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Pacific-Basin Finance Journal Manuscript Draft Manuscript Number: PBFJ-D-12-00036 Title: The Restudy of the Relationship between Market Orders and Stock Returns in Taiwan Article Type: Research Paper Keywords: Reference point; Order imbalance; Panel model. Abstract: Unlike previous studies that adopted "price" as the reference point, this paper employs the adjusted order imbalance related to "volume" as a reference point to examine the relationship between a firm's characteristics and stock returns. Adjusted order imbalance, including trading direction of stock index and trading volume of individual stock and stock index, is freely and easily obtained by investors in Taiwan. Employing the panel regression model, this paper found prior adjusted order imbalance has a significantly positive relationship with individual stock returns. Additionally, empirical results show that adjusted order imbalance enhances the impacts of value and size effect.
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The Restudy of the Relationship between Market Orders and
Stock Returns in Taiwan
Highlights
>>We found the positive impacts of adjusted order imbalance.
>>We examine the effect of reference points related to "volume" to stock returns.
>>We collected numerous observations (number of data is 1,434,768) in the panel
model.
>> The adjusted order imbalance could enhance the value and size effects.
*highlights
i
The Restudy of the Relationship between Market Orders and
Stock Returns in Taiwan
Abstract: Unlike previous studies that adopted "price" as the reference point, this paper
employs the adjusted order imbalance related to “volume” as a reference point to
examine the relationship between a firm’s characteristics and stock returns. Adjusted
order imbalance, including trading direction of stock index and trading volume of
individual stock and stock index, is freely and easily obtained by investors in Taiwan.
Employing the panel regression model, this paper found prior adjusted order imbalance
has a significantly positive relationship with individual stock returns. Additionally,
empirical results show that adjusted order imbalance enhances the impacts of value and
size effect.
Keywords: Reference point; Order imbalance; Panel model.
*Manuscript, excluding Author DetailsClick here to view linked References
1
1. Introduction
Following the 1980s, many researchers found that asset prices often violate the
theoretical expectative prices and were referred to as financial puzzles. Alpert and
Raiffa (1982) pointed out that there are two reasons for violating the market
effectiveness. One is that asymmetric information exists for investors and investors
catch the different quantitative quality of information at different times. The other is that
cognition and awareness are different for investors even given the same information.
Figlewski (1982) mentioned that investors have different information perspectives of
the public information. The investors’ divergence of views of the same information
reflects the fact that the investors’ behaviors contribute to explaining the security price.
Kahneman (1992) supported the viewpoint that the investors participate in
anchoring-and-adjustment of their views as investing. That is, the investors would
choose specific information as a reference when they make investment decisions. The
specific information is like the anchors of a boat that keep it located at a fixed position
rather than drifting out to sea somewhere. Previous research has looked at the
“anchoring effect” (Slovic and Lichtenstein, 1971; Tversky and Kahneman, 1974). The
famous expectative theory also applies the concepts of reference point to explain the
nonlinear utility function (Kahneman and Tversky, 1979; Tversky and Kahneman,
1992). The expectative theory argues that the investors judge their gains or losses
depending on some reference points or relative value rather than an objective or
absolute value.
However, what are the reference points for investors? Past studies supported that
the price variables could be a reference point, such as the purchase cost (Shefrin and
Statman, 1985), and the history price of individual stock, like a recent 52-week high.
2
George and Hwang (2004) supported that the recent 52 week-high could be a reference
point for investors and the zero-costing strategy based on the 52 week-high can create
more positive profits than momentum strategy. Chang (2011) documented the positive
connection between the 5-day high, 20-day high, 60-day high, and 52-week high of a
stock price and its returns.
In addition to the price variables being used as a reference point, investors often
adopt the relevant volume variables as reference points in intuition when they make
investment decisions. Nevertheless, there is a paucity of literature on this subject. In
this paper, we try to choose the “order imbalance” that is one of relevant volume
variables as a reference point to determine their impact on individual stocks. In Taiwan,
both the Taiwan Stock Exchange (TSE) and news services report daily buying and
selling orders of the stock index. The TSE releases the data of accumulated buying or
selling orders of the TAIEX (Taiwan Stock Exchange Capitalization Weighted Stock
Index) everyday. The data is free and easy to obtain from the TSE's website or other
media, such as TV or newspapers. 1
Therefore, market investors can get information
on the order imbalance, which means buying orders greatly outnumber selling orders
on the Taiwan stock index. A reasonable expectation is that the stock prices the next
day reflect the news of order imbalance. The convenience of getting the information
pertaining to order imbalance may lead investors to follow the market orders that could
represent the sentiments of investors. Therefore, order imbalance of the TAIEX should
affect individual stocks the next day.
1The information of orders or order imbalance of “individual” stocks is not easy to obtain for common
investors because the free data only reveals unfilled or unsatisfied orders for the “best five” ticks, not
accumulation of all the orders of individual stocks. Therefore, the order imbalance of individual stocks is
inconvenient to obtain and cannot be used as a reference point for investors.
3
It is worth noticing that we need not identify seller-initiated or buyer-initiated
trades using Lee and Ready’s (1991) approach or other similar approaches. The
seller-initiated or buyer-initiated trades are ex-post, while the buyer or seller orders are
ex-ante, to represent the respective needs of investors. The order imbalance this paper
adopted is the ex-ante concept to show the power of buying or selling.
