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Social Science & Medicine 56 (2003) 935–947
Health inequalities in the older population: the role of personalcapital, social resources and socio-economic circumstances
Emily Grundy*, Andy Sloggett
Centre for Population Studies, London School of Hygiene and Tropical Medicine, 49-51 Bedford Square, London WC1B 3DP, UK
Abstract
Older people now constitute the majority of those with health problems in developed countries so an understanding
of health variations in later life is increasingly important. In this paper, we use data from three rounds of the Health
Survey for England, a large nationally representative sample, to analyse variations in the health of adults aged 65–84 by
indicators of attributes acquired in childhood and young adulthood, termed personal capital; and by current social
resources and current socio-economic circumstances, while controlling for smoking behaviour and age. We used six
indicators of health status in the analysis, four based on self-reports and two based on nurse collected data, which we
hypothesised would identify different dimensions of health. Results showed that socio-economic indicators, particularly
receipt of income support (a marker of poverty) were most consistently associated with raised odds of poor health
outcomes. Associations between marital status and health were in some cases not in the expected direction. This may
reflect bias arising from exclusion of the institutional population (although among those under 85 the proportion in
institutions is very low) but merits further investigation, especially as the marital status composition of the older
population is changing.
Analysis of deviance showed that social resources (marital status and social support) had the greatest effect on the
indicator of psychological health (GHQ) and also contributed significantly to variation in self-rated health, but among
women not to variation in taking three or more medicines and among men not to self-reported long-standing illnesses.
Smoking, in contrast, was much more strongly associated with these indicators than with self-rated health. These results
are consistent with the view that self-rated health may provide a holistic indicator of health in the sense of well-being,
whereas measures such as taking prescribed medications may be more indicative of specific morbidities. The
results emphasise again the need to consider both socio-economic and socio-psychological influences on later life health.
r 2002 Elsevier Science Ltd. All rights reserved.
Keywords: Older people; Health status; Social support; Marital status; Inequalities in health
Introduction
The increased representation of older people in the
population of Britain and other developed countries,
coupled with epidemiological changes which mean that
older people constitute a large majority of those in poor
health, has led to a growing concern with identifying
determinants of health, and inequalities in health, in
later life (Acheson, 1998; Department of Health, 1999).
Variations in the mortality and morbidity of the elderly
population by indicators of socio-economic status based
on past occupation, education, housing tenure, income
and wealth have been reported in a wide range of studies
with those in the most socio-economically disadvan-
taged groups also suffering the greatest health disad-
vantage (Fox, Goldblatt, & Jones, 1985; Arber & Ginn,
1993; Menchik, 1993; Martelin, 1994; Elo & Preston,
1996; Marmot & Shipley, 1996; Rogers, 1996; Sundquist
& Johansson, 1997; Grundy & Glaser, 1999; Grundy &
Holt, 2000). In general, associations between health and
socio-economic characteristics seem less pronounced
than in young or middle-aged groups, but because
*Corresponding author. Tel.: +44-20-7299-4668; fax: +44-
20-7299-4637.
E-mail address: [email protected] (E. Grundy).
0277-9536/03/$ - see front matter r 2002 Elsevier Science Ltd. All rights reserved.
PII: S 0 2 7 7 - 9 5 3 6 ( 0 2 ) 0 0 0 9 3 - X
morbidity and mortality is concentrated in elderly age
groups, attributable differences are greater.
A substantial and to some extent parallel literature,
has shown that socio-demographic and social-psycho-
logical characteristics such as marital status, household
composition and social support are also associated with
differentials in health and mortality in older age groups.
In general, married people have the best health, followed
by the never married and then the formerly married.
Hypothesised reasons for these associations include both
selection factors—good health increases the chances of
marrying (including remarrying) and remaining married
for longer—and the protective effects of care and
support (Verbrugge, 1979; Hu & Goldman, 1990;
Umberson, 1992; Hahn, 1993; Gliksman, Lazarus,
Wilson, & Leeder, 1975; Waite, 1995; Cheung, 2000).
Although these latter effects might be supposed to be
particularly important in older age groups, some studies
suggest a weaker, or even reversed, relationship between
health and marriage with increasing age. Goldman,
Korenman and Weinstein (1995), for example, found
that never-married older women had better health
outcomes than their married counterparts, a result they
attributed to more extensive social ties built up over the
lifetime as an alternative to marriage. However, their
analysis was based on a sample that excluded the
institutional population, which, as the unmarried are
over-represented in institutions, may have biased results.
Analyses of British data on differentials in limiting long
standing illness which included the whole population
have shown a continuing, although weaker, advantage
for the married, even in the oldest age groups (Murphy,
Glaser, & Grundy, 1997).
