food consumption for each year, adding
more difficulties of using food consumption to estimate the overall consumption. Conse-
quently, we make the rational assumption that inter-temporal relative income could be
35
used a good proxy of inter-temporal relative consumption despite the widely-believed
permanent income hypothesis.
Secondly, PSID uses a top coding rule for protecting the private information of
the rich. For instance, in the year 1992 all the salary income greater than 999,999
dollars are reported as 999,999 dollars. It is a mechanism to protect the high-income
responders’ incentive to participate the survey more actively but create biases for our
conclusion. Since the top coding strategy is treated as an up-censored model, the real
incentive for promotion could be underestimate, particularly for high-rank employees.
As a result, I am strongly convinced that the preference for social-status preference
should be overestimated since the pecuniary marginal utility is underestimated by us-
ing PSID database. A possible robustness check is to use other panel database like
National Longitudinal Survey of Youth 1979 (NLSY79) to test the validity of the var-
ious preference on social status and other non-pecuniary factors, which is still beyond
current research and deserves future work.
5 Concluding Remarks
It is the time to answer the three questions raised at the beginning of this article. Indeed
different social status preference could have a significant impact on work-leisure choices.
In our benchmark model, social status is considered to be non-pecuniary normal good.
The substitution effect will dominate income effect for the employee with high rank
preference level, which leads to a longer working hour. They work more time even
overtime a lot, sending their strong-ability signals to employees not only to increase
their potential salary income after promotion but the utility level with a higher social
status. The signaling effect is tested to be weaker for high-rank positions. The working
hour will increase with respect to the relative output elasticities between labor and
capital input. As a result, it is widely observed that workers in developing economies
tend to work overtime more frequently than in developed countries. The leisure time
will be less if the median worker is fond of a higher rank position. In other word, if
the preference for social status is higher inside one corporation, the leisure time will
be occupied with working with higher probabilities. We could observe the working
36
overtime phenomenon in Asian companies since most workers are educated to surpass
others in their early age. For instance, many students are educated to be man on top of
man in those Confucian-dominated culture. In this case, the rational choice is to work
more and consume less leisure. For instance, an Asian kid is typically educated that
Peking University, Tsinghua Universiy, Seoul National University, Tokyo University,
IIT, Harvard, MIT, Stanford are the only choices of college education, which going
without saying increases the working load for teenagers. However, the utility level
might be lower with a strong preference on relative ranking11. An economy with higher
preference on relative ranking should have a faster growth rate while the self-identified
utility level of each individual could be lower. They tend to believe that the utility level
is negative no matter how high are the consumption and leisure level12 if they can fail
to surpass their peers. In other word, they become extremely exhausted chasing high
social ranks although they are compensated with higher consumption level. Finally, we
find no significant evidence that high social preference and working overtime will lead
to an increasing unemployment level. There is still a long way to go to examine the
culture’s influence on labor market decisions. For instance, we could test the validity
of our conclusion using other US or developing countries databases, which could be a
challenging topic for future research.
11In Model 4, it is depicted as a higher κ value12In Model 4, if the social status is lower than κS the utility level is negative.
37
Appendix
Proof of Proposition 2. For the simultaneous inequalities
k∑i=1
(1
λ)i−1 1
in1 = N (68)
(1
λ)k−1 1
kn1 ≥ 1 (69)
(1
λ)k
1
k + 1n1 < 1 (70)
If we assume when N increase to N + 1, kN+1 < kN . Notice k is decided by (69) and
(70) . Then n1,N+1 < n1,N . Then in (68), we should have
kN+1∑i=1
(1
λ)i−1 1
in1,N+1 ≤
kN∑i=1
(1
λ)i−1 1
in1,N+1
<
kN∑i=1
(1
λ)i−1 1
in1,N
= N
(71)
It leads to contradiction. So kN+1 ≥ kN .
Also if assume when λ increase to λ′, kλ′ > kλ. Notice k is decided by (69) and (70)
Then n1,λ′ > n1,λ. Since the promotion difficulties increases and the number of class
also increases, we should have for each rank,
(1
λ′)i−1 1
in1,λ′ ≥ (
1
λ)i−1 1
in1,λ (72)
And
kλ′∑i=1
(1
λ′)i−1 1
in1,λ′ ≥
kλ∑i=1
(1
λ′)i−1 1
in1,λ′ + (
1
λ′)kλ
1
kλ + 1n1,λ′
≥kλ∑i=1
(1
λ)i−1 1
in1,λ + (
1
λ′)kλ
1
kλ + 1n1,λ′
> N
(73)
It leads to contradiction. So kλ′ ≤ kλ.