The trading volume is abandoned for use as a reference point because the order
imbalance offers more useful information for investors. The trading volume does not
include the directions of trades. That means the powers of buying or selling is only
aware of the order imbalance, not trading volume. The power of buying or selling
could reflect the willingness of investors to trade at some point. This is important for
common investors to observe the sentiments of other investors in this market. The
order imbalance provides an indication of the stocks’ potential movement in terms of
being in a positive or negative direction. When a positive order imbalance occurs,
investors will believe that the sentiment of the market is high, optimistic, or brilliant in
the future. In contrast, in the case of a negative order imbalance, investors will believe
that the sentiments of other investors are pessimistic, conservative, or dark. When the
order imbalance is positive (negative), traders adjust their expectations regarding stock
returns in the future, then push the price upwards (downwards).
There is another explanation for the importance of order imbalance -
attention-grabbing news. The “glitter stocks” means the stocks that exist in the news or
information avenues that grab the attention of investors. Odean (1999) argued that
investors choose those glitter stocks to trade. Barber and Odean (2008) pointed out that
the stocks reflecting news such as abnormal trading volume or extremely high or low
daily returns, grabs the attentions of investors and, thereby, are purchased. The research
4
called this behavior of buying stocks with attention-grabbing news “attention-driven
buying”. Previous literature focused on the characteristics of individual stocks that grab
investors’ attention, and the common news of the stock index was ignored by scholars.
However, the latter contributes more toward investing adjustments because the single
measure makes the decision making process simpler for varied stocks, and it is easy to
understand and adopt these investing indexed financial assets. Considering large trading
volume of individual stock grabs investors’ attention and the order imbalance of the
TAIEX motivates investors’ sentiments, this paper investigates the impact of interaction
term and trading volume of a firm and the order imbalance of the TAIEX.
Employing the panel regression model, which could both consider the time series
and cross-section data, this paper finds that the order imbalance of stock index has
positive effects on individual stocks in Taiwan. The important control variables,
including the PE ratio, firm size, and book-to-market ratio, have been considered in the
models. This finding could be explained by the investors’ sentiments. When the buying
orders outnumber the selling orders, the investors prefer to hold positive positions or to
buy stocks. By contrast, when the selling orders outnumber the buying stocks, the
investors prefer to hold negative positions or to sell stocks.
2. Brief Literature Review and Hypotheses
2.1 The relationship between order imbalance and stock returns
The orders of investors seem to have content full of significant information. For
example, Subrahmanyam (2009) agreed that the order flows have profound implications
for all of the finance areas. Fan, Hu, and Jiang (2012) documented the negative price
impact after block trades in China. A substantial body of research has documented the
5
positive relationship between the order imbalance and stock returns. Chan and Fong
(2000) pointed out that order imbalance could explain the greatest movement of stock
prices because the volatility-volume relationship becomes much weaker after
controlling for the impact of order imbalance on the NYSE and NASDAQ. Chordia,
Roll, and Subrahmanyam (2002) pointed out the significant relationship between the
daily order imbalances and contemporaneous market returns in the S&P 500 index.
They argued that the order imbalances are significantly associated with daily changes in
liquidity after controlling for volume, as well as using the excess buying or selling
trades as another determinant of the market price movements. Madhavan and Smidt
(1993), Huang and Stoll (1994), Chordia and Subrahmanyam (2004), and Chordia, Roll,
and Subrahmanyam (2008) also found the positive connection between order imbalance
and stock returns.
For special events, such as the financial crisis on October 19, 1987, Blume,
MacKinlay, and Terker (1989) found a strong relationship existed between order
imbalance and stocks on the New York Stock Exchange (NYSE). The positive impact of
order imbalance to stock returns has been confirmed in different countries. Brown,
Walsh, and Yuen (1997) supported the connection in the Australian stock market. Liu
(1997) and Lee et al. (2004) demonstrated that order imbalances play an influential role
in the Taiwan stock market. Bailey et al. (2009) documented the strong positive
relationship between daily order imbalances and contemporaneous individual stock
returns in China.
As this review shows, there has been extensive research on the relationship
between order imbalance of individual stock and its returns. This study would like to
confirm the adjusted order imbalance in Taiwan because the order of the TAIEX is
6
easily available for investors. Investors tend to take a familiar target as a reference point
to judge the value (Slovic and Lichtenstein, 1971). Tversky and Kahneman (1974)
called it the “anchoring effect.” Purchase cost had been supported to be a good
reference point (Shefrin and Statman, 1985) and the recent 52 week-high of individual
stocks (George and Hwang, 2004) and stock index (Chang, 2011) could also be
anchoring. Similarly, the past price variables could also be a reference point, the volume
variables could too. Because the case investors use volume variables as a reference
point, this study adopted the adjusted order imbalance, which is defined as the relative
proportion of trading volume multiplied y the order imbalance of the Taiwanese stock
index. The factors of adjusted order imbalance are due to the easy availability of volume
variables. The trading volumes of individual stock, the overall trading volume, and the
order imbalance of the TAIEX can be surveyed via the web, newspaper, and TV every
day. We construct the hypothesis of relevant volume variable as a reference point. The
adjusted order imbalance considering the liquidity of individual stock, stock index, and
order imbalance of stock index has a positive impact on stock returns.
2.2 Size, Value, and P/E effects
This paper includes the most common firm characteristics that are important
factors in predicting stock returns mentioned in a number of studies: Firm size, book
to market ratio (B/M), and PE ratio.
