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ARTICLE IN PRESS
0277-9536/$ - se
doi:10.1016/j.so
�Correspond
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(R. Thomas).
Social Science & Medicine 60 (2005) 2773–2783
www.elsevier.com/locate/socscimed
Housing improvement and self-reported mental distress amongcouncil estate residents
Richard Thomasa,�, Sherrill Evansb, Peter Huxleyb, Claire Gatelyb, Anne Rogersc
aSchool of Geography, University of Manchester, Oxford Road, Manchester, M13 9PL, UKbHealth Services Research Department, Institute of Psychiatry, King’s College, SE5 8AF London, UK
cNational Primary Care Research and Development Centre, University of Manchester, Manchester, M13 9PL, UK
Available online 26 January 2005
Abstract
This paper is concerned with how housing improvements instigated either publicly or privately influence the degree of
psychological stress reported by council estate residents in South Manchester. Stress is measured on the GHQ12 scale
containing standard symptomatic items. Potential sources of variation in this indicator are analysed within a
geographical setting where repeated samples of residents were drawn from two adjacent suburban council housing
estates before and after the implementation of a single regeneration budget (SRB) housing initiative in late 1999. The
residents of one of these estates (Wythenshawe) were targeted by this funding while those in the other (Mersey Bank)
were not. The latter, therefore, serve as a control for the effects of the enhanced incidence of housing improvement
activity promoted by this SRB. Regression analyses revealed that stress was raised significantly among the SRB
residents perhaps on account of the additional environmental nuisance they encountered. The experience of stress
among all residents, however, was dominated by measures of personal psychosocial risk and it is argued that future
regeneration initiatives should address the manifestation of these risks in the effort to achieve better mental health.
r 2004 Elsevier Ltd. All rights reserved.
Keywords: Manchester, UK; Council estate residents; Mental health; Urban regeneration
Introduction
The supposition that changing socio-economic cir-
cumstances might affect the mental health of a commu-
nity has been informed through the refinement of a
number of psychological constructions (Weich & Lewis,
1998; Marmot & Bobak, 2000; Rogers et al., 2001;
WHO, 2001). The initial ideas concerning this connec-
tion emphasised the importance of social structure
evidenced by the positive association between psychia-
tric morbidity and social disadvantage and adversity
e front matter r 2004 Elsevier Ltd. All rights reserve
cscimed.2004.11.015
ing author.
ess: [email protected]
(Holingshead & Redlich (1958)) and, later, with
disparities in resources like income, occupation and
years in education (Bartley, Blane & Davey-Smith,
1998). A second strand of this debate, often referred to
as the psychosocial perspective, has noted the more
immediate contribution to the onset of mental distress of
precipitating personal factors like the experience of
stressful life events or changed social circumstances
(Dohrenwend & Dohrenwend, 1982; Brown & Harris,
1978). The evolution of this research has also witnessed
a switch from a preoccupation with the psychiatric
epidemiology elicited from individuals being treated for
mental health problems to a more recent focus on the
origins of symptomatic distress among the community
as a whole (Aneshensel & Sucoff, 1996; Elliott, 2000). A
d.
ARTICLE IN PRESSR. Thomas et al. / Social Science & Medicine 60 (2005) 2773–27832774
corollary of all this effort is that initiatives aimed at
improving the local environment might impact indirectly
upon the mental health of the recipients of these actions.
More particularly, the research reported here is
concerned with how housing improvements instigated
either publicly or privately influence the degree of
psychological stress reported by those most immediately
affected. The measurement of stress is made quantita-
tively by recourse to the General Health Questionnaire
12 point scale (GHQ12) containing standard sympto-
matic items (Goldberg & Williams, 1988). Potential
sources of variation in this indicator are analysed within
a geographical setting where repeated samples of
residents were drawn from two adjacent suburban
council housing estates in South Manchester before
and after the implementation of a single regeneration
budget (SRB) housing initiative in late 1999. The
residents of one of these estates (Wythenshawe) were
targeted by this funding while those in the other (Mersey
Bank) were not. The latter, therefore, serve as a control
for the effects of the enhanced incidence of improvement
activity promoted by this SRB. This design facilitates
the exploration of two general hypotheses. First, are the
GHQ12 scores of residents altered either negatively or
positively by the experience of housing improvement?
Second, are such possible outcomes further affected by
the more intense occurrence of regeneration activity in
the targeted estate? The assessment of these essentially
environmental stimuli also includes an examination of
their leverage relative to known psychological risks
factors for the susceptibility to mental distress.