38
Proof of Proposition 8.
Let
p =S
2(S + 1)λ(74)
Notice
∂p
∂S> 0 (75)
Take the total differential of (30), we should have
ηSη−1
β(1 + µ)dS+
Sη
1 + µ(− 1
β2)dβ =
∂p
∂S(S+1)ηdS+pη(S+1η−1)dS+(1−p)Sη−1dS− ∂p
∂SSηdS
(76)
We have
dS
dβ=
Sη
1+µ(− 1β2 )
((S + 1)η − Sη) ∂p∂S + (pη(S + 1)η−1 + (1− p)Sη−1 − ηSη−1
β(1+µ))< 0 (77)
since
((S + 1)η − Sη) ∂p∂S
> 0 (78)
thus
(pη(S + 1)η−1 + (1− p)Sη−1 − ηSη−1
β(1 + µ)) > (1− p)Sη−1 − ηSη−1
β(1 + µ)> 0 (79)
when 1− p > 56 >
ηβ(1+µ) in our later approach
Proof of Proposition 10.
Take the total differential of (31).
−ρALe −ρ−1dL+ Le 1−ρdB + (1− ρ)BL−ρdL = 0 (80)
We have
dL
dB=
Le 1−ρ
ρALe −ρ−1 − (1− ρ)BLe −ρ> 0 (81)
since A > 0 and B < 0 if γ < 1
Notice ∂B∂η < 0 we have ∂Le
∂η < 0
39
Table 7: Summary statistics for panel data
Variable Mean Std. Dev.
age 38.864 11.051educaion 13.821 10.953nominal income 18116.744 20800.172annual working hours 1877.982 722.348
N 141436
Table 8: Age summary for each year
Year Mean Std. Dev.
1975 40.683 11.8651976 40.295 11.8641977 39.897 11.8441978 39.562 11.7931979 38.906 11.7591980 38.551 11.6121981 38.383 11.4811982 38.325 11.2981983 38.206 11.1931984 38.235 11.0671985 38.261 10.9451986 38.101 10.7161987 38.222 10.5411988 38.273 10.3991989 38.922 10.4041990 39.115 10.571991 39.262 10.4541992 39.502 10.375
40
Table 9: Education level summary for each year
Year Mean Std. Dev.
1975 11.63 3.0631976 11.748 2.9951977 11.837 2.9461978 11.917 2.8611979 12.018 2.7881980 12.121 2.6831981 12.213 2.6071982 12.279 2.5691983 12.438 2.6381984 12.485 2.5881985 12.802 2.5671986 12.846 2.5211987 12.889 2.4781988 12.929 2.4051989 13.243 4.6811990 12.487 2.9191991 12.515 2.891992 12.551 2.864
Table 10: Hours working per year summary 1975-1992
Year Mean Std. Dev.
1975 1872.584 741.3121976 1851.446 749.0241977 1876.023 737.3341978 1895.655 739.7081979 1880.287 730.2061980 1854.485 722.2761981 1838.884 719.0421982 1838.35 706.3921983 1812.677 722.3611984 1828.622 712.5681985 1870.425 730.1751986 1885.719 723.1511987 1895.668 713.9171988 1915.36 712.8471989 1953.08 718.2461990 1909.997 709.1741991 1913.027 704.2581992 1905.777 712.644
41
Table 11: Nominal income summary per year 1975-1992
Year Mean Std. Dev.
1975 9366.403 8136.3331976 9741.860 8019.9611977 10807.123 8869.2211978 12047.257 10316.6741979 12684.298 10801.7731980 13748.575 11348.6491981 14799.202 12484.3251982 16105.113 13395.9771983 16923.797 16338.4471984 18052.262 17867.3691985 19535.002 26110.8281986 20162.431 20439.0091987 21215.044 24605.8121988 22359.454 26948.9221989 24184.252 27122.6381990 23003.262 27420.6281991 22491.541 22089.8721992 23230.69 24691.309
Table 12: US inflation rate 1975-19921975 1976 1977 1978 1979 1980 1981 1982 1983
11.80% 6.72% 5.22% 6.84% 9.28% 13.91% 11.83% 8.39% 3.71%
1984 1985 1986 1987 1988 1989 1990 1991 1992
4.19% 3.53% 3.89% 1.46% 4.05% 4.67% 5.20% 5.65% 2.60%
42
Table 13: Real income per year(in 1975 dollars) summary 1975-1992
Year Mean Std. Dev.