The size effect means that small stocks earn higher returns than larger ones and
there is a negative relationship between firm size and stock returns. Some researchers
believe that size is a critical factor in determining the expectations for stock returns [e.g.,
Banz (1981), Reinganum (1981a), Jaffe et al. (1989), and Rouwenhorst (1998)]. The
7
value effect means that the stocks with low market value (high book-to-market ratio)
yield higher returns than those with high market value and there is a positive
relationship between book-to-market ratio and stock returns. Other studies agreed that
the value effect is indispensible and an important factor, [e.g., Bauman and Miller
(1997), Rosenberg et al. (1985), Chan et al. (1991), Capual et al. (1993), Fant and
Peterson (1995), Piotroski (2000), Chan and Lakonishok (2004)]. Pontiff and Shall
(1998) agreed that the B/M ratio has more predicting power than other variables, such
as interest rate spread and dividend yields. Huang (2011) documented that the strategies
based on value spread in B/M ratio earns significantly positive expected returns. Brown,
Rhee, and Zhang (2008) found the impact of value exists but differs across four Asian
stock markets.
Some empirical studies have argued that the size and value effects should not be
ignored in such an analysis [e.g., Fama and French (1992), Fama and French (1996),
Barber and Lyon (1997), Bauman et al. (1998), Piotroski, (2000), Daniel et al. (2001)].
Reinganum (1981b) argued that the value effect is related to the size effect because
value effect mitigates after controlling firm size; while Chan, Hamao, and Lakonishok
(1991) found the value effect included in their model weakened the size effect in the
Japanese stock market. The results of Loughran’s (1997) study found that the stocks that
are larger in size have a smaller impact of B/M on stock returns, while the stocks that
are smaller in size have a larger impact of B/M effect. De Groot and Verschoor (2002)
find a strong size effect in five Asian emerging markets and a significant value effect in
Korea, Malaysia, and Thailand.
The majority of research in firm characteristics has focused on the firm size and
B/M, the price-to-earnings (PE) ratio that represents the earnings yield effect, which is
8
also emphasized by previous studies. Basu’s (1983) research supported the view that the
PE effect is not independent of firm size. The investors overstate growth expectations
creating over-optimism (over-pessimism) for high (low) P/E stocks. Bleiberg (1989)
supported that the longer the observed sample period, the stronger the relationship
between high PE and S&P 500 stocks’ future returns. Basu (1977), Cook and Rozeff
(1984), Jaffe et al. (1989), Peavy and Goodman (1983), and Fairfield and Harris (2010)
all agreed that stocks with low PE ratios generate higher returns.
In relation to the opposite views on interactions between size and P/E effects, Cook
and Rozeff (1984) argued that the interaction does not exist and size and E/P are
independent effects, unlike what was claimed by Reiganum (1981a) and Basu (1983).
Jaffe et al. (1989) employed the Seemingly Unrelated Regression (SUR) model to
compare the significance of the coefficients of E/P and size in different observation
periods. Their results were consistent with Cook and Rozeff (1984).
The style investing means that investors prefer small size, High B/M, and low P/E.
In this study, we allow the effects of adjusted order imbalance and the impact of the
main firm characteristics such as size, B/M, and P/E. We constructed the enhanced style
effect because the large trading volume grabs investor attention (Barber and Odean
(2008), as does adjusted order imbalance. When investors notice some glittering stocks
they then choose those stocks with their favorite firm characteristics. Therefore, the
hypothesis of enhanced style effect should be supported; the interaction terms of
adjusted order imbalance and firm characteristics are significant and have the same
signs as firm characteristics.
3. Data and Methodology
9
3.1 Data
Investors in Taiwan can get information pertaining to order imbalance of the
Taiwan stock index easily and they may adopt the order imbalance into their
information set to make investment decisions. Therefore, this paper adopts the daily
data of order imbalance of the Taiwanese stock index to find its impact on the next day’s
individual returns. Our sample data is comprised of the daily data of stocks traded on
the Taiwanese stock market. The sample period was from January 1, 1998 to December
31, 2007, totaling 2541 days. The data was collected from the Taiwan Economic Journal
Data Bank. Given that the number of stocks did not stay the same at every sample point
because the number of stocks increased due to initial public offerings and decreased due
to delisting, the panel data is unbalanced. Thus, the total number of firms is up to 704
and the number of data is 1,434,768.
3.2 Measures of Variables
The variables used in the regression model and their definitions are described as
follows.
(1) Stock Returns (RET)
tiRET , =( tiP , - 1, tiP )/ 1, tiP ×100% (1)
where tiP , is the stock closed price of firm i at day t, while 1, tiP is the corresponding
price of firm i at day t-1. tiRET , denotes the stock i returns at time t. The stock returns
are adjusted when the dividend is distributed.
(2) Adjusted Order Imbalance (AOI)
First, we calculated the order imbalance tTWOI , , which is defined as the order
10
imbalance of Taiwanese stock index at day t:
tTWtTWtTw NSNBOI ,,,
(2)
The variables NBTW,t and NSTW,t, denote the buy and sell orders on the Taiwan
stock index at day t, respectively.
Second, considering the difference of trading size and liquidity of individual
stocks i, we adjusted the information for order imbalance of the Taiwan stock index. We
calculated the adjusted order imbalance of firm i tiAOI , , which is defined as the
proportion of the tTWOI , .
tTW
ti
tTWtiVOL
VOLOIAOI
,
,
,,
(3)
The variables VOLi,t, is the trading volume of firm i at day t, and VOLTW,t is the
trading volume.
(3) Price-to-earnings ratio (PE)
tiPE , = tiP , / tiEPS , (4)
where tiEPS , , is yearly earnings divided by outstanding shares of firm i in the latest
season on day t under the assumption that the expected per-share earnings in the coming
year will be the same as the earnings per-share of the last season. Again, tiP , is the
closing stock price for firm i at day t.