Associations between other indicators of social con-
nectedness, including social network size and character-
istics and church or club membership, and both
mortality and other health indicators have also been
reported (Blazer, 1982; Seeman, Kaplan, Knudsen,
Cohen, & Guralnik, 1987; House & Landis, 1988;
Grundy, Bowling, & Farquhar, 1996; Sugisawa, Liang,
& Liu, 1994). However, in some studies effects appear
much weaker, or non-existent, in older than in younger
groups, possibly because of inconsistencies in the
measures of health and social support used and the
relatively small numbers of older people included in
some analyses (Orth-Gomer & Unden, 1987; O’Reilly,
1988; Bowling & Grundy, 1998).
A wide range of studies thus show variations in the
health of elderly people according to differences in
socio-economic circumstances and socio-demographic
or socio-psychological characteristics, although in both
cases variations seem less marked than in younger age
groups. These domains, although often considered
separately (Preston & Taubman, 1994), are clearly
intertwined in several ways. It is known, for example,
that there are social class differences in patterns of social
interaction and in marriage and divorce patterns (House
& Landis, 1988; Ben-Shlomo, Smith, Shipley, &
Marmot, 1993; Schoeni, 1995; Stansfield, 1999). Among
elderly women, in particular, being married is associated
with indicators of economic advantage such as income
and housing tenure (Hahn, 1993; Murphy et al., 1997).
Apart from these interrelationships, there may be
factors which influence both socio-economic and socio-
demographic circumstances at older ages and exert an
influence on health, such as legacies from earlier life.
Attributes present or acquired in childhood may have an
important and lasting effect on life chances, health
behaviours and coping mechanisms, and so on health,
throughout the life course, as well as exerting a strong
influence on adult socio-economic and socio-demo-
graphic experiences and later life circumstances (Barker,
1992; Bartley, Blane, & Montgomery, 1999; Bosma, van
de Mheen, & Mackenbach, 1999; Brunner, Shipley,
Blane, Smith, & Marmot, 1999; Davey Smith, Hart,
Blane, Gillis, & Hawthorne, 1997; Wadsworth, 1997).
Education, for example, may increase feelings of
personal control and promote better health behaviours
as well as providing a route to higher status well paid
occupations and so to accumulated wealth and better
pensions in later life (Bosma, Schrijvers, & Mackenbach,
1999). Height, often used as an indicator of childhood
circumstances and development, is associated with both
adult social class and with the marriage chances of men,
as well as with health (Blane et al., 1996; Kuh &
Wadsworth, 1989; Murray, 2000; Phillips et al., 2001).
As well as common, or overlapping, pathways to
particular health, socio-economic and socio-demo-
graphic statuses in adult life, there may also be common
mechanisms whereby socio-economic and socio-demo-
graphic or psychological characteristics influence health.
Most obviously, social class, education and housing
tenure are all strongly associated with smoking (Blaxter,
1990; Bennett, Dodd, Flatley, Freeth, & Bolling, 1995);
so too is marital status and, among elderly men,
household type (Umberson, 1992). Smoking is clearly
not the only explanation for variations in health as
persistent socio-economic inequalities in mortality and
morbidity in the whole adult population are found even
when smoking is allowed for (Blaxter, 1990; Suadicani,
Hein, & Gyntelberg, 1994). Similarly, studies have
reported associations between social and blood pressure
after adjustment for smoking, exercise, alcohol use and
body mass index (Hanson, Isacsson, Janzon, Lindell, &
Rastam, 1988).
Synergistic or offsetting interactions between econom-
ic and socio-psychological domains may also be
important (Roberts, Dunkle, & Haug, 1994). Material
advantages not only enable the purchase of better food
and housing, but also the purchase of services that may
preserve feelings of control and autonomy and enable
social participation, all factors hypothesised to have
E. Grundy, A. Sloggett / Social Science & Medicine 56 (2003) 935–947936
important influences on health behaviours and physio-
logical functions (Seeman, 2000). Supportive networks
may buffer the effects of stress, including socio-
economic stress, and enhance the operation of immu-
nological functions, as well as being a potential source of
practical help and advice and so an alternative to
purchased assistance (Berkman, Leo-Summers, & Hor-
owitz, 1992; Uchino, Cacioppo, & Kiecolt-Glaser,
1996). Conversely, the combination of poor socio-
economic and poor socio-psychological circumstances
may be particularly harmful (Ben-Shlomo et al., 1993;
Martikainen & Valkonen, 1998).