1975 9366.403 8136.3331976 9128.429 7514.9561977 9624.23 7898.4411978 10041.768 8599.2731979 9627.355 8198.5231980 9160.862 7561.761981 8817.768 7438.5021982 8853.091 7363.8611983 8970.329 8660.0671984 9183.666 9089.6071985 9599.127 12830.3631986 9536.466 9667.2821987 9889.939 11470.6331988 10017.718 12073.9391989 10351.852 11609.6011990 9359.638 11156.991991 8662.023 8507.3311992 8719.968 9268.232
Table 14: Federal Fund Rate 1975-19921975 1976 1977 1978 1979 1980 1981 1982 1983
7.13% 4.87% 4.61% 6.70% 10.07% 13.82% 19.08% 13.22% 8.68%
1984 1985 1986 1987 1988 1989 1990 1991 1992
9.56% 8.35% 8.14% 6.43% 6.83% 9.12% 8.23% 6.91% 4.03%
43
Tab
le15
:T
esti
ng
whet
her
pro
mot
ion
rate
incr
ease
sw
ith
resp
ect
tom
ore
wor
kin
gh
ou
rs
pro
mot
ion
(1)
(2)
(3)
(4)
(5)
(6)
(7)
(8)
(9)
LP
MP
robit
Log
itL
PM
Pro
bit
Logit
LP
MP
robit
Logit
annual
wor
kin
ghou
rs0.
0000
0542∗
∗∗0.
0000
189∗
∗∗0.
0000
330∗
∗∗0.
0000
0579
∗∗∗
0.0000205∗
∗∗0.0
000362∗
∗∗0.0
0000264∗
0.0
000114∗
∗0.0
000201∗∗
(4.6
1)(4
.70)
(4.7
2)(4
.93)
(5.0
4)
(5.0
9)
(2.2
3)
(2.6
8)
(2.6
3)
educa
tion
0.00
167∗∗
∗0.
00556∗∗
∗0.0
0897∗
∗∗0.0
0167∗
∗∗0.0
0560∗∗
∗0.0
0910∗
∗∗
(16.9
9)(1
8.9
9)
(19.1
5)
(17.0
3)
(19.0
1)
(19.2
7)
age
0.0
0238∗
∗∗0.0
0842∗∗
∗0.0
145∗
∗∗
(26.5
2)
(27.3
4)
(27.5
0)
age2
-0.0
0000222∗∗
∗-0
.00000790∗∗
∗-0
.0000136∗∗
∗
(-15.9
9)
(-18.2
5)
(-18.4
8)
const
ant
term
0.19
1∗∗∗
-0.8
74∗∗
∗-1
.443∗
∗∗0.
170∗∗
∗-0
.945∗∗
∗-1
.559∗∗
∗0.0
960∗∗
∗-1
.215∗∗
∗-2
.027∗
∗∗
(81.
97)
(-10
7.65
)(-
101.
68)
(65.