(4) Book to market ratio (BM)
tiBM , = tiValueBook , / )( ,, titi SharesP (5)
11
where tiShares , is the outstanding shares of firm i at day t, tiValueBook ,
represents
the book value of equity.
(5) Firm size (SIZE)
tiSIZE , = titi SharesP ,, (6)
3.3 Methodology
We propose the following equations to examine the impact of order imbalance of
the stock index on individual stock returns.
Model 1:
tititititititi AOISIZEBMPERET ,1,41,31,21,1,, (7)
where tiRET , is the stock returns of firm i at day t , ),,3,2,1( Jjj
1, tiPE , 1, tiBM , 1, tiSIZE , and 1, tiAOI are the price to earning ratio, book-to-market
ratio, the market value, and adjusted order imbalance of firm i on day t-1, respectively.
ti , is the coefficient to estimate,
and ti ,
is the error term.
Model 2:
tititititititi DUMSIZEBMPERET ,1,41,31,21,1,, (8)
where tiDUM , is the dummy variable, which takes on the value 1 if the sign of
adjusted order imbalance is positive, and the value is zero if the sign is negative. If the
coefficient of tiDUM , is not significantly zero, the intercept term equals 4, ti ,
while, if the coefficient of tiDUM , is significant, the intercept term still equals to
ti , .
Model 1 and 2 could test the hypothesis of relevant volume as a reference point.
12
Model 3:
1,1,41,31,21,1,, tititititititi PEDUMSIZEBMPERET
titititititi DUMSIZEDUMBMDUM ,1,71,1,61,1,5 (9)
where the interaction terms of dummy variable products on the other independent
variables allow us to observe the impacts of adjusted order imbalance to firm
characteristics. Hence, with a significant coefficients of interaction terms, the total
impacts for 1, tiPE are 41 , for 1, tiBM
are 52 , and for 1, tiSIZE are
63 ,
respectively. Model 3 could test the hypothesis of enhanced style effect, if the
interaction term is not zero.
This study employs the panel regression analyses, rather than the ordinary least
squares (OLS) model. Kalton, Kasprzyk, and McMillen (1989) argued that the OLS
model may have biased coefficients that make empirical results different between the
whole sample and the individual sample. The panel regression model could include the
time series and cross-section data, and more information from the sample could be
shown in the model than those in the OLS model.
ti
K
k
tkiktiti XY ,
1
1,,,
(10)
where, Ni ,,2,1 , representing the firm i at the day t, and Tt ,,2,1 ,
representing each day during the sample period. tiY , represents the dependent
variable of firm i at the same day t while 1, tkiX represents the k independent variable
of firm i at day t-1. ti , is the residual error and 0)( itE , 2)( itVar for
ji or 0, jitE for t . k for Kk ,,2,1 represents the coefficients of
each dependent variable k. ti , for Ni ,,2,1 represents the intercept term of firm i
13
at day t.
The three different sub-models are dependent on the intercept term ti , :
(1) OLS model: The model is under the assumption that every sample has the same
intercept term. That is ti, .
(2) Fixed Effects model: The model is under the assumption that firm i has a different
intercept term but the same intercept term for each day t. That is iti , .
(3) Random Effects model: The model is most relaxed for the assumption that firm i
has the different intercept term on day t. That is iti , , where λ represents the
random term and i represents the error of the random term.
Before estimating the models, we chose the model by using the F-test to compare
the explanation powers of the fixed model and OLS model, and employing the
Lagrange Multiplier (LM) test supported by Breusch and Pagan (1980) to compare the
Random Effects model and OLS model. The F-test is as follows:
),1(~
)(
)1(
)1(
)(
2
22
knnTnF
knnT
R
n
RR
Ffix
olsfix
(11)
where 2R is the coefficient of determination,
2
fixR is the coefficient of determination
under the Fixed Effects model, while 2
olsR is the coefficient of determination under the
OLS model. If we do not reject the hypothesis 0H , the OLS model is better.
The LM test is as follows:
14
)1(~1
12
2
2
1 1
2
1
2
1
n
i
T
t
it
n
i
T
t
it
e
e
T
nTLM (12)
where e is the error term under the OLS model. If we do not reject the hypothesis 0H ,
the OLS model is better. Otherwise, the Random Effects model is more adequate than
the OLS model.
Finally, to compare the Fixed and Random models the Hausman Test, supported by
Hausman (1978), helped us determine which model is better:
)(~ˆˆˆˆ 21kH randomfixrandomfixrandomfix
(13)
where, fix is the vector of estimated coefficients under the Fixed Effects model,
random is the vector of estimated coefficients under the random effects model, fix is
variance-covariance matrix under the Fixed Effects model, and random fix is
variance-covariance matrix under the Random Effects model. If we do not reject
hypothesis 0H , the Random Effects model is better. Otherwise, the Fixed Effects model
is more adequate than the Random Effects model.
4. Empirical Findings
Table 1 summarizes the descriptive statistics of the variables used in the
regression models. The average daily returns across individual stocks was 0.042%. The
adjusted order imbalance, on average, was negative.
15
[Insert Table 1 about here]
To investigate the relationship between stock returns and the adjusted order
imbalance, we implemented the panel model with control variables including PE, firm
size, and book-to-market ratio. Table 2 reports the F-test, LM test, and Hausman test,
which can help us choose the type of panel model.