For all these reasons it would seem essential to
consider both socio-economic and socio-demographic
factors in analyses of health differentials in later life and
preferably also indicators of childhood legacies and
health behaviours. This type of analysis is, however,
relatively unusual, partly due to data limitations
(Preston & Taubman, 1994). Here we use data from a
large nationally representative sample of the older
population of England to investigate the effect of
attributes acquired in childhood and young adulthood,
which we term personal capital, current social resources
and current socio-economic circumstances on health
variation in later life, while also controlling for smoking
behaviour, one of the mechanisms whereby the other
domains may influence health. The personal capital
variables used were height and educational qualifica-
tions. Educational qualifications may be gained in
adulthood, but in the cohorts with which we are
concerned this was relatively unusual and highest
qualification obtained is a good indicator of educational
experiences and outcomes in childhood and early
adulthood, themselves strongly influenced by social
class of origin (White, Blane, Morris, & Mourouga,
1999).
As already noted there is an extensive literature on
links between marital status and health, although still
some uncertainty as to whether associations are
attenuated, or even reversed in older age groups. We
used this, together with a variable measuring perceived
social support, as indicators of social resources.
Housing tenure has been shown in numerous studies
to be associated with other indicators of socio-economic
status, such as income and social class, and to be
strongly associated with differentials in health (Fox
et al., 1985). It has the advantage, in comparison with
occupationally based measures, of relating to current
material circumstances and applying equally to men and
women (Arber & Ginn, 1993; Grundy & Holt, 2001). We
used this as an indicator of socio-economic circum-
stances together with receipt of income support, a means
tested benefit paid to those on low incomes.
Our aims were to quantify the extent of inequalities in
the health of older people, see which of the broad
domains considered was most strongly associated with
health in later life, and investigate possible interactive
effects of socio-economic and socio-demographic dis-
advantage on health in later life. Health, whether
conceptualised negatively as the absence of disease,
positively as a complete state of well-being, or norma-
tively as the average, is a multidimensional concept that
is difficult to measure (Ware, Allyson, & Robert, 1980).
It is well recognised, for example, that self-reported and
observational measures produce different results,
although which gives a better indicator of ‘true’ health
status remains a matter of debate. Several analysts have
concluded that self-reported and directly measured
indicators of physical function represent different
dimensions of health (Guralnik, Branch, Cummings, &
Curb, 1989; Merrill, Seeman, Kasl, & Berkman, 1997).
In this study we use a range of six indicators of health
status, four based on self-reports and two based on
nurse collected data, which we hypothesised would
identify different dimensions of health. We aimed to
investigate both associations between the explanatory
domains and these outcome indicators and whether the
explanatory variables had consistent or varying effects
on different indicators of health status.
Data and methods
The data we use come from the 1993–95 rounds of the
Health Survey for England (HSfE) (Bennett et al., 1995).
We chose this study because it is nationally representa-
tive, includes a range of indicators of health status,
together with information on health-related behaviours
and socio-demographic and socio-economic character-
istics, and has a large enough sample size, when, as here,
3 years data are combined to allow detailed analysis.
Data in the HSfE are collected through a questionnaire,
nearly all interviewer administered, and a second nurse
visit during which prescribed medicines are counted and
blood pressure taken. Nurses also took blood samples
but blood analyte data were unavailable for over 30% of
elderly respondents and so are not used here.
Co-variates used in the analysis
Height was measured by interviewers using a portable
stadiometer. As height varies by cohort, age and sex, the
indicator of height we derived for our analyses was
tertile of the height distribution for those of the same
gender and 10-year age group. Those for whom a
measurement of height was lacking were identified
separately. As a large proportion of today’s elderly
population have no formal educational qualifications,
we distinguished only two qualification groups, those
with and those without an educational qualification of
any kind. The size of the sample meant that we were able
to use a fourfold classification of marital status
E. Grundy, A. Sloggett / Social Science & Medicine 56 (2003) 935–947 937
(currently married or cohabiting; never married; wi-
dowed; divorced or separated) rather than amalgamat-
ing the unmarried groups. The perceived social support
measure used in the HSfE was developed for the Health
and Lifestyle Survey and was based on seven questions
on support and encouragement from family and friends,
each with three possible responses. Responses were
combined into a single scale ranging from 0 to 21. We
followed developers of the scale in categorising those
with scores of 21 as having no lack of social support,
those with scores of 18–20 as having some lack of social
support and those with scores of less than 18 as having a
severe lack of social support (Blaxter, 1990; Bennett
et al., 1995). Three tenure groups were used in the
analysis, owner–occupiers, tenants of local authorities or
housing associations, and other tenants. The second
socio-economic indicator used distinguished recipients
of income support from non-recipients.
Indicators of health status
The indicators of health status we analyse comprised
four based on self-reports and two based on nurse
collected data. The self-reported measures were presence
of a long-standing illness; number of specific long-
standing conditions (with those with no long-standing
illness coded as zero), and self-reported general health
(dichotomised into ‘bad’ or’ very bad’ rather than ‘very
good’, ‘good’ or ‘fair’). The fourth measure was self-
completed score on the General Health Questionnaire
(12-item version); a well validated instrument for
measuring minor psychiatric morbidity. In line with
accepted practice we dichotomised responses into those
of four or above, a threshold taken to indicate
‘caseness’, and those with lower scores (Goldberg &
Williams, 1988).
