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Socioeconomic status, financial hardship and measured obesity in older adults: a cross-sectional study of the EPIC-Norfolk cohort
https://doi.org/10.1186/1471-2458-13-1039
© Conklin et al.; licensee BioMed Central Ltd. 2013
Received: 7 August 2013
Accepted: 24 October 2013
Published: 4 November 2013
Abstract
Background
Socioeconomic status is strongly associated with obesity. Current economic circumstances are also independently associated with self-reported weight status in Finnish civil servants. We aimed to examine three types of financial hardship in relation to measured general and central obesity in a general population of older adults, while considering conventional socioeconomic indicators.
Methods
Data from 10,137 participants (≥50 years) in the EPIC-Norfolk cohort who responded to a postal Health and Life Experiences Questionnaire (1996–2000) and attended a clinical assessment (1998–2002). Multivariable logistic regression models assessed likelihood of general obesity (BMI ≥30 kg/m2) and central obesity (women: ≥88 cm; men: ≥102 cm) calculated from measured anthropometrics.
Results
Obesity prevalence was consistently patterned by standard socioeconomic indicators, with over-50s in the lowest social class being twice as likely to be obese than those in the highest class (women OR 2.10 [CI95: 1.41—3.13]; men OR 2.36 [1.44—3.87]). After adjustment for socioeconomic status, reporting having less than enough money for one’s needs (compared to more than enough) was associated with obesity in women (OR 2.04 [1.54—2.69]) and men (OR 1.83 [1.34—2.49]). Similar associations were demonstrated between obesity and always or often not having enough money for food/clothing (women OR 1.40 [1.03—1.90]; men OR 1.81 [1.28—2.56]), compared to reporting this never occurred. The strongest independent associations were seen for obesity and reported greatest level of difficulty paying bills (women OR 2.20 [1.37—3.55]; men 2.40 [1.38—4.17]), compared to having no difficulties. Findings for central obesity were slightly higher in women and lower in men.
Conclusions
Obesity in British over-50s was more likely in study participants who reported greater financial hardship, even after education, social class and home ownership were taken into account. Public health policies need to consider the hitherto neglected role of financial hardship in older people, especially difficulty paying bills, as part of strategies to prevent or reduce obesity.
Keywords
Background
Obesity is one of the biggest public health challenges faced by high income countries, accounting for a large and growing disease burden (cardiovascular disease, type 2 diabetes, some cancers) and imposing substantial cost burden on both the healthcare system and society at large [1–3]. Both general (weight status) and central (excess abdominal fat) obesity significantly increase a person’s risk of, for example, cardiometabolic conditions [4]. Obesity is strongly and inversely related to socioeconomic status (SES) as measured by conventional indicators of education or social class, particularly in the case of women [5–7]. But, conventional SES has been acknowledged as insufficient to understand how a person’s economic situation is associated with their body mass index (BMI) or waist circumference (WC) [8], and differences in obesity by education or income are not consistently observed in UK adults [9].
A limitation with conventional SES indicators is that they do not fully capture people’s material circumstances and spending power, whereas everyday financial troubles may be a stronger antecedent to obesity than income, occupational status, or education [8, 10]. Wider research on poverty has highlighted the added value of material hardship measures to concepts of inequality [11]. Evidence from two occupational cohorts supports the notion that financial hardship reflects a distinct set of economic factors that independently impacts health beyond the reported influence exerted by conventional SES [8, 10, 12–15]. Another study found an association between financial hardship and smoking even within high-income groups [16]. To date, one longitudinal study of US adolescents explored separate types of financial hardship and found suggestive evidence that having trouble paying bills may be related to obesity in women, but not men [17].
Financial hardship is closely correlated, but not interchangeable, with conventional SES and therefore deserves specific attention [18]. Since individuals at all income levels can experience financial hardship with consequent health effects, the implications for public health and policy are that income (or other standard SES indicators) should not be seen as the sole criteria for targeting interventions [12, 18–20]. One of the largest drains on disposable income, especially in older people, is paying bills and affording adequate food and clothing [21], and yet, health research and policy has tended to neglect current financial difficulties as a unique economic domain determining health. Consequently, evidence remains limited on the role of financial hardship in obesity and whether separate types of hardship differ in their associations with obesity, particularly among older adults who comprise a growing population [8, 19, 22]. Older adults with greater hardships may purchase less food and have lower weights due to fewer calories; however, they may also purchase cheaper food high in energy density which could contribute to excess weight.
