Introduction
In recent years, population ageing and improving health at older ages in Western countries have placed political and economic emphasis on the need to reduce early retirement (before statutory pension age) and extend working life (beyond age 50). Employment rates among older workers (ages 50–64) in England are increasing, from 62 % in 2001 to 67 % in 2013 (Redden
2013). Across Europe, however, effective retirement ages (the average age of labour market exit) continue to lag behind statutory ones (i.e. more people stop working before statutory pension age than do after; OECD
2011). With old-age dependency ratios (persons aged 65+ as a proportion of persons aged 20–64) forecast to rise further in coming decades (Eurostat
2015), a better understanding of the antecedents of early labour market exit is imperative.
Retirement decisions have been linked to a range of individual and organisational attributes (Adams and Beehr
2003), but less is known about the role of the psychosocial work environment. Recognising that workplace adjustments represent a modifiable target for policy intervention, this study considers job demands and job resources as potential determinants of extended working. Job demands refer to aspects of the job “that require sustained physical and/or psychological effort” (Bakker and Demerouti
2007), whereas resources are attributes that stimulate personal growth, learning and development, contribute towards the achievement of work goals or reduce job demands (p. 312).
The existing literature on the interplay of demands, resources and subsequent poor health is extensive (Demerouti et al.
2001; Haüsser et al.
2010). However, few studies have considered these factors in relation to retirement, and many of these have focused on specific outcomes (e.g. disability pension) or occupations (e.g. nurses). Of particular relevance, here are the dual psychological processes proposed by Karasek's demand-control model (Karasek et al.
1981), and how these relate to retirement outcomes. In the ‘health impairment’ process, excessive job demands result in high levels of stress, leading in the short term to a state of exhaustion and fatigue (Schreurs et al.
2011), and later, to serious health problems (Landsbergis et al.
1995). The ‘motivational’ process suggests that job resources can motivate employees, resulting in increased levels of work engagement, performance and satisfaction (Bakker
2008).
Working conditions may be related to retirement outcomes via three pathways. High levels of job demands can, by exhausting mental and physical capacity, lead to work overload and subsequent poor health. Given strong evidence showing poor health to predict early retirement and retirement intent (Mortelmans and Vannieuwenhuyze
2013), demands may encourage retirement insofar as they deteriorate health. High demands have also been linked with reduced job satisfaction that can motivate early retirement (Mein et al.
2000) even without the deleterious effects upon health.
A second pathway suggests that job resources may discourage retirement intent by raising levels of work enjoyment and satisfaction. Positive job attributes such as control, social support, career opportunities or financial reward have been shown to be positively associated with job satisfaction (Cheng et al.
2014), work engagement (Xanthopoulou et al.
2009) and subjective well-being (Stansfeld et al.
2013). It has also been shown that employees are less likely to stop working when they enjoy what they are doing or feel fulfilled by their work (Gagné and Deci
2005). Job resources, therefore, may discourage early retirement by enhancing overall job quality.
A third potential pathway arises from the interaction of demands and resources whereby resources influence retirement indirectly by moderating the association between high demand and subsequent poor health. Karasek’s model states that job strain arises from a combination of high job demands and low decision latitude. While empirical support for the interactive demand–resource relationship has been weak (Dollard and Winefield
1998; Landsbergis et al.
1995), job resources may indirectly reduce early retirement intent by weakening the link between job demands and poor health.
Existing evidence on working conditions and retirement
There has been mixed evidence for the relationship between physically strenuous work and retirement timing. Some studies have found physical demands (e.g. lifting or pushing heavy loads, repeated bending of the neck or back, or standing for prolonged periods) to predict early or health-related retirement (Blekesaune and Solem
2005; Sejbaek et al.
2012), but a recent systematic review (van den Berg et al.
2010) was less supportive, finding a statistically significant association between physical demands and early retirement in just 1/3 studies. With regards to the relationship between psychosocial demands and retirement outcomes, Smeaton et al. (
2009) found that older workers in England reporting high levels of work-related stress were more likely to say they plan to retire before state pension age. Laine et al. (
2009) used data from the
Finnish Public Sector Study showing workers reporting high levels of job strain to be 2.60 (95 % C.I. 1.26, 5.34) times more likely to leave work on a disability pension, compared to those reporting low levels of strain (after adjusting for demographic characteristics and health risk behaviour). Other studies, however, have found no support for the association of psychosocial demands upon retirement timing (e.g. Salonen et al.
2003; Zappalà et al.
2008).
Several studies have emphasised job resources (over demands) as the key determinant of retirement outcomes. Hurd and McGarry (
1993) found job flexibility and financial rewards (such as pensions or healthcare insurance) to play a greater role in determining extended working (beyond age 62 or 65), compared to physical or mental demands. Retirement intentions have been shown to be influenced by low job control (Sutinen et al.