The observational indicators were high blood pressure
(systolic blood pressure >159mm Hg or diastolic blood
pressure >94 mm Hg, or taking anti-hypertensive
medication) and number of prescribed medications
being taken. These data were collected during the nurse
visit that followed administration of the main ques-
tionnaire. Nurses measured blood pressure using a
Dinamap 8100 monitor and recorded information on
all medications being taken. Number of medications is
here dichotomised into 0–2 and 3 and more.
The Health Survey for England includes only those in
private households. Some 20% of those aged 85 and
over live in institutions, and as entry to an institution is
strongly associated with health, with marital status and,
less strongly, with housing tenure (Grundy & Glaser,
1997), analysis of differentials in the health of the oldest
old by these characteristics will be biased if based on
samples, like the HSfE, which exclude the institutional
population. Our concerns about this were compounded
by the extent of information missing for those aged 85
and over who were included in the survey (20% had no
height measurement; 26% no count of medicines and
46% no blood pressure measurement). We therefore
restricted our analyses to those aged 65–84. In this
broad age group only 2% of men and 4% of women
lived in institutions in 1991 (Grundy, Glaser, & Murphy,
2000).
Response rates and missing data
Response rates to the HsfE, reported in detail
elsewhere, are good and exceed 80% in elderly age
groups (Bennett et al., 1995). However, some of the
variables we used were based on measurements which
were lacking for some of the sample. This is shown in
Table 1 which gives details of the proportions with
missing information on height (measured by inter-
viewers during the first visit); number of medications
and blood pressure (measured by the nurse during the
second visit) and GHQ (measured using a self-comple-
tion booklet included in the main interview) together
with the proportion of respondents and non-respon-
dents to these items who reported their health as bad or
very bad. The proportions with missing blood pressure
measurements were quite high and those lacking this
measure included an over representation of people
Table 1
Percentage of sample with missing measurements and prevalence (%) of self-reported bad or very bad health by whether a measure was
recorded or unrecorded
Age Blood pressure Height Medicines GHQ
Missing
(%)
Bad health (%) Missing
(%)
Bad health (%) Missing
(%)
Bad health (%) Missing
(%)
Bad health (%)
Rec. Unrec. Rec. Unrec. Rec. Unrec. Rec. Unrec.
65–9 25 7 14 4 8 27 15 13 8 4 8 26
70–4 27 7 13 5 8 24 15 10 10 4 8 21
75–9 29 9 15 6 9 39 16 14 11 6 9 19
80–4 38 10 16 11 10 35 19 15 12 7 11 23
E. Grundy, A. Sloggett / Social Science & Medicine 56 (2003) 935–947938
reporting their health as bad or very bad. The
proportions with missing height or GHQ information
were much lower but, particularly for height, those
without a measurement were much more likely than
those with one to report bad or very bad health.
Information on medicines was missing for some 17% of
the sample, but there was no difference between those
with and without this measure in reporting of bad or
very bad health. Here, those with missing height data
have been included and are shown as a separate group.
Those with missing outcome data have had to be
excluded from analyses of that outcome.
We first calculated the prevalence of each indicator of
health according to our indicators of personal capital,
social resources and socio-economic circumstances using
linear regression to adjust for age and survey year. In
subsequent multivariate analyses we used logistic
regression to estimate odds of poor outcomes in models
including all the variables, together with age group and
survey year. Analysis of deviance was used to identify
which domain was most strongly associated with
variation in the outcome variables. Appendix A shows
the distribution of the sample by variables used in the
analysis (except height which, as explained above, was
coded into tertiles).
Results
Fig. 1 shows the age-adjusted prevalence of self-
reported bad or very bad health according to the pairs
of variables representing the three domains of interest.
Among both men and women a higher proportion of
those with no educational qualifications rated their
health bad or very bad and among men and, to a lesser
extent women, there was a gradient in prevalence with
height (Fig. 1, Panel a). Short men and women with no
qualifications were twice as likely to report poor health
as their tall counterparts with qualifications. The
prevalence of bad health was very high among those
with no measure of height, a group which would include
the chairbound and those too frail to stand unaided.
0
5
10
15
20
25
30
35
Owner occ Priv. Tenant LA tenant Owner occ Priv. Tenant LA tenant
Housing tenure
(c) by housing tenure and receipt of income support
No inc. support Has inc. support
Men Women
0
5
10
15
20
25
30
35
%%
Married Single WidowedDivorced Married Single Widowed Divorced
Marital status
(b) by marital status and perceived social support
No lack Some or severe lack
WomenMen
0
5
10
15
20
25
30
35
Tall Mid Short Unmeasured Tall Mid Short Unmeasured
Height tercile
(a) by education and height
Has educ. Qual. No quals.