We therefore investigated the sex-specific associations between three types of self-reported financial hardships and obesity measured objectively in adults aged 50 and older. We hypothesised that greater levels of financial hardship may be associated with greater odds of obesity, overall and centrally, with sex differences in magnitude of associations. We further hypothesised that associations would remain significant after adjusting for conventional socioeconomic status.
Methods
Study population
We used data collected as part of the EPIC-Norfolk prospective cohort study—a component of the European Prospective Investigation of Cancer (EPIC) study in 10 European countries [23]. As we were interested in adults near the end of working life and beyond to place findings in a healthy ageing context, we included over-50s (n = 20,274) from the population-based cohort who were recruited from age-sex registers of general practices and who attended a first health check at entry (1993–97). At entry, over-50s were similar to the total cohort (n = 25,639) in terms of health behaviours and other socio-demographic factors. Ethnicity of 99.7% of EPIC-Norfolk participants was of white origin.
Financial hardship was assessed using the postal “Health and Life Experiences Questionnaire” (HLEQ) (1996–2000) designed to assess social and psychological circumstances [24, 25]. Completed responses from over-50s ranged between 17,953 and 17,998. Outcome data on BMI (n = 11,982) and WC (n = 12,000) were measured objectively during a second clinical assessment (1998–2002). Our available sample therefore included over-50s who responded to financial hardship questions, had covariates and follow-up anthropometry (range: 10,113—10,137) with 99% complete data (see Additional file 1: Figure S1). The sample was similar in characteristics and lifestyle to responders in the full cohort, and over-50s not responding to hardship questions were similar to cohort non-responders. All volunteers gave written informed consent and the study was approved by the Norwich district ethics committee.
Measures
Financial hardship and conventional socioeconomic indicators
Financial hardship was measured by three self-reported questions in line with Pearlin’s list of chronic strains as used in similar studies [12, 20]. Questions covered sufficiency of money to meet needs (more than enough, just enough, less than enough), frequency of not having enough money to afford adequate food or clothing (5 responses, range 'always’ to 'never’), and difficulty paying bills (6 responses, range 'very great’ to 'none’). Responses 'always’ and 'often’ , or 'great’ and 'very great’ , were combined for analysis due to low numbers in the bottom two categories.
We analysed three conventional indicators of SES. Education level (no qualification, O-level (16 years), A-level (18 years), degree (>18 years)) and occupation were self-reported at cohort entry, with occupation used to classify participants into six hierarchical categories of the Registrar General’s classification scheme of social class (professional, managerial and technical, skilled non-manual, skilled manual, partly skilled, and unskilled). Social class in women was based on her partner’s occupation (68%) unless it was unclassified, missing, or they were single and then her own occupation was used [26]. We also employed a measure of housing tenure (home-owner, public renting, private renting) as a conventional SES proxy, given that previous research has documented the utility of home ownership as a measure of wealth in older populations [27].
Obesity
Trained nurses used standardised protocols to measure weight, height, and WC of all participants attending the second clinic assessment, as reported elsewhere [26, 28]. BMI was calculated as weight in kilograms divided by the square of height in metres. Participants who had a BMI ≥ 30 kg/m2 were classified as obese overall. Central obesity was calculated using sex-specific threshold criteria for WC: women with WC ≥ 88 cm and men with WC ≥ 102 cm were classified as centrally obese.
Socio-demographic variables
Participants self-reported smoking status (current, former, never), marital status (married/living as married, single, widowed, separate, divorced), and general health status (excellent, good, moderate, poor), at second health check (1998–2002). Regular car use (yes/no) was self-reported in the Environment and Physical Activity questionnaire (EPAQ2) (1998–2000). Socio-demographic variables for date of birth (continuous age) and sex were measured at cohort entry.
Data analysis
Descriptive statistics summarised socio-demographic characteristics (sex, education, social class, home-ownership, car use, health status, smoking status, marital status), and crude prevalence of obesity across financial hardship levels. We used a correlation matrix to examine inter-relationships among the financial hardship indicators after recoding two indicators into three levels: frequency of not having enough money for food or clothing (never; sometimes/seldom; often/always), and difficulty paying bills (none; very little/slight; some/great/very great). Odds ratios of prevalent obesity for the six socioeconomic indicators were examined by fitting logistic regression models a priori sex-stratified and adjusted for age, smoking status and marital status. As known confounders, each is associated with socioeconomic factors and independently with obesity [29–32].