The paper is organised as follows. Section 2 considers
recent research concerning the relationship between
environmental influences and the psychosocial risks for
mental distress. Section 3 describes the survey methods
together with the experimental design. The latter
consists of a sequence of multiple regression models
specified first to establish the leverage of the incidence of
housing improvements on GHQ12 scores and then to
include variation associated with the presence of known
psychosocial risks. Section 4 describes the results of
these statistical procedures. The discussion relates these
findings to the debate about the influence of spatially
tailored social policy interventions on community
mental health.
Environmental and individual risks for mental distress
The structural and psychosocial constructions of
mental distress are not mutually exclusive because both
attach importance to the generalised risks associated
with socio-economic deprivation. The former, however,
emphasises the influence of environmental deprivation
while the latter highlights the more immediate contribu-
tion of adverse personal experiences. A hierarchical
framework that integrates these perspectives has been
proposed by Stansfeld, Head and Marmot (1998) and
Stansfeld, Fuhrer, Cattell, Wardle, and Head (1999). In
their scheme, risks originate in the physical environment
through the gradation of material resources. In turn, this
variation affects the frequency with which psychological
risk factors are present in the local social environment.
Poverty, for example, might be expected both to
enhance the likelihood of unemployment and to exacer-
bate the personal consequences of such an event.
Alternatively, access to financial resources might act
positively to buffer these potential impacts. Whether or
not such circumstances are expressed as symptoms of
distress depends upon the perceptions of each indivi-
dual, which is presumed to serve as the last filter on the
pathway to poor mental health.
A method for operationalising the main elements of
this scheme has been outlined in Thomas et al (2002)
where the distinction was made between risk factors
defined by state variables and those that represent
discrete events. States refer to persistent effects that
gradually enhance the likelihood of psychosocial risk.
They may be chosen to reflect structural characteristics
of the physical environment, like living in a community
with persistently high levels of unemployment, or to
measures of personal vulnerability more specifically
linked to the prevalence of common mental health
problems. Instances of such vulnerability include people
with a limiting disability or those with parents who died
during childhood. By contrast, events refer to occur-
rences thought to precipitate the onset of symptomatic
distress like the encounter of psychosocial risks. In
addition, individual perceptions may be reflected as
events representing reactions to current life circum-
stances. Feelings of entrapment, for example, which
have been found to be crucial to the formation of
depression in both patient and non-patient series
(Brown, Harris, & Hepworth, 1995), may be evident
by the reporting of a restricted opportunity like being
unable to move home. Such feelings may also become
manifest in the failure to achieve personal goals like the
work aspirations of those currently unemployed (Nor-
denmark & Strandh, 1999). Powerlessness, loss and
humiliation characterise the final pathway to depression
and both naturalistic studies and controlled trials
suggest that psychosocial situations reflecting new hope
(or fresh starts) characterise a similar pathway to
remission from depression (Harris, 2001).
Relationships between variables representing these
constructs have been analysed using data surveyed from
the South Manchester council estate residents prior to
the Wythenshawe SRB (Thomas et al., 2002). The
analysis revealed that the variation in GHQ12 scores
correlated more strongly with psychosocial event vari-
ables than those representing environmental states. In
addition both GHQ12 and the event variables were
ARTICLE IN PRESS
1However, there are a number of reasons to suppose this
sample may well be representative. A relatively low response
rate does not necessarily indicate low representativeness (Cook,
Heath, & Thompson, 2000; Krosnik, 1999). We compared the
respondents gender, age, ethnicity, marital status and employ-
ment status with the 1991 census data for the area, and the only
major difference was in the age distribution; 19–24 year olds
were under-represented in the sample (9.5% compared to
15.4% in the census). National sample surveys also report fewer
respondents in this age group (Krosnik, 1999), but there has
also been a reduction in this age group in the population
between 1991 and 1999; 15–24 year olds were 12% of the UK
population in 1999 (ONS, 2001). According to figures for the
study wards, there were 10.8% in this age group by 1998
R. Thomas et al. / Social Science & Medicine 60 (2005) 2773–2783 2775
found to be inversely related to the age of the resident.
These results are consistent with previous studies that, in
particular, report a relatively low incidence of depres-
sion in old age (Paykel, 1991). Similarly, the less
frequent occurrence of the precipitators of stress (life
events, goal-setting and restricted opportunities) among
the elderly also helps to account for their comparatively
better mental health.