2005), effort-reward imbalance (Siegrist et al.
2007) and unsupportive workplace norms and supervisors (van Solinge and Henkens
2013). Job control has additionally been linked to labour market exit (Blekesaune and Solem
2005) and disability pension (Vahtera et al.
2010). Other studies have been less supportive, finding no association between job resources and early retirement intent (Sejbaek et al.
2012).
Very few studies have considered the demand–resource interaction in relation to retirement timing. One study found job stress to be a stronger predictor of early retirement when it coincided with low control (Elovainio et al.
2005). Another found high control to reduce the risk of disability retirement due to musculoskeletal disorders (Vahtera et al.
2010).
This paper considers the role of the psychosocial work environment in relation to two outcomes: retirement preferences (preferred number of years until retirement) and labour market exit (moves out of paid employment). Three hypotheses are tested:
Results
The analytical sample consisted of 3462 individuals aged 50–69 who were working (>0 h/week) for at least one wave during the ELSA study period. Individuals were omitted due to missing data on retirement preferences (
n = 311), job characteristics (
n = 37) and other covariates (
n = 74). Compared to the excluded sample, the analytical sample was younger (average age of 58.7 vs. 67.4 %;
p < 0.0001) and contained a smaller proportion of women (52.9 vs. 56.6 %;
p < 0.0001). The analytical sample was also healthier, with a smaller proportion of individuals reporting poor health (51.2 vs. 67.3 %;
p < 0.0001) and long-term limiting illness (42.7 vs. 58.9 %;
p < 0.0001). Descriptive statistics for the analytical sample are given in Table
1.
Table 1
Characteristics of the analytical sample
Age [years; mean ± SD (range)] | 58.0 ± 4.1 (50.0–69.0) |
Female | 51.2 % |
Poor self-rated health | 49.1 % |
Long-term limiting illnessa
| 41.2 % |
Partnership status |
No partner | 19.1 % |
Partner is working | 57.0 % |
Partner not working | 20.2 % |
Partner recently retired | 3.6 % |
Income decileb [mean ± SD (range)] | 7.3 ± 2.4 (1.0–10.0) |
Job characteristics |
Physical job demands [scale; mean ± SD (range)] | 3.2 ± 1.6 (1.0–7.0) |
Psychosocial job demands [scale; mean ± SD (range)] | 4.0 ± 1.5 (1.0–7.0) |
Decision authority [scale; mean ± SD (range)] | 4.8 ± 1.2 (1.0–7.0) |
Low social supportc
| 25.4 % |
Low recognitionc
| 30.0 % |
Outcomes |
Preferred years until retirementd [mean ± SD (range)] | 4.9 ± 6.5 (0.0–70.0) |
Work exit next wavee
| 19.4 % |
N | 3462 |
Minimally (age, sex) and additionally adjusted (age, sex, income, self-rated health, limiting long-term illness, partner’s employment status) estimates for the influence of job characteristics upon retirement preferences are presented in Table
2. These were estimated for (a) each job characteristic separately and (b) all job characteristics simultaneously. Considered separately, three out of five job characteristics were significantly associated with retirement preferences at the next wave, after full adjustment. Psychosocial job demands were, per unit increase in the summed score (range 1–7), associated with preferences for retirement 0.25 years earlier (95 % C.I. −0.37, −0.13). Decision authority was, per unit increase, associated with preferences for retirement 0.41 years later (95 % C.I. 0.28, 0.55). Low recognition at work (‘disagree’ or ‘strongly disagree’ compared to ‘agree’ or ‘strongly agree’) was associated with preferences for retirement 0.40 (95 % C.I. 0.07, 0.73) years earlier. When all job characteristics were tested simultaneously, only psychosocial demands (
β = −0.18; 95 % C.I. −0.31, −0.06) and decision authority (
β = 0.38; 95 % C.I. 0.23, 0.53) remained statistically significant predictors of retirement preferences.