[Insert Table 2 about here]
For Model 1, the statistic of F-test answers which is more adequate for the OLS
model or Fixed Effects model. The F statistic was 1.4022 and rejected the hypothesis.
The Fixed Effects model is adequate for Model 1. The LM statistic was 68.8281 and
rejected the hypothesis, which means the Random Effects model is more adequate than
the OLS model. However, the Hausman test conducts that the statistic, 590.1289,
rejected the null hypothesis and suggests that the results of the Fixed Effects model
should be statistically preferred over the results from the Random Effects model. Finally,
the Fixed Effects model was most adequate for Model 1. The comparisons of the OLS,
Fixed Effects model, and Random Effects model for Model 2 and Model 3 are similar to
Model 1. The Fixed Effects model is supported as the most adequate for Model 2 and
Model 3. We then adopted the Fixed Effects model to estimate in Tables 3, 4, and 5.
[Insert Table 3 about here]
Employing the Fixed model, the coefficients in Table 3 reveal that the adjusted
16
order imbalance of the Taiwan stock index has a positive impact (2.219) on individual
stock returns at a 1% significance level in Model 1. The results agree with the
hypothesis of relevant volume variables as a reference point. The information related to
the adjusted order imbalance is easily available via the TSE web, newspaper, or news
media. We found that the impact of the PE effect, value effect, and size effect on stock
returns exists. For comparison, the base model without AOI variable is shown in Table 3.
Both the base model and model 1 agree that the expectative signs of coefficients of PE,
BM, and SIZE are supported.
For both the firm size and PE ratio, we found significant negative impacts on stock
returns and the BM were found to have a positive impact on stock returns. The last
bottom row in Table 3 is the F-test to find whether the AOI variable adds significant
explanatory power to the base model. The F-test was used for the comparison of nested
models, which are the two sets of estimates in Model 1. The first set of regression
models includes the firms’ characteristics variables and the AOI variable, while the
second set of results comes from a restricted model in which the AOI variable is omitted.
The F-test for the coefficient of AOI variable is based on a simple comparison of the
residual sum of square from this restricted regression and the residual sum of squares
from the unrestricted model. The F-test was 6.72 and its p-value was less than 1%, this
means that the increase in explanatory power of the full model versus the model only,
including variables of firms’ characteristics and intercept term, is significant.
[Insert Table 4 about here]
Table 4 shows the estimates from Model 2 in which the dummy variable,
17
depending on the signs of adjusted order imbalance of the Taiwan stock index, was
added. We used a dummy variable to capture these effects, which are possibly different
between positive and negative adjusted order imbalance. The coefficient for the dummy
variable represents the change in the intercept for the positive adjusted order imbalance.
The intercept term represents the impact of the omitted variable, which is a set of other
factors possibly affecting the individual stock returns but not included in the regression
model. The coefficient of dummy variable is significantly positive. The higher the
adjusted order imbalance, the higher the individual stock returns. Again, the signs of
characteristic variables are the same as those in Table 3.
[Insert Table 5 about here]
Because the signs of adjusted order imbalance of stock index may have differing
responses to other independent variables, the interaction terms are shown in Table 5.
The coefficients of interaction terms can help us to understand how the firm’s
characteristics, including PE, BM, and SIZE, affect the individual stock returns under
the conditions of either positive or negative adjusted order imbalance. Including the
cross term of DUMt-1×PE t-1, DUM t-1×BM t-1, and DUM t-1×SIZE t-1, we found the
interaction terms remain the same signs of the characteristics term: PE t-1, BM t-1, and
SIZE t-1, respectively. For example, the coefficient of SIZE t-1 was -0.446 and the
coefficient of interaction term DUM t-1×SIZE t-1 was also negative, -0.631. Similarly, the
coefficients of PE ratio and interaction term of market order imbalance and PE ratio are
negatively significant. The coefficients of B/M ratio and the interaction of market order
imbalance and B/M ratio are positively significant. Therefore, the hypothesis of enhance
18
style effect is supported and the individual firms’ characteristics and the information set
of adjusted order imbalance interact with each other, and the relationships between the
characteristics and stock returns is stronger for positive adjusted order imbalance. This
suggests that ignoring the adjusted order imbalance leads to an under-estimation of the
impact of the firms’ characteristics variables.
5. Conclusion
The order imbalance represents the excess demand and the common sentiments of
investors. The information of adjusted order imbalance, which is easily available in
Taiwan, is an important reference for investors. However, previous literature focused on
the order imbalance of individual stocks, which may not easily be available for
investors and the order imbalance of stock index was omitted. In Taiwan, the
information of order imbalance of stock index is easily available for investors from the
TSE website or news media but not of order imbalance of an individual stock. We
employed the adjusted order imbalance that considers the liquidity of individual stock
and stock index and order imbalance of stock index, and confirmed the positive
relationship between the order imbalance of stock index and the individual stock
returns.
Besides agreeing to the positive connection between the adjusted order imbalance
and the individual stock returns, the empirical results suggest the interaction of the
adjusted order imbalance and characteristics variables. First, the size effect, value effect,
and PE effect are supported in this paper. There is a positive relationship between the
stock returns and BM, while there are negative relationships between the stock returns
and firm size or PE. We then found that the coefficients of interaction term of
19
characteristics variables and the adjusted order imbalance keep the same signs of the
coefficients of characteristics variables. The relationship between individual stock
returns and a firm’s characteristics, including firm size, BM, and PE, is enhanced for the
positive adjusted order imbalance. Therefore, ignoring the adjusted order imbalance
may lead to an under-estimation of the impact of firms’ characteristics variables.