Housing is seen to be implicit in the structure of this
general framework as a state of the physical environ-
ment. Type of tenure, for example, has been viewed as a
relational resource linked to psychological characteris-
tics such as a sense of identity and aspirations which
provide the basis for security, mastery, self-esteem and
overall life satisfaction (Mcintyre, Hiscock, Kearns, &
Ellaway, 2001; Nettleton & Burrows, 2000). This
research has demonstrated that psychological character-
istics are distributed unequally among residents in ways
that are likely to have different health impacts on those
who rent property compared to owner-occupiers. The
distribution of housing stressors, like overcrowding and
dampness, together with perceptions of the local
environment (area reputation) have been shown to
partly explain the relationship between housing tenure
and both physical and mental health (Ellaway &
Macintyre 1998). In addition, there is more limited
evidence to suggest that such potential health risks can
be reduced by interventions targeted at those with
specific vulnerabilities. Favourable outcomes have been
found for improved housing conditions (Halpern, 1980)
and, in particular, for those re-housed on the grounds of
poor mental health (Elton & Packer 1986). Similar
findings have been reported for local interventions
aimed at the unemployed (Price, van Ryan, & Vinokur,
1992) and pregnant teenagers living in poverty (Olds,
Henderson, Tatelbaum, & Chamberlin, 1988).
The effects of area-based housing improvement
initiatives, however, are more ambiguous. While better
living conditions are anticipated to be beneficial in the
long term, the immediate effects of repair and construc-
tion are more likely to be sources of stress. Such
outcomes have led a recent review of the health effects of
housing improvement interventions (Thomson, Petti-
crew, & Morrison, 2001) to conclude that large scale
studies investigating their wider social context are
required. This claim, therefore, provides a rationale for
our investigation of the mental health consequences of
the Wythenshawe SRB.
(Manchester City Council, 2000). Furthermore, a comparisonbetween our sample and the MORI survey (MORI, 2001;
n ¼ 3480) in eight comparable SRB areas, for 15 variables
common to both studies, showed that the present study mean
for all variables was always within the MORI range and close to
the mean. The means for six variables (employment, length of
residence, long standing illness, having no car, crime rating, and
safety at night) were all within one percentage point of the
MORI mean.
Design
Survey details
The Wythenshawe SRB area was matched with
neighbouring wards forming the Mersey Bank council
housing estate using the index of deprivation supple-
mented by locally available statistics. An initial postal
survey to addresses randomly selected from the electoral
register was conducted in March 1999 prior to the SRB
initiative. The 2596 respondents to this survey repre-
sented a relatively low response rate (17%) which is not
uncommon for postal surveys in deprived areas, and in
line with the pilot study response from a neighbouring
non-study area (18%).1
This survey was repeated 22 months later and sought
information from those people who had responded to
the postal survey and who had not moved away from the
area. By follow-up, 522 baseline respondents had moved
and 1344 of the remainder (65%) replied. Socio-
demographic variables predicting failure to return the
questionnaire at follow-up for whatever reason were age
(younger), gender (men) and marital status (single). The
respondents in index and control areas were similar in
age and gender: mean age 51 years (sd 18.4) vs. 53 (17.0),
p ¼ 0:20; percentage male 52% in both areas (p ¼ 0:95).
However there were slightly higher proportions of non-
whites and single people in the control area (6% vs. 2%,
po0.001 and 31% vs. 21% for control versus index
area, po0.001 in both cases).
The intervention
This research was founded on the expectation that the
SRB would lead to more changes in the index than in the
control area. Very little SRB expenditure had been
committed up to the time of the baseline survey, but
over £2m was invested over the study period. Some of
the major developments are ‘complementary’, that is,
not part of this £2m, but part of the overall package of
ARTICLE IN PRESS
Table 1
Types and frequencies of housing improvement reported by residents at follow-up
Type Wythenshawe
residents in
receipt(WR)
Wythenshawe
residents not in
receipt (WNR)
Mersey Bank
residents in
receipt(MBR)
Mersey Bank
residents not in
receipt (MBNR)
Heating 157 547 73 567
Damp proofing 41 663 53 587
Lighting/electrics 48 656 48 592
Roofing 28 676 55 585
Bathroom 110 594 43 597
Plumbing 25 678 32 608
Kitchen 73 631 33 607
Windows 133 571 79 561
Other 38 666 33 607
At least one of the above (area %) 360(51.1) 344(48.9) 225(35.2) 415(64.8)
R. Thomas et al. / Social Science & Medicine 60 (2005) 2773–27832776
interventions in the area, including private sector
finance. The changes of tenancy from local authority
to housing trust status, in the Willow Park area of
Wythenshawe, were part of the associated complemen-
tary developments. The total investment from all sources
to the end of the study period was about £45 m.