For each categorical measure of financial hardship, we fitted sequential logistic regression models to base models (sex-stratified and adjusted for age, smoking and marital status); first by education, followed by occupational social class, and then housing tenure. The final model for each hardship indicator mutually adjusted for all conventional SES and covariates and therefore the remaining sex-specific odds ratios for general and central obesity were interpreted as independent associations of the financial hardship variable in question.
In secondary analyses, we further adjusted for concurrent lifestyle variables: total energy intake (Kcal), total alcohol consumption (units/week), and physical activity and energy expenditure (PAEE) score. Self-reported total energy and alcohol intake were assessed by food frequency questionnaire [33]; and PAEE by the EPAQ2 questionnaire, previously validated against individually calibrated heart rate against energy expenditure [34]. For women, we also adjusted for menopause and HRT status in secondary models.
Statistical analyses were performed separately for women and men using Stata 12.1 [35]. Results are presented as odds ratios (ORs) and 95 percent confidence intervals (95% CIs).
Results
The mean age of participants was 62.5 years (SD 7.5) with 54% of the sample made up of women. A majority (81%) reported being in good or excellent general health, and 51% were ever smokers. For the whole sample, 11% were educated to degree-level; 14% of men and 9% of women were educated to this level. Professional (class I), and managerial and technical (class II), occupations comprised 42% of the sample; few women (4%) and men (3%) had unskilled occupations. Mean BMI was 27 kg/m2 (SD 3.3) in men, and 26.8 kg/m2 (SD 4.4) in women; 16% of men and 20% of women were classified as obese overall. Women’s average WC was 82.9 cm (SD 10.6) and men’s was 96.7 cm (SD 9.6); 29% of women and 27% of men were classified as being centrally obese.
There was a close inter-relationship between the three measures of self-reported financial hardship and other socio-demographic measures (see Additional file 1: Table S2). We found that the three financial hardship measures were moderately related to each other. The indicator having enough money for needs shared 23% and 26% of its variability with the indicators frequency of not having enough money for food or clothing (r = 0.48) and difficulty paying bills (r = 0.51), respectively. Frequency of not having enough money for food or clothing shared 38% of its variability with difficulty paying bills (r = 0.62).
Conventional SES indicators and odds of obesity
Odds ratios of general and central obesity in women and men (≥50 years) across levels of social class, education, and housing tenure in the EPIC-Norfolk cohort
General obesity | Central obesity | |||
|---|---|---|---|---|
Women | Men | Women | Men | |
Social Class | (n = 6320) | (n = 5277) | (n = 6327) | (n = 5286) |
I | 1.00 | 1.00 | 1.00 | 1.00 |
II | 1.29 (0.96, 1.72) | 1.33 (0.96, 1.84) | 1.11 (0.88, 1.41) | 1.08 (0.85, 1.37) |
III–non manual | 1.23 (0.90, 1.66) | 1.57 (1.09, 2.26) | 0.99 (0.77, 1.28) | 1.13 (0.86, 1.49) |
III–manual | 1.49 (1.10, 2.02) | 1.53 (1.09, 2.14) | 1.10 (0.85, 1.41) | 1.03 (0.80, 1.34) |
IV | 2.10 (1.53, 2.86) | 1.36 (0.94, 1.96) | 1.41 (1.08, 1.84) | 1.10 (0.83, 1.45) |
V | 2.10 (1.41, 3.13) | 2.36 (1.44, 3.87) | 1.57 (1.11, 2.22) | 1.47 (0.97, 2.24) |
Education | (n = 6464) | (n = 5353) | (n = 9531) | (n = 6327) |
Degree | 1.00 | 1.00 | 1.00 | 1.00 |
A-level | 1.16 (0.92, 1.46) | 1.48 (1.28, 2.15) | 1.12 (0.92, 1.36) | 1.17 (0.97, 1.42) |
O-level | 1.33 (1.01, 1.74) | 1.27 (0.90, 1.78) | 1.07 (0.84, 1.36) | 1.27 (0.98, 1.65) |
No qualification | 1.59 (1.27, 1.99) | 1.66 (1.28, 2.15) | 1.38 (1.14, 1.67) | 1.42 (1.16, 1.73) |
Housing tenure | (n = 5727) | (n = 4706) | (n = 5734) | (n = 4712) |
Owner | 1.00 | 1.00 | 1.00 | 1.00 |
Renting, private | 1.49 (1.02, 2.17) | 1.85 (1.20, 2.85) | 1.41 (1.00, 1.99) | 1.43 (0.97, 2.11) |
Renting, public | 1.49 (1.15, 1.92) | 1.70 (1.22, 2.35) | 1.66 (1.32, 2.08) | 1.69 (1.27, 2.24) |
Further adjustment for total energy intake, physical activity and alcohol intake attenuated or made little difference to most of the associations between conventional SES indicators and obesity (see Additional file 1: Table S3). Addition of menopause and HRT status made no difference to overall magnitude or direction of findings for women (data not shown).