Men Women
(a) (b)
(c)
Fig. 1. Age adjusted prevalence of self-reported bad or very bad health among men and women aged 65–84: (a) by education and
height; (b) by marital status and perceived social support; (c) by housing tenure and receipt of income support.
E. Grundy, A. Sloggett / Social Science & Medicine 56 (2003) 935–947 939
Among men differentials by marital status, shown in
the second panel of the figure, were as expected with the
highest prevalence of bad health among the divorced
and the lowest among the married. Among women,
however, the proportion reporting bad or very bad
health was lowest among single women and highest
among the divorced. For both men and women in all
marital status categories those reporting a lack of social
support had worse health on this indicator, but
differences were not large. Socio-economic differences
in bad health, shown in the third panel, were substantial.
More tenants than owner–occupiers reported bad health
and prevalence rates were markedly raised among those
in receipt of income support.
Parallel analyses of variations in the other five
indicators of health status were undertaken but, in the
interests of brevity, are not presented here. Results were
similar to those shown in Fig. 1, although there were
some differences in their magnitude and ordering. There
was less variation in the prevalence of hypertension than
in the other indicators, especially the self-reported ones.
For example among men the prevalence of hypertension
by marital status and social support ranged from 50%
among married men with no lack of social support to
58% among widowers with some or a severe lack of
support. Variation in the prevalence of GHQ scores of
four or more was much greater (8% among married men
with no lack of social support compared with 24%
among less well-supported widowers).
This descriptive analysis showed that all the variables
chosen to represent important domains of life were
associated with the health indicators considered, to
varying degrees. There were of course strong correla-
tions between the co-variates considered. Receipt of
income support, for example, was associated with
educational qualifications, housing tenure and marital
status as well as with age and gender and perceived
social support was associated with marital status,
particularly for men.
Logistic regression analysis was undertaken to esti-
mate the effect of each variable on the outcomes
considered, after adjustment for the other co-variates,
including 5 year age group, smoking status and survey
year. Initial analyses showed that unmeasured height
was, as might be expected, strongly associated with
significantly higher odds of several of the six health
indicators used. However, measured height was only
significantly associated with one indicator—high blood
pressure—among women and among men with none of
the health indicators. We therefore decided to drop this
variable and the results presented below thus include
only one variable (education) to represent the personal
capital domain. We included a control for a number of
physical conditions reported in the model of GHQ
because of known strong associations between physical
and mental health.
Results from these models for men, presented in
Table 2, show lack of an educational qualification was
associated with GHQ scores above three and with taking
three or more medicines. Widowers had significantly
higher odds of bad health, taking three or more
medicines, high blood pressure and psychiatric morbid-
ity than married men (the reference group). Men
reporting some lack of social support had higher risks
of a poor GHQ score. Local authority tenure was
associated with higher odds of reporting bad health and
with GHQ. Receipt of income support was associated
with raised odds of five of the six indicators, the
exception being raised blood pressure. Of the control
variables, older age was associated with higher odds of
taking three or more medicines and former smoking
habit with all indicators except blood pressure and
GHQ.
Results for women presented in Table 3 show that
education was associated with three of the six indicators.
Lack of social support was positively associated with
GHQ and with bad health, less strongly with reported
long-standing illness and negatively with raised blood
pressure. The marital status results suggest, after control
for all the other variables in the model, no advantage for
the currently married. Single and widowed women had
lower odds of reporting bad or very bad health, single
women also had lower odds of a raised GHQ score and
of reporting two or more conditions. Divorced women
had a reduced risk of taking three or more medicines.
Local authority tenants and those in receipt of income
support had raised odds of five out of six of the health
indicators considered.
One of our research questions was whether disadvan-
tage in one sphere compounded disadvantage in another
and whether strengths in, for example socio-economic
circumstances, could compensate for weaknesses in
social resources. In order to analyse this we tested for
interactions in all the models fitted. However, for neither
men nor women did we find any interactions that were
statistically significant.
These results show that the indicators of personal
capital, social resources and socio-economic resources
were associated to varying degrees with higher odds of
poor health in models including all co-variates. How-
ever, some of the marital status associations were not in
the hypothesised direction. The co-variates most con-
sistently associated with higher odds of poor health
indicators were receipt of income support, local author-
ity tenure and some lack of social support. The patterns
of associations varied considerably depending on which
health indicator was considered. Thus there were more
significant associations between the explanatory vari-
ables considered and proportions in bad or very bad
health and proportions with GHQ scores of 4 or more
than with the other two indicators based on self-
reported information. On this criteria taking more than
E. Grundy, A. Sloggett / Social Science & Medicine 56 (2003) 935–947940
three medicines appears more sensitive than the other
nurse measured indicator, high blood pressure, although
the extent of missing blood pressure measurements may
be an influence on this.