The follow-up survey asked respondents to report any
housing improvements completed since 1999. The
frequencies of these improvements by type are listed in
Table 1 for both Wythenshawe and Mersey Bank. The
survey did not identify how these improvements were
funded and, therefore, it is not possible to identify the
exact numbers attributable to the SRB. The differences
between the frequencies in the two areas, however, are
indicative of how improvements in Wythenshawe were
affected by this area intervention. In this respect, 51.1%
of the Wythenshawe respondents were in receipt of at
least one type of housing improvement compared to
35.2% for those in Mersey Bank. Moreover, the
frequencies for the different types of alteration indicate
the main effect on housing conditions of the SRB was to
promote improvements to heating, bathrooms, kitchens
and windows.
Methods and measures
The analysis entails the estimation of a series of
regression models specified with variables collected from
both the baseline and follow-up surveys. In these
models, the dependent variable is the GHQ12 score
which is taken to be indicative of the degree of mental
distress. This measure is a 12-item screening instrument
covering a range of psychiatric symptoms such as
anxiety, depression, somatic and social dysfunction.
These items are ‘been unable to concentrate on whatever
you’re doing’, ‘lost much sleep over worry’, ‘felt you
were not playing a useful part in things’, ‘felt incapable
of making decisions about things’, ‘felt constantly under
strain’, ‘felt you couldn’t overcome your difficulties’,
‘been unable to enjoy your normal day to day activities’,
‘been unable to face up to your problems’, ‘been feeling
unhappy or depressed’, ‘been losing confidence in
yourself’, ‘been thinking of yourself as a worthless
person’ and ‘been feeling reasonably unhappy all things
considered’. Each of these items is presented to the
respondent on a four-point scale containing two
gradations of ‘problem’–‘no problem’. A value of one
is added to the GHQ12 score if the respondent rated
either of the ‘problem’ gradations and where a final
score greater than two indicates a mental health problem
with high sensitivity and specificity (Goldberg &
Williams, 1988).
Independent variables have been chosen to represent
individual susceptibility to mental distress and the
respondent’s status with regard to the SRB and the
receipt of housing improvement during the episode
between the surveys. The susceptibility of the individual
is reflected by variables measuring the age of the
respondent (AGE) and number of restricted opportu-
nities (RO) reported to be incident on the date of survey.
More specifically, RO was constructed as an indicator of
psychosocial risk and was measured on an eight-point
scale counting positive responses to the following items:
‘lacked money to enjoy life’, ‘like more leisure but
cannot’, ‘more active social life but unable to’, ‘wanted
to move but could not’, ‘wanted to improve living
conditions but could not’, ‘wanted to improve person
safety but could not’, ‘wanted to participate in family
activity but could not’, and ‘wanted help with health
problems but could not get it’.
The justification for this parsimonious choice of two
susceptibility indicators is based upon a previous
analysis of the baseline survey (Thomas et al., 2002)
that estimated regression relationships between GHQ12
ARTICLE IN PRESSR. Thomas et al. / Social Science & Medicine 60 (2005) 2773–2783 2777
and an array of variables representing facets of both
structural and psychosocial risk.2 Here, AGE and RO
were found to be the dominant explanatory factors for
the variation in GHQ12. In addition, RO was the one
psychosocial construct that correlated strongly with the
indicators of structural risk and, therefore, serves as a
useful proxy for this variation in the present reduced
analysis. Moreover, in this analysis, RO is always
measured as the count reported at the time of the
baseline survey. This specification is made to avoid the
possibility that the scoring of the constituent items of
RO might be affected by mental health problems
encountered after this date. For this reason, such
problems are anticipated to be manifest solely in the
value of GHQ12 reported at follow-up.
The potential effects of living in the SRB intervention
zone are represented by the variable AREA, which
comprises of the two categories Mersey Bank (MB) and
Wythenshawe (W—the targeted estate). These categories
are distinguished as a dummy variable where zero
indicates residence in Mersey Bank and unity residence
in Wythenshawe. Similarly, the types of housing
improvement listed in Table 1 are represented by a
separate categorical variable that includes the generic
label IMP in its title. For each of these variables a value
of unity indicates receipt (R) of the specified improve-
ment during the intervention episode, while zero
indicates non-receipt (NR). Among this set, the central
focus of the analysis is the ‘at least one’ category, which
distinguishes between those who received some kind of
alteration to their housing and those who did not.
The independent variables described above are the
main effects selected to explain the variation in GHQ12.