Financial hardship and odds of obesity
Odds ratios of general obesity across levels of financial hardship in women and men (≥50 years) in the EPIC-Norfolk cohort
Women | ||||
|---|---|---|---|---|
Model A | Model B: A + education | Model C: B + social class | Model D: C + housing tenure | |
Enough money for needs | ||||
More than enough | 1.00 | 1.00 | 1.00 | 1.00 |
Just enough | 1.50 (1.24, 1.81) | 1.39 (1.15, 1.69) | 1.36 (1.12, 1.65) | 1.34 (1.10, 1.64) |
Less than enough | 2.56 (1.98, 3.33) | 2.32 (1.78, 3.03) | 2.20 (1.68, 2.88) | 2.04 (1.54, 2.69) |
Frequency of not enough money | ||||
Never | 1.00 | 1.00 | 1.00 | 1.00 |
Seldom | 1.41 (1.21, 1.66) | 1.38 (1.18, 1.62) | 1.36 (1.16, 1.60) | 1.35 (1.14, 1.59) |
Sometimes | 1.64 (1.36, 1.98) | 1.57 (1.30, 1.90) | 1.53 (1.26, 1.85) | 1.44 (1.18, 1.76) |
Often/Always | 1.68 (1.26, 2.25) | 1.57 (1.18, 2.10) | 1.54 (1.15, 2.06) | 1.40 (1.03, 1.90) |
Difficulty paying bills | ||||
None | 1.00 | 1.00 | 1.00 | 1.00 |
Very little | 1.38 (1.18, 1.62) | 1.37 (1.16, 1.60) | 1.33 (1.13, 1.56) | 1.32 (1.12, 1.56) |
Slight | 1.78 (1.41, 2.25) | 1.75 (1.39, 2.21) | 1.76 (1.39, 2.23) | 1.67 (1.32, 2.13) |
Some | 2.08 (1.66, 2.61) | 1.99 (1.59, 2.50) | 1.92 (1.53, 2.42) | 1.81 (1.43, 2.30) |
Great/Very great | 2.52 (1.60, 3.98) | 2.37 (1.50, 3.75) | 2.38 (1.50, 3.78) | 2.20 (1.37, 3.55) |
Men | ||||
Model A | Model B: A + education | Model C: B + social class | Model D: C + housing tenure | |
Enough money for needs | ||||
More than enough | 1.00 | 1.00 | 1.00 | 1.00 |
Just enough | 1.28 (1.02, 1.59) | 1.22 (0.97, 1.53) | 1.18 (0.94, 1.48) | 1.17 (0.93, 1.47) |
Less than enough | 2.13 (1.59, 2.85) | 2.00 (1.49, 2.69) | 1.93 (1.43, 2.61) | 1.83 (1.34, 2.49) |
Frequency of not enough money | ||||
Never | 1.00 | 1.00 | 1.00 | 1.00 |
Seldom | 1.32 (1.09, 1.60) | 1.30 (1.07, 1.57) | 1.29 (1.06, 1.56) | 1.30 (1.07, 1.59) |
Sometimes | 1.30 (1.01, 1.66) | 1.26 (0.98, 1.62) | 1.24 (0.97, 1.60) | 1.15 (0.88, 1.49) |
Often/Always | 2.04 (1.47, 2.84) | 1.98 (1.42, 2.76) | 1.93 (1.38, 2.71) | 1.81 (1.28, 2.56) |
Difficulty paying bills | ||||
None | 1.00 | 1.00 | 1.00 | 1.00 |
Very little | 1.05 (0.87, 1.28) | 1.04 (0.86, 1.27) | 1.04 (0.85, 1.26) | 1.02 (0.84, 1.24) |
Slight | 1.18 (0.87, 1.60) | 1.17 (0.86, 1.59) | 1.17 (0.86, 1.58) | 1.13 (0.83, 1.55) |
Some | 1.61 (1.21, 2.15) | 1.58 (1.18, 2.11) | 1.54 (1.15, 2.06) | 1.39 (1.02, 1.88) |
Great/Very great | 2.48 (1.45, 4.26) | 2.43 (1.42, 4.18) | 2.51 (1.46, 4.34) | 2.40 (1.38, 4.17) |
Odds ratios of central obesity across levels of financial hardship in women and men (≥50 years) in the EPIC-Norfolk cohort