We also wished to examine the contribution of each
of these domains, and of smoking, to the overall
variation in health in this sample of elderly people. We
therefore undertook an analysis of the contribution of
each to reductions in the deviance (variation) in the
sample. Results, presented in Table 4, show that all the
domains, and smoking contributed significantly to
reductions in the deviance when variations in bad or
very bad health were modelled. The contribution of the
socio-economic resources indicator was particularly
strong, whereas the contribution of the smoking
variable, although statistically significant, was weaker
than that of the three other domains. When long-
standing illness was taken as an outcome, however,
among men only smoking contributed significantly to
reductions in the deviance and among both men and
women the education variable was not significantly
associated with a reduction in deviance in either long-
standing illness or reporting of two more conditions.
When taking more than three medicines was used as an
outcome, the contributions of education and socio-
economic resources were significant but less important
than in the models fitted to self-reported health. The
effect of smoking however, was, much more important.
Among women the social resources domain did not
contribute significantly to improving the fit of this
model. In the analysis of hypertension smoking and
social resources were both associated with significant
(but not large) reductions in the deviance for men, while
among women significant reductions were associated
with education and socio-economic resources. Social
resources were, for both men and women, the most
important domain associated with reductions in the
deviance for GHQ.
Table 2
Odds ratios from logistic regression models of indicators of poor health, men aged 65–84
Co-variates Bad/very bad
health
Long-
standing
illness
2+Conditions 3+Medicines High blood
pressure
Psychiatric
morbidity
(GHQ 4+)
Age 70–4 0.88 1.13 1.19 1.25* 1.12 1.10
70–5 0.86 1.07 1.24* 1.49** 1.17 1.18
80–4 0.96 0.83 1.07 1.44* 1.10 1.58*
Smoking Ex 1.49* 1.19 1.32** 1.47** 1.17 1.05
Current 1.29 0.77* 1.07 0.82 0.85 1.07
Number
physical
conditions
— — — — — 1.71***
Personal capital
Education No quals 1.26 0.98 1.06 1.31** 1.07 1.41**
Social resources
Marital status Single 0.92 0.88 0.89 0.86 1.69** 0.75
Widowed 1.41* 1.13 1.14 1.37** 1.30* 1.73***
Div./sep 1.44 1.19 1.18 1.16 1.19 1.40
Social support Some lack 0.90 0.95 1.18 1.32** 1.03 1.37**
Severe lack 1.10 1.11 1.17 0.98 1.04 1.91***
Socio economic resources
Housing tenure LA tenant 2.00*** 1.14 1.11 1.17 1.01 1.34*
Other tenant 1.42 0.97 0.81 0.75 0.96 1.22
Income support Receives 2.87*** 1.35* 1.38** 1.52** 1.19 1.83***
N 3706 3708 3701 3244 2760 3608
Reference categories: age 65–9; never smoked; (no physical conditions, GHQ model only); has a qualification; married; no lack of
social support; owner–occupier; not in receipt of income support.
***Po0:001; **Po0:01; *Po0:05:
E. Grundy, A. Sloggett / Social Science & Medicine 56 (2003) 935–947 941
Discussion
In this paper we have used data from a large
nationally representative sample to analyse differentials
in the health of older adults according to variables
selected to represent personal capital, social resources
and socio-economic resources. Unlike many analyses
which have considered only one outcome, we analysed
variations in six indicators of health status including
both self-reported and nurse-measured variables. We
also controlled for smoking status as well as for age.
Our initial analyses showed that all the variables we
selected as indicative of the domains we wanted to
consider were associated with at least some of our
indicators of health status. In multivariate analyses
socio-economic indicators, particularly receipt of
income support (a marker of poverty) appeared
most consistently associated with raised odds of poor
health outcomes. Of our two indicators of childhood
legacies, measured stature was only associated with
blood pressure in women (which is consistent with
documented physiological associations between stature
and cardiovascular performance) and, was dropped
from the multivariate analysis. This does not, of course,
mean that legacies from childhood are unimportant in
explaining health differentials in later life and indeed we
found associations between educational qualification,
our second indicator of personal capital, and several
health indicators. Our analysis was limited by the fact
that other indicators of childhood experience were
unavailable. Moreover, childhood experiences may
influence health in later life indirectly through their
effects on current socio-economic status, which was
taken account of in our analyses (Bosma et al., 1999;
Ross & Mirowsky, 1999).