The inclusion of the two dummy variables in the design,
however, allows for the possibility of their interaction
with the ratio variables AGE and RO. The functional
form of the relationship between GHQ12 and AGE in
Wythenshawe, for example, might be significantly
different from that estimated for Mersey Bank. To test
for all such outcomes, the main effects AREA and IMP
are disaggregated into the four dummy categories
labelled WR, WNR, MBR and MBNR. Thus, WR
refers to the subset of respondents in Wythenshawe in
receipt of the specified improvement while WNR
denotes the complementary Wythenshawe residents
who were non-recipients. Membership of each dummy
category is denoted by unity (MBR ¼ 1 if the respon-
dent is both resident in Mersey Bank and in receipt of
2In addition to restricted opportunities, psychosocial risk in
this study was also represented by variables measuring the
incidence of negative life events, the frequency of goal setting
behaviours and the quality of life, while structural risk included
measures of individual socio-economic deprivation and perso-
nal vulnerability. The analysis was derived from the 2596
respondents to the baseline survey.
the improvement) and non-membership by zero (all the
other respondents). Then, the ratio variables are
themselves disaggregated according to these dummy
specifications. AGE, for example, can be partitioned
into the interaction variables AGE(WR), AGE(WNR),
AGE(MBR) and AGE(MBNR). Accordingly,
AGE(MBR) contains the ages of those respondents
who are members of MBR and zero otherwise. To
execute the regression analysis one of the interaction
categories is specified as a fixed effect against which the
significance of the relationships with the other categories
is assessed (Johnston, 1980). Throughout, this fixed
category is MBNR. The regression coefficients estimated
for the dummy categories (WR etc.) are intercepts (a)expressed in units of GHQ12, while those for the
interaction variables [AGE(WR) etc.] are b-values
describing the direction and strength of their relation-
ship with GHQ12.
The following analysis first examines regression
relationships involving the main effects and then tests
the significance of the interactions associated with the
AGE and RO variables. The presentation is cross-
sectional in style and entails a comparison of results
obtained from models where the dependent variable is
GHQ12 at baseline and those where this specification is
replaced by the score reported at follow-up.
Results
Main effects models
Bivariate regression statistics estimated by OLS for
the relationship of each main effect variable with
GHQ12 at both baseline (t1) and follow-up (t2) are
listed in Table 2. At both dates, AGE and RO display
highly significant relationships with GHQ12 with larger
adjusted R2 values estimated for the baseline variables.
RO is positively associated with GHQ12 and, typically,
explains about 15% of the variation in this score. By
contrast the reporting of symptoms of distress declines
with AGE and this relationship explains about 2% of
the variation in GHQ12.
At t1, the bivariate regression for the AREA effect
(b ¼ 0.278) is not significant (p ¼ 0.110). This b-value
refers to the difference between the mean GHQ12 score
in Wythenshawe [a(W, t1) ¼ 2.528] and the mean score
in Mersey Bank [a(MB, t1) ¼ 2.250] and this insignif-
icant prior outcome is some justification for our
selection of the Mersey Bank estate as a control for
the SRB intervention in Wythenshawe. At t2 the AREA
effect (b ¼ 0.314) is of modest significance (p ¼ 0:079)
and the mean GHQ12 score for Wythenshawe residents
(2.621) is greater than that estimated for Mersey Bank
(2.307). The bivariate regressions for the At least 1 IMP
effect are significant at t1 (b ¼ 0.411, p ¼ 0.019) and t2
ARTICLE IN PRESS
Table 3
Paired sample t–tests for the difference between mean GHQ12 scores at baseline (t1) and at follow-up (t2) for each categorical effect
Effect GHQ12(t1) mean GHQ12(t2) mean Mean difference (t2– t1) t–Statistic Exact significance
AREA:
MB 2.250 2.307 0.057 0.322 0.747
W 2.528 2.621 0.093 0.457 0.647
At least 1 IMP:
NR 2.217 2.309 0.092 0.620 0.535
R 2.628 2.681 0.053 0.121 0.904
Total 2.409 2.459 0.050 0.556 0.578
Table 2
Bivariate regressions for the main effects as predictors of GHQ12 at baseline (t1) and at follow-up (t2)
Effect a b Exact significance R2 Exact significance
(a) GHQ12(t1)
AGE 3.384 �0.028 0.000 0.023 0.000
RO(t1) 0.218 0.619 0.000 0.172 0.000
AREA:
MB 2.250
W 2.528 0.278 0.110 0.001 0.110
At least 1 IMP:
NR 2.217
R 2.628 0.411 0.019 0.003 0.019
(b) GHQ12(t2)
AGE 3.730 �0.024 0.000 0.017 0.000
RO(t1) 0.589 0.535 0.000 0.123 0.000
AREA: 2.307
MB 2.621 0.314 0.079 0.002 0.079
W
At least 1 IMP:
NR 2.309
R 2.681 0.372 0.039 0.002 0.039
Exact significance: for the AREA and At least 1 IMP effects this probability refers to the difference between the intercept terms, that is
b(W) ¼ a(W)–a(MB). These intercepts are the mean GHQ12 score for the given category.