Women | ||||
|---|---|---|---|---|
Model A | Model B: A + education | Model C: B + social class | Model D: C + housing tenure | |
Enough money for needs | ||||
More than enough | 1.00 | 1.00 | 1.00 | 1.00 |
Just enough | 1.55 (1.31, 1.83) | 1.48 (1.25, 1.75) | 1.50 (1.26, 1.78) | 1.50 (1.26, 1.78) |
Less than enough | 2.51 (1.99, 3.18) | 2.37 (1.86, 3.00) | 2.32 (1.82, 2.97) | 2.16 (1.68, 2.78) |
Frequency of not enough money | ||||
Never | 1.00 | 1.00 | 1.00 | 1.00 |
Seldom | 1.33 (1.15, 1.53) | 1.30 (1.13, 1.50) | 1.29 (1.12, 1.49) | 1.29 (1.11, 1.49) |
Sometimes | 1.49 (1.26, 1.77) | 1.45 (1.22, 1.72) | 1.44 (1.21, 1.71) | 1.38 (1.15, 1.65) |
Often/Always | 1.76 (1.36, 2.29) | 1.69 (1.30, 2.19) | 1.65 (1.26, 2.15) | 1.51 (1.15, 1.99) |
Difficulty paying bills | ||||
None | 1.00 | 1.00 | 1.00 | 1.00 |
Very little | 1.39 (1.21, 1.60) | 1.38 (1.20, 1.59) | 1.36 (1.18, 1.56) | 1.36 (1.17, 1.57) |
Slight | 1.57 (1.26, 1.94) | 1.55 (1.25, 1.92) | 1.57 (1.26, 1.95) | 1.50 (1.20, 1.87) |
Some | 1.74 (1.41, 2.15) | 1.69 (1.37, 2.09) | 1.68 (1.36, 2.08) | 1.59 (1.28, 1.99) |
Great/Very great | 2.66 (1.73, 4.08) | 2.55 (1.66, 3.92) | 2.46 (1.59, 3.82) | 2.34 (1.49, 3.67) |
Men | ||||
Model A | Model B: A + education | Model C: B + social class | Model D: C + housing tenure | |
Enough money for needs | ||||
More than enough | 1.00 | 1.00 | 1.00 | 1.00 |
Just enough | 1.19 (1.00, 1.42) | 1.14 (0.96, 1.36) | 1.16 (0.97, 1.39) | 1.14 (0.95, 1.37) |
Less than enough | 1.76 (1.38, 2.25) | 1.66 (1.30, 2.13) | 1.69 (1.31, 2.17) | 1.64 (1.26, 2.12) |
Frequency of not enough money | ||||
Never | 1.00 | 1.00 | 1.00 | 1.00 |
Seldom | 1.32 (1.13, 1.55) | 1.30 (1.11, 1.52) | 1.30 (1.11, 1.53) | 1.30 (1.11, 1.53) |
Sometimes | 1.33 (1.08, 1.63) | 1.29 (1.05, 1.58) | 1.30 (1.06, 1.60) | 1.26 (1.01, 1.56) |
Often/Always | 1.62 (1.20, 2.19) | 1.58 (1.17, 2.13) | 1.57 (1.16, 2.13) | 1.51 (1.11, 2.07) |
Difficulty paying bills | ||||
None | 1.00 | 1.00 | 1.00 | 1.00 |
Very little | 1.14 (0.98, 1.33) | 1.13 (0.97, 1.32) | 1.14 (0.98, 1.34) | 1.13 (0.96, 1.32) |
Slight | 1.25 (0.97, 1.61) | 1.24 (0.97, 1.60) | 1.25 (0.97, 1.61) | 1.24 (0.96, 1.61) |
Some | 1.53 (1.19, 1.96) | 1.50 (1.17, 1.93) | 1.47 (1.14, 1.90) | 1.35 (1.04, 1.77) |
Great/Very great | 1.48 (0.88, 2.49) | 1.45 (0.86, 2.44) | 1.53 (0.90, 2.59) | 1.49 (0.87, 2.54) |
Additional adjustment for other lifestyle variables had little effect on the measures of association either for general or central obesity (see Additional file 1: Table S4 and Table S5).