A surprising finding was of weak or counterintuitive
associations between marital status and health indica-
tors. Some previous studies have also reported better
health among single than married elderly women in
studies, like this one, including only the private house-
Table 3
Odds ratios from logistic regression models of indicators of poor health, women aged 65–84
Co-variates Bad/very bad
health
Long-
standing
illness
2+Conditions 3+Medicine High blood
pressure
Psychiatric
morbidity
(GHQ 4+)
Age 70–4 1.27 1.01 0.97 1.10 1.24* 1.11
70–5 1.69*** 1.34** 1.18 1.23 1.60** 1.43**
80–4 1.64** 1.50*** 1.19 1.95*** 2.11*** 1.60***
Smoking Ex 1.44** 1.16* 1.18* 1.56*** 0.89 1.08
Current 1.20 0.89 0.74** 0.88 0.82 1.20
No. physical
conditions
— — — — — 1.53***
Personal capital
Education No quals 1.63** 0.91 0.97 1.12 1.35*** 1.35**
Social resources
Marital status Single 0.58* 0.82 0.71* 0.71 0.85 0.45***
Widowed 0.67*** 0.99 1.04 1.02 1.05 1.03
Div./sep 0.93 1.09 1.47* 0.65* 0.81 1.17
Social support Some lack 1.05 1.04 1.12 1.09 0.88 1.38**
Severe lack 1.68*** 1.23* 1.04 1.03 0.79* 2.57***
Socio economic resources
Housing tenure LA tenant 1.84*** 1.39*** 1.57*** 1.35** 1.42*** 1.13
Other tenant 1.16 1.08 1.27* 1.38* 1.30* 1.04
Income support Receives 2.26*** 1.59*** 1.40*** 1.71*** 1.13 1.28*
N 4966 4976 4964 4147 3541 4812
Reference categories: age 65–9; never smoked; (no physical conditions, GHQ model only); medium height; has a qualification;
married; no lack of social support; owner–occupier; not in receipt of income support.
***Po0:001; **Po0:01; *Po0:05:
E. Grundy, A. Sloggett / Social Science & Medicine 56 (2003) 935–947942
hold population. We restricted our analyses to those
aged 65–84 in order to reduce bias arising from
differential exclusion as a result of residence in an
institution. In this age group the proportion of people in
institutions, and so excluded from surveys such as the
Health Survey for England, is small. Nevertheless, as
institutional residence is associated with both marital
status and health and 10% of single men and women
Table 4
Analysis of deviance in proportions with poor health by indicator of poor health
Men Women
Model Deviance/change
in deviance
Df/change in df Po Deviance/change
in deviance
Df/change In df Po
(a) Self reported ‘bad’ or ‘very bad’ health
Age group and year 2360 3700 0.001 3086 4960 0.001
+Personal capital �20 �1 0.001 �40 �1 0.001
+Social resources �23 �5 0.001 �24 �5 0.001
+Socio-economic
resources
�87 �3 0.001 �99 �3 0.001
+Smoking �6 �2 0.05 �11 �2 0.005
(b) Long-standing illness
Age group and year 4855 3702 6533 4970
+Personal capital �0 �1 NS �0 �1 NS
+Social resources �7 �5 NS �12 �5 0.05
+Socio-economic
resources
�7 �3 NS �56 �3 0.001
+Smoking �28 �2 0.001 �10 �2 0.05
(c) 2+Conditions
Age group and year 4425 3695 6129 4960
+Personal capital �2 �1 NS �3 �1 NS
+Social resources �10 �5 NS �25 �5 0.001
+Socio-economic
resources
�11 �3 0.05 �59 �3 0.001
+Smoking �11 �2 0.01 �23 �2 0.001
(d) Taking three or more prescribed medicines
Age group and year 3250 3238 0.001 4233 4141 0.001
+Personal capital �12 �1 0.001 �10 �1 0.005
+Social resources �18 �5 0.01 �7 �5 NS
+Socio-economic
resources
�12 �3 0.05 �49 �3 0.001
+Smoking �31 �2 0.001 �36 �2 0.001
(e) Hypertension
Age group and year 3809 2754 4705 3535
+Personal capital �2 �1 NS �28 �1 0.001
+Social resources �14 �5 0.05 �10 �5 NS
+Socio-economic
resources
�1 �3 NS �19 �3 0.001
+Smoking �12 �2 0.005 �5 �2 NS
(f) GHQ Score of 4+
Age group and year 2464 3601 4057 4805
+Personal capital �22 �1 0.001 �20 �1 0.001
+Social resources �53 �5 0.001 �87 �5 0.001
+Socio-economic
resources
�23 �3 0.001 �9 �3 0.001
+Smoking �0 �2 NS �3 �2 NS
Df=degrees of freedom.