R. Thomas et al. / Social Science & Medicine 60 (2005) 2773–27832778
(b ¼ 0.372, p ¼ 0.039). For both regressions, the mean
GHQ12 score for the receipt category (R) are greater
than the mean scores for those in the NR category. Since
membership of R refers to receipt of an improvement in
the episode after the baseline survey, the significant
difference estimated at t1 indicates those in the R
category maintained higher scores than those in NR
before any receipt of an actual housing improvement.
The regression statistics reveal differences between the
category effects at a specified survey date but do not test
for the change in the mean scores observed for a single
category on the these dates. The latter differences are
tested by paired sample T-statistics (Table 3). The results
are all insignificant and indicate a high degree of
stability between the mean GHQ12 scores observed for
each category over the study period. The same outcome
occurs for the mean scores for the entire sample (Total)
where the insignificant change in GHQ12 (0.050) is
positive over the interval from t1 to t2. The correlation
coefficient for the GHQ12 scores at t1 and t2 is 0.487
(p ¼ 0.000).
Models with interaction effects
The significant differences between the main cate-
gories at specific survey dates suggest the possibility of
their interaction with both RO and AGE. In this respect,
the regression model for the disaggregation of RO
ARTICLE IN PRESS
Table 4
Multiple regressions for AGE interactions with AREA�At least 1 IMP as predictors of GHQ12 at baseline (t1) and at follow-up (t2)
Effect a b Exact significance R2 Exact significance
(a) GHQ12(t1)
AREA�At least 1 IMP:
MBNR 2.813
MBR 4.613 1.800 0.018
WNR 4.168 1.35 0.066
WR 4.274 5.461 0.041
AGE(AREA�At least 1 IMP):
MBNR �0.015 0.092
MBR �0.039 0.084
WNR �0.034 0.160
WR �0.031 0.211
Model 0.028 0.000
(b) GHQ12(t2)
AREA�At least 1 IMP:
MBNR 2.868 0.396 0.612
MBR 3.264 1.586 0.037
WNR 4.454 1.736 0.019
WR 4.604
AGE(AREA�At least 1 IMP):
MBNR �0.013 0.137
MBR �0.013 0.984
WNR �0.038 0.077
WR �0.034 0.114
Model 0.021 0.000
Exact significance: for the AREA�At least 1 IMP effects this probability refers to the difference between the intercept term and the
corresponding fixed effect, that is b(.) ¼ a(.)–a(MBNR). For the AGE(AREA�At least 1 IMP) interactions the probability refers to
the difference term Db(.) ¼ b(.)–b(MBNR). In (b), for example, Db(WR) ¼ b(�0.034)–b(�0.013) ¼ �0.21.
R. Thomas et al. / Social Science & Medicine 60 (2005) 2773–2783 2779
according to the categorical effects revealed no sig-
nificant interactions with GHQ12 either at t1 or t2 (not
illustrated). The regression models for the AGE(AR-
EA�At least 1 IMP) interactions, however, yielded
more positive outcomes (Table 4). Here, the intercepts
(a) are the estimated value of GHQ12 when AGE ¼ 0.
The b-coefficients for the AGE interactions are all
negative and denote the decrement to the value of their
respective intercept that is consequent upon each
additional year of life. Accordingly, these intercepts
and b-coefficients describe the linear relationship be-
tween GHQ12 and AGE for each of the interaction
effects. These relationships are visualised in Fig. 1 for
the regression models (a) estimated at baseline (b) and
follow-up.
The functional form of these interactions is seen to
differ at the survey dates. At t1, the significance statistics
(Table 4a) distinguish between relationship obtained for
the MBNR category and the functional forms obtained
for the three remaining categories. The predicted values
of GHQ12 estimated for MBNR are lower than the rest
and are subject to a reduced b-coefficient for the
negative effect of AGE (Fig. 1a). At t2, however, the
inter-relations between the categories are more symme-
trical. Compared to those for both MB categories, the
equivalent functions for Wythenshawe are subject to
both higher intercept values (increased predicted
GHQ12) and steeper b-coefficients for the AGE effect
(Fig. 1b). Moreover, the intercept values estimated for
the non-receipt categories (MBNR and WNR) are less
than the values obtained for the corresponding receipt
categories (MBR and WR). Despite this more regular
outcome, the estimate of R2¼ 0.021 obtained for the t2
regression model explains less of the variation in
GHQ12 than the t1 model (R2¼ 0.028).