Table 2
Coefficients for retirement preferences (preferred years until retirement) measured at the next ELSA wave
Physical demands | −0.04 | | | | | 0.01 | −0.04 | | | | | 0.01 |
(−0.15, 0.08) | | | | | (−0.11, 0.12) | (−0.15, 0.08) | | | | | (−0.11, 0.13) |
Psychosocial demands | | −0.26*** | | | | −0.19** | | −0.25*** | | | | −0.18** |
| (−0.38, −0.14) | | | | (−0.31, −0.06) | | (−0.37, −0.13) | | | | (−0.31, −0.06) |
Decision authority | | | 0.43*** | | | 0.39*** | | | 0.41*** | | | 0.38*** |
| | (0.29, 0.56) | | | (0.24, 0.54) | | | (0.28, 0.55) | | | (0.23, 0.53) |
Low social support | | | | −0.28 | | 0.31 | | | | −0.23 | | 0.32 |
| | | (−0.64, 0.08) | | (−0.12, 0.74) | | | | (−0.59, 0.12) | | (−0.10, 0.75) |
Low recognition | | | | | −0.45** | −0.07 | | | | | −0.40* | −0.05 |
| | | | (−0.78, −0.12) | (−0.47, 0.32) | | | | | (−0.73, −0.07) | (−0.45, 0.35) |
Individualsc
| 3462 | 3462 | 3462 | 3462 | 3462 | 3462 | 3462 | 3462 | 3462 | 3462 | 3462 | 3462 |
Considered separately, three out of five job characteristics were significantly associated with work exit, after full adjustment (Table
3). Decision authority was, per unit increase in the summed score, associated with reduced odds of work exit (OR = 0.91; 95 % C.I. 0.86, 0.95). In practical terms, workers who reported high decision authority (a score of 7) were 8.6 % less likely to stop working, compared to those reporting low decision authority (a score of 1). Conversely, increased odds of work exit were found for low social support (OR = 1.25; 95 % C.I. 1.09, 1.44) and low recognition (OR = 1.34; 95 % C.I. 1.17, 1.53). Workers who ‘disagreed’ or ‘strongly disagreed’ with the statements on social support or recognition were 3.2 and 4.1 % more likely, respectively, to stop working between two consecutive ELSA waves. When testing all job characteristics simultaneously, only decision authority (OR = 0.93; 95 % C.I. 0.88, 0.97) and low recognition (OR = 1.23; 95 % C.I. 1.10, 1.43) remained statistically significant.
Table 3
Odds ratios for work exit next by next ELSA wave
Physical demands | 0.99 | | | | | 0.98 | 0.99 | | | | | 0.98 |
(0.96, 1.03) | | | | | (0.94, 1.02) | (0.95, 1.02) | | | | | (0.94, 1.01) |
Psychosocial demands | | 1.02 | | | | 0.98 | | 1.02 | | | | 0.99 |
| (0.97, 1.06) | | | | (0.94, 1.03) | | (0.98, 1.06) | | | | (0.95, 1.04) |
Decision authority | | | 0.90*** | | | 0.92** | | | 0.91*** | | | 0.93* |
| | (0.85, 0.94) | | | (0.87, 0.96) | | | (0.86, 0.95) | | | (0.88, 0.97) |
Low social support | | | | 1.29*** | | 1.10 | | | | 1.25** | | 1.08 |
| | | (1.12, 1.47) | | (0.94, 1.28) | | | | (1.09, 1.44) | | (0.92, 1.27) |
Low recognition | | | | | 1.36*** | 1.23** | | | | | 1.34*** | 1.23** |
| | | | (1.20, 1.56) | (1.10, 1.43) | | | | | (1.17, 1.53) | (1.10, 1.43) |
Individualsc
| 3462 | 3462 | 3462 | 3462 | 3462 | 3462 | 3462 | 3462 | 3462 | 3462 | 3462 | 3462 |
All two-way interactions between job demands and job resources were tested, adjusting for other job characteristics and individual covariates. With one exception, no statistically significant interaction effects were observed (at the 5 % level; see Table
4). Among workers reporting low levels of psychosocial demand, those receiving low levels of social support were more likely to stop working, compared to workers reporting higher levels of support (predicted probabilities of work exit for low and high support = 24.3 and 18.3 %, respectively). However, this was only borderline significant (
p = 0.045), and no corresponding effect was observed for workers reporting high levels of psychosocial demand (predicted probabilities of work exit for low and high support = 19.3 and 18.6 %, respectively).
Table 4
Adjusted Wald test statistics for demand–resource interactions
Physical job demands | × Decision authority | 3.14 | 0.077 | 0.41 | 0.520 |
× Low social support | 0.02 | 0.895 | 0.97 | 0.325 |
× Low recognition | 0.08 | 0.773 | 0.59 | 0.443 |
Psychosocial demands | × Decision authority | 0.68 | 0.410 | 0.79 | 0.375 |
× Low social support | 0.30 | 0.583 | 4.02 | 0.045 |
× Low recognition | 1.75 | 0.186 | 0.77 | 0.380 |
Sensitivity tests were conducted to test whether the influence of job characteristics differed by age or sex. Physical and psychosocial job demands had a stronger downward influence upon retirement preferences as age increased (χ
2 = 10.22 and 15.73, respectively; p < 0.01 on 2 df), but no other differences by age were found. No differences were found by sex, for either outcome. We further tested whether the chosen cut-point for work exit (0 h/week) influenced our findings. The direction and substantive interpretation of results did not change whether this cut-point was set at 0, 5, 10, 15, or 20 h/week.