Discussion
Synopsis of results
This cross-sectional, population-based study of UK over-50s showed social class, education, and housing tenure gradients in obesity. It further demonstrated strong associations with obesity for three types of financial hardship that were independent of social class, education and housing tenure. Independent associations were particularly strong for central obesity in women compared to men.
Methodological considerations
The financial hardship variables were self-reported and like all such variables may be subject to recall or social desirability bias. Interpretation of the meaning of financial hardship can also vary widely across the population; equivalent levels of financial strain can be perceived and experienced as a normative status of daily living for some groups but as deprivation for others [19]. Precedent exists, however, for the measures used here as findings of independent associations are consistent with other studies of self-reported and objective health outcomes in similarly-aged groups [14, 19, 20]. Although financial hardship was assessed before anthropometry measurement, we could not ascertain the duration of, or transition in, hardship in relation to obesity as the survey was administered once. Thus, there may have been misclassification of exposures stemming from changes to participants’ hardship levels in the interval between assessment of financial circumstances and anthropometric measurement. Such misclassification would be non-differential since it was unlikely to have been related to our outcomes and hence would have biased results towards the null.
Our findings may also be subject to residual confounding in two ways. First, income was not collected in EPIC-Norfolk and thus we could not account for income-based differences. However, income is not consistently shown to have an impact on weight in older adults or for both sexes [36, 37], and may not sufficiently reflect structural resources in our sample of older adults since they likely also use savings to fund their expenses [38]. Our study nevertheless examined six socioeconomic indicators separately and also included education, social class and housing tenure in analyses of financial hardship. Second, parity was not analysed but may have confounded or mediated our associations between socioeconomic factors and obesity [39, 40].
Notwithstanding some limitations, the study’s strengths include a large sample size, sex-specific analyses, adjustment for multiple known confounders and lifestyle variables, and two objective obesity measures. Finally, this cohort had similar characteristics to the general UK population apart from fewer smokers and lack of ethnic diversity [23, 28], and so findings could be generalised to other white European-origin older adults.
Relationship to previous work
Our work is novel in at least three ways. First, we examined three separate financial hardship exposure measures and thus provide unique information on how different types of the financial hardship domain might be associated with higher prevalence of obesity [41]. We therefore add depth to previous studies which combined hardship questions into one summary indicator [8, 10, 14, 15, 42–45]. Second, our focus on over-50s contributes new knowledge in support of a healthy ageing agenda as no studies of economic strain and health in older populations have assessed obesity, to our knowledge [19, 22]. Third and most notably, our study is clinically relevant. We used two objective measures of obesity recommended as separate predictors of health risk, particularly central adiposity [46], rather than self-reported weight which is prone to systematic bias from inaccuracy of height and underreporting and misclassification for obese categories [47, 48].
Our finding that financial hardship showed independent associations with BMI is consistent with current evidence which notably comes from occupational cohorts [8, 14, 44]. The Helsinki Health Study of middle-aged employees, mostly women, reported increased odds of self-reported BMI for frequent financial hardship independent of conventional SES and early life factors [8], but our estimates were slightly larger. Unlike our work, that study of self-reported BMI included only age and no other BMI-related covariates associated with standard SES and obesity [49]. Another study of the same occupational cohort found a higher odds of weight gain (≥5 kg) with increasing frequency of economic difficulties after conventional SES adjustment, but again without accounting for smoking status, living arrangement or other health behaviours [10]. The Whitehall II study of financial hardship and coronary events in middle-aged men also found that a higher economic difficulties score was associated with a higher BMI and waist-hip ratio measured objectively, but the age-adjusted association did not account for conventional SES [14]. To our knowledge, no other studies of financial hardship have reported on central obesity for us to compare our findings.