The preceding analysis has identified the separate
significance of the hypothesised sources of variation in
GHQ12 at both baseline and follow-up. The regression
model listed in Table 5 examines the effects of these
sources in combination by specifying RO and the
AGE(AREA�At least 1 IMP) interactions as the
predictors of GHQ12 at t2 (Table 5). The adjusted
value of R2¼ 0.125 compares with the estimate of
R2¼ 0.123 (Table 2b) obtained when RO was specified
as the single predictor of GHQ12(t2). Thus, RO
accounts for the majority of the variation in these scores
ARTICLE IN PRESS
(a)
(b)
Fig. 1. AGE(AREA�At least 1 IMP) interation plots against
(a) predicted GHQ12 at baseline (b) and at follow-up.
Table 5
Multiple regression for RO and the AGE(AREA�At least 1 IMP) i
Effect a b
AREA�At least 1 IMP:
MBNR 0.508 �0.009
MBR 0.499 1.176
WNR 1.684 1.392
WR 1.900
AGE(AREA�At least 1 IMP):
MBNR 0.001
MBR 0.004
WNR �0.020
WR �0.022
RO(t1) 0.514
Model
Exact significance: for the AREA�At least 1 IMP effects this probab
corresponding fixed effect, that is b(.) ¼ a(.)–a(MBNR). For the AGE
the difference term Db(.) ¼ b(.)–b(MBNR).
R. Thomas et al. / Social Science & Medicine 60 (2005) 2773–27832780
while the AGE interaction retains a degree of signifi-
cance. The functional form of the categorical relation-
ships, however, is altered in the presence of RO (Fig. 2).
In this last respect, the intercept terms in the
combined model refer to the predicted value of
GHQ12 for each category when both AGE and RO
are zero. For the Mersey Bank categories (MBR,
MBNR) neither their intercepts nor their b-coefficients
are significantly different from zero (Table 5). The
intercepts for the Wythenshawe categories (WR, WNR),
however, are both positive and retain similar negative
AGE gradients. The inclusion of RO in this specifica-
tion, therefore, subsumes the previously identified age
effect among MB residents and the lower predicted
GHQ12 values estimated for those in the NR categories.
These differences are evident from the Fig. 2, where the
Wythenshawe categories are those that display a similar
negative relationship with AGE.
For completeness, Table 6 provides statistics for
combined regression models where the IMP category
has been re-specified for each type of housing improve-
ment that was promoted by the SRB initiative. In
general, the statistics estimated in these regression
models are quite consistent with those obtained for the
At least 1 IMP specification. The degrees of model
explanation (R2) and contributions of the RO variable
are virtually identical and the intercepts their
b-coefficients for the Mersey Bank AGE interactions
are not significantly different from zero. The Wythen-
shawe categories maintain the negative AGE gradient
although the strength of this relationship varies across
the WR and WNR categories. In the Bathroom IMP
regression the strongest relationship is estimated
for the WR category whereas, for the other types of
nteractions as predictors of GHQ12(t2)
Exact significance R2 Exact significance
0.990
0.102
0.046
0.876
0.813
0.107
0.069
0.000
0.125 0.000
ility refers to the difference between the intercept term and the
(AREA�At least 1 IMP) interactions the probability refers to
ARTICLE IN PRESSR. Thomas et al. / Social Science & Medicine 60 (2005) 2773–2783 2781
improvement, this outcome is associated with the WNR
category.
Discussion
Better mental health was not a specific target of the
SRB intervention in Wythenshawe. Yet, our first ideas
about this matter were predicated upon the expectation
that such an extensive investment in the socio-economic
infrastructure would indirectly improve mental health
within this community. The analysis presented in this
paper was designed to investigate this broad hypothesis
with particular regard to the potential benefits of
Fig. 2. RO and the AGE(AREA�At least 1 IMP) interactions
plotted against predicted GHQ12 at follow-up.
Table 6
Regression models for each SRB housing improvements as predictor
IMP WR WNR
Heating a 0.706 1.956
ba�0.013 �0.024
Bathroom a 2.173 1.683
ba�0.025 �0.020
Kitchen a 0.982 1.858
ba�0.009 �0.022
Windows a 1.792 1.779
ba�0.018 �0.022
At least 1 a 1.900 1.684
ba�0.022 �0.020
Independent variables are RO and the AGE(AREA� IMP) interacti
Bold indicates a coefficient is significant at pr0.05. Italics indicates aaThe first four values in each row are age b�-coefficients, the fifth i
At least 1 IMP regression are also listed in Table 5 which provides a
housing improvement. The following interpretation of
the results, however, provides evidence that is often
counter to this expectation.