Discussion
In this analysis of a nationally representative sample of 3462 older workers in England, we found no evidence of an association between job demands (either physical or psychosocial) and the probability of work exit, but psychosocial demands were predictive of preferences for shorter time until retirement. In contrast, good evidence was found to support the hypothesis that job resources predicted preferences for longer time until retirement and reduced probability of work exit. When adjusting for age and sex, all three measures of job resource (decision authority, low social support and low recognition) were associated with the probability of work exit, as hypothesised, while decision authority and low recognition were predictive of retirement preferences. In the additionally adjusted models, only decision authority and low recognition remained statistically significant. All job characteristics had a stronger influence when considered separately which, given high correlations between the different measures, was to be expected. Workers reporting high levels of decision authority are likely to also enjoy high levels of social support and recognition. We found very little support for our third hypothesis, the interactive relationship between demands and resources. Low psychosocial demands were more strongly associated with work exit if workers reported low social support (compared to high support), but this was only borderline significant (p = 0.045) and no corresponding effect was observed for high psychosocial demands.
We found that decision authority and low recognition predicted retirement preferences as well as work exit. However, although psychosocial demands were predictive of wanting to retire sooner, they had no influence upon actual exit probabilities. This is consistent with previous studies showing discrepancies between retirement intentions and behaviours (Solem et al.
2014; Dal Bianco et al.
2015). Workers may be forced to retire earlier than they would like because of poor health or caring responsibilities. Conversely, working life may extend beyond preferred retirement age due to financial insecurity or lack of pension eligibility. That retirement decisions are constrained by individual circumstances is particularly relevant when considering the role of the work environment. While adjusting for income and health, our model of the probability of work exit assumed that individuals had an equal capacity to retire. Our results may underestimate the influence of the work environment, therefore, since only a subset of workers experiencing high demands or low resources will be able to act upon their preferences.
Our findings are consistent with past studies showing no association between job demands and retirement timing (Salonen et al.
2003; Zappalà et al.
2008). The results for decision authority (Blekesaune and Solem
2005) and work recognition (Thorsen et al.
2012) also support those from previous studies. A key contribution of this study was to test the demand–resource interaction in relation to retirement timing. Here, our findings are at odds with past studies on retirement. Elovainio et al. (
2005) found support for a demand–control interaction, but their sample incorporated a wider age range than our study (20–65 rather than 50–69) and consisted of Finnish healthcare employees only, rather than the nationally representative sample employed here. Instead, our findings are more consistent with the broader demand–resources literature (e.g. Dollard and Winefield
1998), which tends to support the additive but not interactive effects of demands and resources.
This study is one of the first to consider working conditions and retirement outcomes among a large, longitudinal and nationally representative sample of older workers in England. With the exception of some Scandinavian studies (e.g. Vahtera et al.
2010), past research has often relied upon small sample sizes or focused within particular institutional settings. Other strengths are that job characteristics were measured repeatedly and it was possible to adjust for several potential covariates.
In terms of limitations, our analysis relies on a few simple measures of the work environment. Such measures have been shown to have acceptable validity (Leineweber et al.
2010), but the multi-item scales employed in past studies would provide better coverage of the constructs of interest. The analysis was also limited to considering each respondent’s first observed transition out of work, precluding later returns to work. Job characteristics were measured at older ages only (50+) despite past research showing retirement timing to depend upon occupational exposures across the life course (Liebermann et al.
2013). Sample attrition represents another important limitation. The analytical sample was younger and healthier than excluded respondents. ELSA respondents who are still working at ages 50+ are likely to enjoy more favourable working conditions and be better educated compared to those who exited the labour market before age 50. Our results are generalizable only to workers aged 50–69 living in England and Wales.
These results are important within the context of the UK and European policies to promote extended working. They suggest that workplace modifications to improve the psychosocial work environment can delay retirement timing by moderate but statistically significant amounts. In our results, increases in decision authority (from low to high) were associated with preferences for retirement 2 years later. This is comparable to rises in compulsory retirement age proposed in Europe (Sinclair et al.
2013) and the US (General Accounting Office
2011).
At the same time, we would not wish to overstate the potential for change. Given heterogeneous working arrangements and relations, and the fluctuating influence of macro-economic circumstances, such improvements may be difficult to achieve. Moreover, as noted above, retirement timing is constrained by factors such as poor health or financial need that may curtail or extend working life irrespective of the work environment. Decision authority and work recognition therefore represent important targets for policy, but only insofar as these factors can be successfully modified. Recent large-scale interventions (Hasson et al.
2012; Gilbert-Ouimet et al.
2015) suggest that improvements to the psychosocial work environment are feasible, but further research is needed to develop and test such interventions.