E. Grundy, A. Sloggett / Social Science & Medicine 56 (2003) 935–947 943
aged 65–84 were in institutions in 1991 (compared with
2% of all men and 4% of all women), this limitation of
the data may have had some effect on our results
(Grundy et al., 2000). It is also important to remember
that the odds ratios shown in Tables 3 and 4 are those
from the full models, that is after allowance for socio-
economic factors and social support, which have not
been taken into account in many other earlier studies of
links between marital status and health.
Apart from exclusion of the institutional population,
other forms of selection may also influence health
differentials in the older population, most obviously
selective survival. Estimates from the Government
Actuary’s Department show that 69% of men and
78% of women born in 1930 survived to aged 65; of
those born in 1911, the oldest birth cohort represented in
our analysis, only 14% of men and 31% of women
survived to age 84. Results will therefore be influenced
by prior mortality of the unhealthiest. This, together
with the fact that poor health provides a major impetus
for giving up smoking, is likely to account for the
increased odds of poor health outcomes among ex, but
not current, smokers.
We used six indicators of health status in our analysis
and our results have implications both for selection
of the most sensitive indicators to use in surveys
and suggest that pathways to particular indicators
of poor health may vary. On the first count the
self-rated general health indicator appeared to perform
well, particularly in comparison with the widely used
long-standing illness indicator. On the second our
analysis of deviance showed that social resources
contributed significantly to variation in self-rated health,
but among women not to the three or more medicines
indicator (after allowance for personal capital, socio-
economic resources and smoking) and among men not
to long-standing illness or reporting two or more
conditions. Marital status and lack of social support
had the greatest effect on the GHQ variable, which is
consistent with what is known about links between
social support and psychological health. However,
it must be recognised that the social support measure
was based on self-reports and it may well be that
people who are depressed are more likely to perceive
and report that their levels of social support are low
simply because of their mental state. Smoking was
much more strongly associated with the medicines
indicator and with long-standing illness (men) or
reporting two or more conditions (women) than with
the self-rated health variable. These results are consis-
tent with the view that self-rated health measures
provide holistic indicators of health in the sense of well
being, whereas indicators such as taking medicines
may be more indicative of specific morbidities
(Idler & Benyamini, 1997). Factors which influence
these different dimensions of health may not be the
same, just as specific diseases and causes of death
seem to relate to the life course in different ways
(Blane, 1999; Davey Smith, Gunnell, & Ben-Shlomo,
2001).
These results are based on cross sectional data and
clearly longitudinal data would be much more suitable
for unravelling the pathways to good and bad health in
later life. Currently, large, nationally representative
longitudinal data on the older population are not
available in Britain, a gap the new English Longitudinal
Study of Ageing (based on a follow up of the 2000
HSfE) is designed to fill. Other limitations of the study
not already referred to include the rather restricted
choice of indicators available to represent personal
capital and social resources and lack of information
about social capital and other area characteristics which
may also influence health. Additionally, as already
noted, perceptions of social support may be influenced
by psychological health, and both physical and psycho-
logical health may influence social participation and
opportunities for developing and maintaining the social
networks from which social support is drawn. In this
analysis it is not possible to identify causal pathways
between these variables.
Despite these limitations, these results, based on a
large nationally representative sample and including
both observational and self-reported indicators of
health, extend our knowledge in several ways. Firstly,
our results demonstrate unequivocally the strong link
between poverty in old age and poor health, even after
control for smoking and other relevant factors. Sec-
ondly, the increased odds of psychiatric morbidity
among those with no educational qualifications suggests
a link between early life circumstances and development,
perhaps including development of coping strategies, and
psychological well-being in later life. A third finding of
interest was the lack of health advantage for married
older people, particularly among women, and, again
among women, the possible advantage of the never
married. The effects of marital status and history on
health and support needs in later life are a very
important issue for the future because of large differ-
ences in the marital experiences of cohorts born in the
inter-war and immediate post-war period and those
born from the mid 1950s onward (Grundy, 1996).
Further work on the selective and protective effects of
marriage and development of alternative sources of
support would therefore seem important. These results
also indicate the complexity of measuring health status
in later life and the possibly differing influences on
various types of health indictor. Finally, our analyses
emphasise again the need to consider both socio-
economic and socio-psychological influences on health
and health inequalities and the need for both further
research and policy initiatives to reduce the extent of
health inequalities in later life.
E. Grundy, A. Sloggett / Social Science & Medicine 56 (2003) 935–947944
Acknowledgements
This research was supported by the Economic and
Social Research council, grant reference number L128
251040, as part of its Health Variations (Phase II)
Programme. Gemma Holt provided valuable assistance
with data management and preparation in the early
stages of the work reported here.
Appendix
See (Table 5).
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