88)
(-104.7
7)
(-99.4
3)
(26.4
8)
(-90.1
3)
(-85.7
7)
N14
1436
1414
3614
1436
14143
6141436
141436
141436
141436
141436
tst
ati
stic
sin
pare
nth
eses
∗p<
0.0
5,∗∗p<
0.0
1,∗∗∗p<
0.0
01
44
Tab
le16
:R
egre
ssio
non
nom
inal
and
real
wage
per
hou
raft
erco
ntr
oll
ing
stat
us
dep
end
ent
vari
ab
le(1
)(2
)(3
)(4
)(5
)(6
)(7
)(8
)w
agep
erh
ou
rw
agep
erh
ou
rw
agep
erh
ou
rw
agep
erh
ou
rre
alw
agep
erh
ou
rre
alw
agep
erh
ou
rre
alw
agep
erh
ou
rre
alw
agep
erh
ou
r
an
nu
al
work
ing
hou
rs0.0
00419∗∗∗
0.0
00440∗∗∗
0.0
00381∗∗∗
0.0
000371
0.0
00201∗∗∗
0.0
00198∗∗∗
0.0
00183∗∗∗
0.0
0000957
(18.3
6)
(19.3
0)
(16.6
7)
(1.7
8)
(20.0
2)
(19.7
1)
(18.2
1)
(0.8
2)
(sta
tus
=1
isom
itte
d)
statu
s=2
3.5
56∗∗∗
3.4
75∗∗∗
3.4
62∗∗∗
2.0
07∗∗∗
1.6
51∗∗∗
1.6
63∗∗∗
1.6
61∗∗∗
1.6
07∗∗∗
(83.5
3)
(81.5
9)
(81.6
3)
(46.9
1)
(88.4
4)
(88.8
6)
(88.9
2)
(67.3
6)
statu
s=3
7.3
38∗∗∗
7.2
33∗∗∗
7.1
54∗∗∗
4.9
15∗∗∗
3.9
07∗∗∗
3.9
22∗∗∗
3.8
99∗∗∗
4.0
72∗∗∗
(159.2
8)
(156.8
0)
(155.5
7)
(113.4
0)
(193.4
2)
(193.5
0)
(192.5
5)
(168.5
4)
statu
s=4
14.4
0∗∗∗
14.2
8∗∗∗
14.0
6∗∗∗
9.5
00∗∗∗
8.2
82∗∗∗
8.3
00∗∗∗
8.2
28∗∗∗
8.0
77∗∗∗
(202.7
3)
(201.0
6)
(197.9
4)
(167.0
7)
(265.9
8)
(266.0
5)
(263.1
3)
(254.8
1)
statu
s=5
33.3
9∗∗∗
33.2
5∗∗∗
32.9
6∗∗∗
21.2
3∗∗∗
19.3
2∗∗∗
19.3
4∗∗∗
19.2
4∗∗∗
17.9
2∗∗∗
(185.5
3)
(185.0
9)
(183.9
4)
(169.2
4)
(244.9
4)
(245.1
5)
(243.8
8)
(256.2
4)
statu
s=6
80.3
4∗∗∗
80.2
3∗∗∗
79.9
0∗∗∗
42.2
2∗∗∗
45.4
6∗∗∗
45.4
8∗∗∗
45.3
6∗∗∗
35.2
2∗∗∗
(193.8
2)
(194.0
0)
(193.9
9)
(134.8
1)
(250.2
4)
(250.3
8)
(250.1
9)
(201.8
0)
statu
s=7
263.7∗∗∗
263.5∗∗∗
263.3∗∗∗
114.3∗∗∗
132.0∗∗∗
132.0∗∗∗
132.0∗∗∗
95.3
6∗∗∗
(284.5
8)
(284.9
8)
(286.0
2)
(102.4
0)
(324.9
9)
(325.1
4)
(325.6
0)
(153.3
2)
edu
cati
on
0.0
410∗∗∗
0.0
425∗∗∗
0.0
281∗∗∗
-0.0
0596∗∗∗
-0.0
0533∗∗∗
0.0
123∗∗∗
(26.3
5)
(27.3
2)
(15.6
5)
(-8.7
1)
(-7.7
8)
(12.2
9)
age
0.4
00∗∗∗
0.0
679∗∗∗
0.1
13∗∗∗
0.0
444∗∗∗
(33.2
2)
(6.9
0)
(21.3
6)
(8.1
0)
age2
-0.0
0434∗∗∗
-0.0
00709∗∗∗
-0.0
0119∗∗∗
-0.0
00443∗∗∗
(-31.2
5)
(-6.2
3)
(-19.4
7)
(-6.9
9)
un
emp
loym
ent
-0.0
00264∗∗∗
-0.0
00137∗∗∗
(-5.9
1)
(-5.5
0)
con
stant
term
3.6
70∗∗∗
3.1
73∗∗∗
-5.1
52∗∗∗
0.6
06∗∗
2.0
14∗∗∗
2.0
86∗∗∗
-0.3
40∗∗
0.5
63∗∗∗
(72.3
8)
(58.7
7)
(-20.9
5)
(3.0
0)
(90.5
0)
(87.8
7)
(-3.1
4)
(5.0
0)
N142964
142964
142964
41143
142881
142881
142881
41139
tst
ati
stic
sin
pare
nth
eses
∗p<
0.0
5,∗∗p<
0.0
1,∗∗∗p<
0.0
01
45
Table 17: The influence on wage rate using Heckman correction
Regressand (1) (2) (3) (4)realwageperhour realwageperhour realwageperhour realwageperhour