20
Table 1 Descriptive Statistics
This table reports the descriptive statistics for listed stocks in Taiwan. The sample covers daily
observations for the 1998/1/1-2007/12/31 period, totaling 2541 days. RET is stock returns, AOI is the
adjusted order imbalance, PE is price to earnings ratio, BM is book-to-market ratio, and SIZE is the
market value. Given that the number of stocks did not stay the same at every sample point, as the number
of stocks increased due to initial public offerings and decreased due to delisting, the panel data is
unbalanced. Thus, the total number of firms is up to 704.
Average Medium Std. Dev. Number of
Observation
RET 0.0420 0.0000 2.8656 1434768
AOI -0.2808 -0.0282 28.08 1434768
PE 23.4564 12.8200 76.9659 1429524
BM 0.9473 0.7576 0.8460 1434768
SIZE 20631.26 4497 76733.99 1434768
21
Table 2 The Tests for Adequate Models
This table reports the statistics of F-test, LM test, and Hausman test. The sample covers daily
observations for the 1998/1/1-2007/12/31 period, totaling 2541 days. Given that the number of stocks did
not stay the same at every sample point, as the number of stocks increased due to initial public offerings
and decreased due to delisting, the panel data is unbalanced. Thus, the total number of firms is up to 704.
The three models are as follows:
Model 1: tititititititi AOISIZEBMPERET ,1,41,31,21,1,,
Model 2: tititititititi DUMSIZEBMPERET ,1,41,31,21,1,,
Model 3: 1,1,41,31,21,1,, tititititititi PEDUMSIZEBMPERET
titititititi DUMSIZEDUMBMDUM ,1,71,1,61,1,5
where RET is stock returns, AOI is the adjusted order imbalance, PE is price to earnings ratio, BM is
book-to-market ratio, SIZE is the market value, and DUM is the dummy variable, which take value 1 for
the positive AOI and 0 for negative AOI.
F-test
LM test
Hausman test
Models
0H :OLS is more adequate
1H :Fixed effect model is
more adequate
0H :OLS is more adequate
1H :Random effect model
is more adequate
0H :Random effect model
is more adequate
1H :Fixed effect model is
more adequate
Model 1 F=1.4022***
( P<0.0001 )
LM=68.8281***
( P<0.0001)
Hausman statistic=
590.1289***
( P<0.0001 )
Reject H0 Reject H0 Reject H0
The adequate model: Fixed effect model
Model 2 F=1.3233***
( P<0.0001 )
LM=29.3697***
( P<0.0001)
H=536.9451***
( P<0.0001 )
Reject H0 Reject H0 Reject H0
The adequate model: Fixed effect model
Model 3 F=1.2619***
( P<0.0001 )
LM=52.2358***
( P<0.0001)
H=508.5189***
( P<0.0001 )
Reject H0 Reject H0 Reject H0
The adequate model: Fixed effect model
Note: The notation *** represents that the value is significant at 1%.
22
Table 3 Empirical Results of Panel Regression Model
This table reports regression results. The sample covers daily observations for the 1998/1/1-2007/12/31
period, totaling 2541 days. Given that the number of stocks did not stay the same at every sample point,
as the number of stocks increased due to initial public offerings and decreased due to delisting, the panel
data is unbalanced. Thus, the total number of firms is up to 704. The model is as follows:
Base Model: titititititi SIZEBMPERET ,1,31,21,1,,
Model 1: tititititititi AOISIZEBMPERET ,1,41,31,21,1,,
where RET is stock returns, AOI is the adjusted order imbalance, PE is price to earnings ratio, BM is
book-to-market ratio, and SIZE is the market value.
Model 1 (Unrestricted) Base Model (Restricted)
Independent
variables
coefficient
(t statistic) p-value
coefficient
(t statistic) p-value
intercept -0.0198*** <0.0001 -0.0208***
<0.0001
(-4.2783) (-4.4996)
PEt-1 -55.7942a* 0.0799 -56.6
a*
0.0752
(-1.7514) (-1.7795)
BM t-1 0.0791*** <0.0001 0.0794***
<0.0001
(22.2819) (22.3768)
SIZE t-1 -0.6683a*** <0.0001 -0.6641a***
<0.0001
(-8.2950) (-8.2487)
AOI t-1 2.2187a*** 0.0095
(2.5929)
F(1,1428113)=6.7231***
Note: The notation *, *** represents that the value is significant at 10%, and 1%, respectively. The
superscript “a” represents to multiply 10-6
.
23
Table 4 Empirical Results of Panel Regression Model
This table reports regression results. The sample covers daily observations for the 1998/1/1-2007/12/31
period, totaling 2541 days. Given that the number of stocks did not stay the same at every sample point,
as the number of stocks increased due to initial public offerings and decreased due to delisting, the panel
data is unbalanced. Thus, the total number of firms is up to 704. The model is as follows:
Model 2: tititititititi DUMSIZEBMPERET ,1,41,31,21,1,,
where RET is stock returns, PE is price to earnings ratio, BM is book-to-market ratio, SIZE is the market
value, and DUM is the dummy variable, which takes value 1 for the positive adjusted order imbalance
and 0 for the negative adjusted order imbalance.
Independent
variables coefficient (t statistic) p-value
intercept -0.0857*** (-17.7474) <0.0001
PE t-1 -54.4727a* (-1.7123) 0.0868
BM t-1 0.0704*** (19.8163) <0.0001
SIZE t-1 -0.7183a*** (-8.9311) <0.0001
DUM t-1 0.2362*** (46.3441) <0.0001
Note: The notation *, *** represents that the value is significant at 10%, and 1%, respectively.