The regression results demonstrate in sequence how
housing improvement activity and indicators of pyscho-
social risk combine to affect the reporting of mental
distress by the surveyed residents. In this respect, the
GHQ12 scores reported by those in Wythenshawe SRB
zone are of special interest. In the bivariate regression at
baseline, their mean score is not significantly different
from that estimated for Mersey Bank residents while, at
follow-up, this difference is significant and positive. The
latter outcome persists both in the separate analysis of
the AGE interactions and in the combined model. One
implication of this difference is that the reporting of
mental distress among Wythenshawe residents was
disturbed by the implementation of the SRB. It is quite
possible these residents experienced a degree of stress
from local environmental nuisance that was attributable
to enhanced improvement activity on the estate. This
additional stress is more evident among younger
Wythenshawe residents and tends to dissipate in those
over 60 years of age.
The results obtained for the housing improvement
effect are more ambiguous. At baseline, for example,
those who subsequently received at least one type of
improvement reported additional symptoms of stress
irrespective of their residential estate. Such an outcome
could be interpreted as a structural effect related to
living in a house in need of repair. The persistence of this
enhanced stress at follow-up, however, might be
attributable to the disruption to home life engendered
by house improvement. The clearer delineation between
the R and NR categories obtained for the separate
analysis of the AGE interactions at follow-up (Fig. 1b)
would appear to add weight to the case for such
s of GHQ12 at follow-up
MBR MBNR RO(t1) R2
0.366 0.556 0.127
0.011 0.000 0.515
1.898 0.336 0.127
�0.028 0.005 0.518
�0.163 0.516 0.126
0.008 0.002 0.519
0.454 0.521 0.126
0.008 0.001 0.517
0.499 0.508 0.125
0.004 0.011 0.514
ons.
coefficient is significant in the range pr0.10, p40.05.
s the restricted opportunities b- coefficient. The statistics for the
key for the other regression results given above.
ARTICLE IN PRESSR. Thomas et al. / Social Science & Medicine 60 (2005) 2773–27832782
disruption. This distinction, however, is largely absent in
the combined model estimates when the restricted
opportunities variable is included in the specification.
A clearer interpretation of these improvement effects
might have been possible had the mean GHQ12 scores
for the categorical variables altered between the two
survey dates. Their stability over this interval (Table 3),
however, indicates the nuisance effect served only to re-
distribute these category means at each specific date.
Moreover, the local leverage of this environmental effect
on GHQ12 scores is small in comparison to that
estimated for the reporting of restricted opportunities.
Predicted GHQ12 at t2, for example, increases from
about 0 to 6 within the reporting range of RO (0 to 8
items) compared to the unit response exhibited by the
negative AGE interactions for Wythenshawe residents
(see Fig. 2).
Thus, the results of our analysis suggest better mental
health outcomes are associated with low personal
assessments of psychosocial risk (RO). In contrast, the
effects of housing improvement tend to be detrimental.
From the policy perspective, this evidence indicates
structural investment is unlikely to reduce the reporting
of symptoms of mental distress and, instead, a surer
strategy to achieve this aim is to devise interventions
that target the incidence of psychosocial risk. Such a
conclusion, however, must be tempered by limitations of
the present research design. The follow-up survey was
undertaken 22 months into the duration of the SRB and,
therefore, captured only the immediate impacts of this
intervention. The long-term impacts on residents of
these structural changes remain to be established.
Similarly, the relatively low response rates to our surveys
might influence the generality of our findings with
regard to the populations from which they were drawn.
Finally, the research presented here was complemen-
ted by in-depth interviews with a sub-sample of the
residents during the intervention episode. These findings
will be reported elsewhere (Rogers, Gately, Evans,
Huxley, & Thomas, 2005), however, some of the issues
they raised are pertinent to the current discussion. Many
of these respondents referred to a lack of opportunities
on the estates and, in particular, expressed concern
about the poor provision of play and leisure facilities for
children and youth, the reputation of the area, and
restrictions on travel, especially at night. They also
suggested the perceived benefits of housing improve-
ments were viewed as constituting cosmetic changes
when compared to the quality of private housing being
built within the same area. Others pointed out that
substantial alterations had been made by tenants
themselves and there was a fear of increased rental
charges which was a seemingly negative outcome to be
set against making improvements. Therefore, they
regarded the structural changes we measured as both
modest and insufficient to match their expectations for
the intervention. Accordingly, targeting such concerns
prior to the implementation of urban regeneration
initiatives might precipitate more decisive mental health
outcomes than those reported here.
Acknowledgement
The research in this paper was funded by ESRC
research award L128 25 1041 whose support we grate-
fully acknowledge.
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