annual working hours 0.000271∗∗∗ 0.000267∗∗∗ 0.000270∗∗∗ 0.000267∗∗∗
(15.50) (15.49) (15.49) (15.48)
education 0.0184∗∗∗ 0.181∗∗∗ 0.0184∗∗∗ 0.181∗∗∗
(15.46) (64.20) (15.46) (64.22)
age 0.262∗∗∗ 0.262∗∗∗
(28.48) (28.49)
age2 -0.00257∗∗∗ -0.00257∗∗∗
(-24.17) (-24.17)
experience 0.118∗∗∗ 0.118∗∗∗
(64.03) (64.06)
experience2 -0.00145∗∗∗ -0.00145∗∗∗
(-54.00) (-54.00)
constant term -1.918∗∗∗ 0.684∗∗∗ -1.917∗∗∗ 0.685∗∗∗
(-10.19) (10.29) (-10.19) (10.31)selecteducation 0.000194 -0.0109∗∗∗
(0.18) (-7.16)
age -0.0111∗∗∗
(-10.61)
relation -0.0300∗∗ -0.0298∗∗
(-2.66) (-2.65)
type of income 0.101∗∗∗ 0.101∗∗∗
(6.95) (6.94)
experience -0.0111∗∗∗
(-10.61)
cons 2.863∗∗∗ 2.786∗∗∗
(53.24) (57.66)athrhocons -0.0272∗∗ -0.0267∗∗
(-2.91) (-2.88)lnsigmacons 1.608∗∗∗ 1.600∗∗∗
(859.54) (855.23)N 142881 142881 142881 142881
t statistics in parentheses∗ p < 0.05, ∗∗ p < 0.01, ∗∗∗ p < 0.001
46
Table 18: The influence of working hours on unemployment for all labor market par-ticipants
Unemployment (1) (2) (3) (4) (5) (6) (7) (8)all class class=1 class=2 class=3 class=4 class=5 class=6 class=7
annual working hours -0.0818∗∗∗ -0.0785∗∗∗ -0.119∗∗∗ -0.114∗∗∗ -0.101∗∗∗ -0.0771∗∗ -0.0735 -0.119(-47.58) (-20.43) (-38.02) (-31.09) (-13.12) (-2.69) (-1.74) (-0.30)
age -0.414∗∗∗ -0.488∗∗ -0.794∗∗∗ -0.536∗∗∗ -0.357 -1.916 0.759 -19.43∗
(-4.97) (-2.99) (-5.36) (-3.62) (-1.27) (-1.00) (0.25) (-2.80)
education 0.813∗∗∗ 1.358∗∗∗ 0.188 -1.093∗∗ -7.233∗∗∗ -22.44∗∗∗ -4.067 22.71(5.11) (4.42) (0.78) (-3.20) (-7.02) (-4.41) (-0.42) (0.76)
type of income -13.82∗∗∗ -9.453 1.500 -4.106 -13.10∗ -15.86 -32.38 323.3(-7.34) (-1.52) (0.43) (-1.54) (-2.42) (-0.55) (-0.72) (1.83)
constant term 263.3∗∗∗ 271.3∗∗∗ 342.4∗∗∗ 332.0∗∗∗ 393.9∗∗∗ 655.6∗∗∗ 287.5 193.9(62.48) (28.63) (44.07) (34.27) (17.43) (6.01) (1.75) (0.49)
N 63500 13516 22320 16996 4737 647 101 14
t statistics in parentheses∗ p < 0.05, ∗∗ p < 0.01, ∗∗∗ p < 0.001
Table 19: The influence of working hours on unemployment for the labor market par-ticipants who experience unemployment during one year
Unemployment (1) (2) (3) (4) (5) (6) (7)all class class=1 class=2 class=3 class=4 class=5 class=6
annual working hours -0.438∗∗∗ -0.437∗∗∗ -0.421∗∗∗ -0.428∗∗∗ -0.506∗∗∗ -0.569∗ -1.219(-52.27) (-34.45) (-35.46) (-20.98) (-8.52) (-2.09) (-1.17)
age 0.235 -0.673 -0.225 0.806 8.750∗∗ 10.58 6.629(0.74) (-1.61) (-0.32) (1.44) (2.75) (0.70) (0.40)
education -3.850∗∗∗ -2.026∗ -2.779∗∗∗ -6.263∗∗∗ -48.65∗∗∗ -198.0∗∗∗ 17.48(-6.63) (-2.37) (-3.60) (-4.23) (-5.04) (-4.44) (0.11)