The superscript “a” represents to multiply 10-6
.
24
Table 5 Empirical Results of Panel Regression Model
This table reports regression results. The sample covers daily observations for the 1998/1/1-2007/12/31
period, totaling 2541 days. Given that the number of stocks did not stay the same at every sample point,
as the number of stocks increased due to initial public offerings and decreased due to delisting, the panel
data is unbalanced. Thus, the total number of firms is up to 704. The model is as follows:
Model 3: 1,1,41,31,21,1,, tititititititi PEDUMSIZEBMPERET
titititititi DUMSIZEDUMBMDUM ,1,71,1,61,1,5
where RET is stock returns, PE is price to earnings ratio, BM is book-to-market ratio, SIZE is the market
value, and DUM is the dummy variable, which takes a value of 1 for the positive adjusted order
imbalance and 0 for negative adjusted order imbalance.
Independent
variables coefficient (t statistic) p-value
intercept -0.0443*** (-8.2938) <0.0001
PE t-1 -31.500a*** (-0.8320) 0.4054
BM t-1 0.0192***
(4.5687) <0.0001
SIZE t-1 -0.4460a*** (-5.2439) <0.0001
DUM t-1×PE t-1 -92.500a (-1.3933) 0.1635
DUM t-1×BM t-1 0.1329***
(22.7450) <0.0001
DUM t-1×SIZE t-1 -0.6310a*** (-9.6100) <0.0001
DUM t-1 0.1228***
(15.2283) <0.0001
Note: The notation *** represents that the value is significant at 1%. The superscript “a”
represents to multiply 10-6
.
25
References
[1] Alpert, M., & Raiffa, H. (1982). A progress report on the training of probability
assessors, judgment under uncertainty: Heuristics and biases. Cambridge,
London: Cambridge University Press, 294-305.
[2] Banz, R. W. (1981). The Relationship between returns and market value of
common stock. Journal of Financial Economics, 9, 3-18.
[3] Barber, B. M., & Odean, T. (2008). All that glitter: The effect of attention and
news on the buying behavior of individual and institutional investors. Review of
Financial Studies, 21, 785-818.
[4] Barber, B. M., & Lyon, J. D. (1997). Detecting long-run abnormal stock returns:
The empirical power and specification of test statistics, Journal of Financial
Economics, 43, 341-372.
[5] Bailey, W., Can, J., Cheung, Y., & Wang, F. (2009). Stock returns, order
imbalances, and commonality: Evidence on individual and proprietary investors
in China. Journal of Banking and Finance, 33, 9-19.
[6] Basu, S. (1977). Investment performance of common stocks in relation to their
price-earnings ratios: A test of the efficient market hypothesis. Journal of
Finance, 32, 663-682.
[7] Basu, S. (1983). The relationship between earning’s yield, market value, and
returns for NYSE common stocks: Further evidence. Journal of Financial
Economics, 12, 129-156.
[8] Bauman, W. S., & Miller, R. E. (1997). Investor expectations and the performance
of value stocks versus growth stocks. Journal of Portfolio Management, 23, 56-78.
[9] Bauman, W. S, Conover, C. M., & Miller, R. E. (1998). Growth versus value and
large-cap versus small-cap stocks in international market. Financial Analysts
Journal, 53, 75-89.
[10] Bleiberg, S. (1989). How little we know. Journal of Portfolio Management, 15,
26-31.
[11] Blume, M., MacKinlay, A., & Terker, B. (1989). Order imbalances and stock price
movements on October 19 and 20, 1987. Journal of Finance, 44, 827-848.
[12] Breusch, T. S., & Pagan, A. R. (1980). The lagrange multiplier test and its
applications to model specification in econometrics. Review of Economic Studies,
47, 239-254.
[13] Brown, S., Rhee, S. G., & Zhang, L (2008). The return to value in Asian stock
markets. Emerging Markets Review, 9, 194-205.
26
[14] Brown, P., Walsh, D., & Yuen, A. (1997). The interaction between order imbalance
and stock price. Pacific-Basin Finance Journal, 5, 539-557.
[15] Capaul, C., Rowley, I., & Sharpe, W. (1993). International value and growth stock
returns. Financial Analysts Journal, 49, 27-36.
[16] Chan, K., & Fong, W. (2000). Trade size, order imbalance, and the
volatility-volume relation. Journal of Financial Economics, 57, 247-273.
[17] Chan, L., Hamao, Y., & Lakonishok, J. (1991). Fundamentals and stock returns in
Japan. Journal of Finance, 46, 1739-1789.
[18] Chang, C. Y. (2011). The relationship between the 52-week high of an individual
stock and stock market index level: Evidence from Taiwan. Journal of
International Financial Markets, Institutions & Money, 21, 14-27.
[19] Chordia, T., Roll, R., & Subrahmanyam, A. (2002). Order imbalances, liquidity,
and market returns. Journal of Financial Economics, 65, 111-130.
[20] Chordia, T., & Subrahmanyam, A. (2004). Order imbalance and individual stock
returns: Theory and evidence. Journal of Financial Economics, 72, 485-518.
[21] Chordia, T., Roll, R., & Subrahmanyam, A. (2008). Liquidity and market
efficiency. Journal of Financial Economics, 87, 249-268.
[22] Cook, T. J., & Rozeff, M. S. (1984). Size and earnings/price ratio anomalies:
One effect or two? Journal of Financial and Quantitative Analysis, 19, 449-466.