Existing evidence supports the notion that social inequalities in obesity differ between the sexes with SES differences being associated more strongly and consistently with BMI in women [5–7, 50]. Sex differences have also been reported among the few studies examining financial hardship and obesity, suggesting independent associations are stronger in men [8, 10]. Notably, those results were reported in a younger population comprised of civil servants. The present study of a population-based sample of older British adults revealed contrasting results. Conventional SES proxies appeared to be more strongly and consistently associated with men’s higher odds of obesity which does not have a clear explanation. By contrast, the main associations between financial hardship and obesity were larger than SES and stronger in women. However, after adjusting for conventional SES, sex differences observed in the magnitude of associations depended on the type of hardship and obesity measure. This observed reversal between the sexes in the strength of socioeconomic disparities in obesity might point to gender-based differences in the experience of financial hardship. For example, men and women have differential vulnerabilities to financial hardship as women report not having enough money for food twice more often than men [51, 52], and they also have differential power in intra-household economics and division of labour [53, 54].
Several potential mediators might explain our finding of a link between financial hardship and obesity. Financial hardship is a powerful stressor and sociologists have shown the utility of coping and social support in explaining differences between socially and economically demarcated groups in effects of financial hardship [42, 55]. Coping behaviours, involving the manipulation of goals and values, were found to be effective for minimizing adverse effects of household financial strain, and to be used to a greater extent by socially advantaged groups, namely men, the educated, and the affluent [55]. Other potential mediators include psychological resources such as self-esteem and sense of mastery [22]. Structural factors range from consumer prices of goods and services (e.g. food, transportation) [43], and neighbourhood access to healthy foods and safe spaces for physical activity [56], to employment [57, 58] and cultural norms and social meanings reinforced through media and advertising [59, 60]. Since financial hardship was a stronger correlate of obesity than conventional SES, excess weight and abdominal fat may be more directly influenced by mechanisms related to spending power and material resources, including lack of sleep from financial worries and physiological responses to hardship-related stress, than by non-material factors such as social roles, cultural norms, and knowledge. Both chronic stress and insufficient sleep have independent associations with obesity [61–63].
Although people of all ages may encounter financial hardship, adults in older age groups are at greater risk of increased financial hardship which commonly results from events they are more likely to experience such as divorce, death of spouse, or involuntary job loss [22, 42]. Our results suggest that monetary and coping interventions may be useful in efforts to reduce obesity among over-50s. Formal mediation analyses of stress-related indicators are warranted to examine physiological mechanisms of influence between financial hardship and obesity in older women and men. Future research should also explore how both social and economic aspects of an individual’s life circumstances interact to produce combined effects on obesity as called for in the public health research and policy literature [64, 65]. Nevertheless, prevention of obesity in over-50s would benefit more from an increased focus on their experience of financial hardship in addition to their education or income levels.
Conclusions
British over-50s reporting greater levels of financial hardship were more likely to have excess weight and abdominal fat. Likelihood of obesity was more strongly correlated with financial hardship than conventional markers of SES. Thus, financial hardship indicators provided additional explanatory power beyond education, social class or home-ownership in understanding variation in prevalence of obesity in over-50 women and men. Our findings confirm that it is not sufficient to solely consider education, social class or home-ownership when examining the role of socioeconomic factors in the prevention of obesity or in weight support among older adults. Rather, public health policies and strategies need to support older people in terms of their more contemporaneous economic concerns. Interventions and practice standards to reduce or prevent obesity might include coping and monetary strategies and a focus on meeting bill payments might be a suitable target for approaches to address obesity.
Declarations
Acknowledgements
The authors thank the EPIC-Norfolk participants and staff for their contributions. AIC acknowledges PhD funding from the Gates Cambridge Trust. The work was undertaken by the Centre for Diet and Activity Research (CEDAR), a UKCRC Public Health Research Centre of Excellence. Funding from the British Heart Foundation, Economic and Social Research Council, Medical Research Council, the National Institute for Health Research, and the Wellcome Trust, under the auspices of the UK Clinical Research Collaboration, is gratefully acknowledged. EPIC-Norfolk is supported by programme grants from the Medical Research Council and Cancer Research UK. We also acknowledge support from the MRC Epidemiology Unit MC_UU_12015/1 and MC_UU_12015/5.
Authors’ Affiliations
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