type of income -11.84 37.08 4.822 -28.61 -22.03 -69.83 -48.39(-1.39) (1.83) (0.36) (-1.87) (-0.56) (-0.31) (-0.22)
constant term 1258.3∗∗∗ 1237.5∗∗∗ 1207.9∗∗∗ 1251.5∗∗∗ 1563.1∗∗∗ 3547.4∗∗∗ 1496.5(66.98) (40.83) (39.78) (27.71) (8.73) (4.83) (0.91)
N 10825 3023 4626 2539 540 63 9
t statistics in parentheses∗ p < 0.05, ∗∗ p < 0.01, ∗∗∗ p < 0.001
47
Table 20: The influence of working hours on unemployment the year after for all labormarket participants
Unemployment (1) (2) (3) (4) (5) (6) (7)in the next year all class class=1 class=2 class=3 class=4 class=5 class=6
unemployment 0.146∗∗∗ 0.174∗∗∗ 0.138∗∗∗ 0.139∗∗∗ 0.0956∗∗∗ 0.0333∗ 0.0130(35.42) (16.58) (17.85) (17.78) (10.15) (2.43) (0.19)
annual working hours -0.0193∗∗∗ 0.000433 -0.0309∗∗∗ -0.0460∗∗∗ -0.0384∗∗∗ -0.0260∗ -0.0484(-10.32) (0.09) (-8.08) (-11.76) (-7.38) (-2.58) (-1.68)
age 0.00442 -0.504∗ 1.243∗∗∗ -0.747∗∗∗ -0.231 -1.725∗ 0.865(0.05) (-2.39) (7.26) (-4.96) (-1.27) (-2.58) (0.43)
education 0.940∗∗∗ 0.764 1.014∗∗∗ 0.229 -1.949∗∗ -1.360 1.009(5.37) (1.81) (3.47) (0.66) (-2.82) (-0.76) (0.16)
type of income -20.36∗∗∗ -24.59∗∗ -21.99∗∗∗ -7.159∗ 0.856 21.53∗ -8.082(-10.06) (-3.04) (-4.93) (-2.52) (0.24) (2.13) (-0.26)
constant term 127.5∗∗∗ 140.5∗∗∗ 123.3∗∗∗ 183.0∗∗∗ 142.3∗∗∗ 133.9∗∗∗ 75.55(27.78) (11.55) (12.98) (17.84) (9.30) (3.43) (0.67)
N 53605 9701 18907 15399 4518 625 99
t statistics in parentheses∗ p < 0.05, ∗∗ p < 0.01, ∗∗∗ p < 0.001
Table 21: The influence of working hours on unemployment the year after for the labormarket participants who experience unemployment during one year
Unemployment (1) (2) (3) (4) (5) (6) (7)in the next year all class class=1 class=2 class=3 class=4 class=5 class=6
unemployment 0.0302∗∗∗ 0.0566∗∗ 0.0318∗ 0.0265 0.00560 0.000836 0.0909(3.81) (2.80) (2.44) (1.79) (0.31) (0.02) (0.48)
annual working hours -0.0589∗∗∗ -0.0402∗ -0.0388∗∗ -0.107∗∗∗ -0.108∗∗∗ 0.0446 0.345(-7.27) (-2.25) (-3.18) (-6.29) (-3.90) (0.53) (0.75)
age -0.460 -0.483 -0.487 -0.456 1.002 -1.414 3.654(-1.75) (-1.09) (-0.76) (-1.09) (0.72) (-0.30) (0.57)
education -0.417 -1.384 0.221 -0.568 -5.981 3.159 0.0752(-0.80) (-1.20) (0.31) (-0.52) (-1.41) (0.20) (0.00)
type of income 3.762 8.950 -1.461 0.710 33.75∗ 129.8 78.47(0.50) (0.36) (-0.11) (0.06) (1.97) (1.94) (0.95)
constant term 331.5∗∗∗ 308.9∗∗∗ 299.7∗∗∗ 412.1∗∗∗ 345.4∗∗∗ -2.606 -517.9(17.40) (7.03) (9.35) (10.51) (4.22) (-0.01) (-0.75)
N 9092 2137 4036 2308 519 61 9
t statistics in parentheses∗ p < 0.05, ∗∗ p < 0.01, ∗∗∗ p < 0.001
48
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