[23] Daniel, K., Titman, S., & Wei, K. C. J. (2001). Explaining the cross-section of
stock returns in Japan: Factors or Characteristics? Journal of Finance, 56,
743-766.
[24] De Groot, C. G. M., & Verschoor, W. F. C. (2002). Further evidence on Asian stock
returns behavior. Emerging Markets Review, 3, 179-193.
[25] Fairfield, P. M., & Harris, T. S. (2010). Price-earning and price-to-book anomalies:
Tests of an intrinsic value explanation. Contemporary Accounting Research, 9,
590–611.
[26] Fan, L., Hu, B., & Jiang, C. (2012). Pricing and information content of block trades
on the Shanghai Stock Exchange. Pacific-Basin Finance Journal, 20, 378-397.
[27] Fant, L. F., & Peterson, D. R. (1995). The effect of size, book-to-market equity,
prior returns and beta on stock returns: January versus the remainder of the year.
Journal of Finance Research, 18, 129-142.
27
[28] Fama, E. F., & French, K. R. (1992). The cross-section of expected stock returns.
Journal of Finance, 47, 427-465.
[29] Fama, E. F., & French, K. R. (1996). The CAPM is wanted, dead or alive. Journal
of Finance, 51, 1947-1958.
[30] Figlewski, S. (1982). Information diversity and market behavior. Journal of
Finance, 37, 87-102.
[31] George, T. J., & Hwang, C. Y. (2004). The 52-week high and momentum investing.
Journal of Finance, 59 (5), 2145-2176.
[32] Hausman, J. A. (1978). Specification tests in econometrics. Econometrica, 46,
1251-1271.
[33] Huang, R.D., & Stoll, H.R. (1994). Market microstructure and stock returns
prediction. Review of Financial Studies, 7, 179-213.
[34] Huang, I. H. (2011). The cyclical behavior of the risk of value strategy: Evidence
from Taiwan. Pacific-Basin Finance Journal, 19, 404-419.
[35] Jaffe, J., Keim, D. B., & Westerfield, R. (1989). Earning yields, market, values,
and stock returns. Journal of Finance, 44, 135-148.
[36] Kalton, G., Kasprzyk, D., & McMillen, D. B. (1989). Nonsampling errors in panel
surveys. New York, NY: John Wiley and Sons.
[37] Kahneman, D. (1992). Reference points, anchors, norms, and mixed feelings.
Organizational Behavior and Human Decision Processes, 51, 296-312.
[38] Kahneman, D., & Tversky, A. (1979). Prospect theory: An analysis of decision
under risk. Econometrica, 47, 263-291.
[39] Lee, Y. T., Liu, Y. J., Roll, R., & Subrahmanyam, A. (2004). Order imbalances and
market efficiency: Evidence from the Taiwan stock exchange. Journal of
Financial and Quantitative Analysis, 39, 327-341.
[40] Lee, C., & Ready, M. (1991). Inferring trading direction from intraday data.
Journal of Finance, 46, 733-746.
[41] Liu, Y. J. (1997). Periodic market closure and order imbalances. Global
Finance Journal, 8, 95-111.
[42] Loughran, T. (1997). Book-to-market across firm size, exchange, and seasonality:
Is there an effect? Journal of Financial and Quantitative Analysis, 32, 249-268.
28
[43] Madhavan, A., & Smidt, S. (1993). An analysis of daily changes in specialist
inventories and quotations. Journal of Finance, 48, 1595-1628.
[44] Odean, T. (1999). Do investors trade too much? American Economic Review, 89,
1279-1298.
[45] Peavy, J. W., & Goodman, D. A. (1983). The significance of price-earnings ratios
on portfolio returns. Journal of Portfolio Management, 9, 43-47.
[46] Piotroski, J. (2000). Value investing: The use of historical financial statement
information to separate winners from losers. Journal of Accounting Research, 38,
1-41.
[47] Pontiff, J., & Shall, L. D. (1998). Book-to-market ratios as predictors of market
returns. Journal of Financial Economics, 49, 141-160.
[48] Reinganum, M. R. (1981a). A misspecification of capital asset pricing: Empirical
anomalies based on earnings yields and market values. Journal of Financial
Economics, 9, 19-46.
[49] Reinganum, M. R. (1981b). Abnormal returns in a small firm portfolio. Financial
Analyst Journal, 31, 313-321.
[50] Rosenberg, B., Reid, K., & Lanstein, R. (1985). Persuasive evidence of market
inefficiency. Journal of Portfolio Management, 11, 9-16.
[51] Rouwenhorst, G. K. (1998). International momentum strategies, Journal of Finance
53, 267-284.
[52] Subrahmanyam, A. (2009). The implications of liquidity and order flows for
neoclassical finance. Pacific-Basin Finance Journal, 17, 527-532.
[53] Shefrin, H., & Statman, M. (1985). The disposition to sell winners too early and
ride losers too long: Theory and evidence. Journal of Finance, 40, 777-790.
[54] Slovic, P., & Lichtenstein, S. (1971). Comparison of baysian and regression
approaches to the study of information processing in judgments. Organizational
Behavior and Human Performance, 6, 649-744.
[55] Tversky, A., & Kahneman, D. (1974). Judgment under uncertainty: Heuristics
and biases. Science, 185, 1124-1131.
[56] Tversky, A., & Kahneman, D. (1992). Advances in prospect theory: Cumulative
representation of uncertainty. Journal of Risk and Uncertainty, 5, 297-323.