key: cord-1000494-eqiw8a2f
authors: Demiral, Yucel; Ihle, Tobias; Rose, Uwe; Conway, Paul Maurice; Burr, Hermann
title: Precarious Work as Risk Factor for 5-Year Increase in Depressive Symptoms
date: 2022-03-08
journal: Int J Environ Res Public Health
DOI: 10.3390/ijerph19063175
sha: c04cd6c285fb28da5b6cb9b257c7f9eb0fe8227a
doc_id: 1000494
cord_uid: eqiw8a2f

Objectives: The aim was to investigate the longitudinal relationship between precarious work and depressive symptoms in a representative cohort of employees in Germany. Methods: In the German Study on Mental Health at Work (S-MGA) (n = 2009), depressive symptoms were assessed by the Patient Health Questionnaire (PHQ−9). Precarious work was measured through baseline (2012) self-reported job insecurity, marginal part-time, fixed-term contract, hourly wage and—during follow-ups 2012–2017—unemployment. Among employees without depressive symptoms at baseline (2012), we ran logistic regression analyses stratified by gender with depressive symptoms at follow-up in 2017 as the dependent variable, adjusting for baseline (2012) age, gender, socioeconomic position and partner status. Results: Among men, job insecurity (OR: 2.47; 95% 95% CI: 1.37–4.48) and low wage (3.79; 1.64–8.72) at baseline were significantly associated with depressive symptoms at follow-up. Among women, indicators of precarious work were not associated with depressive symptoms at follow-up. Among men, a cumulative exposure index of precarious work was significantly associated with the development of depressive symptoms (one indicator: 1.84; 0.94–3.60, ≥two indicators: 7.65; 3.30–17.73). This index was not associated with depressive symptoms among women. The population attributable fraction of precarious work due to depressive symptoms among men was approximately 30%. Conclusions: Among employees in Germany, precarious work seems to be a risk factor for the subsequent development of depressive symptoms among men, but not among women. Research on precarious employment in different countries is needed.

The employment policies associated with the Keynesian economy, which became the norm in the "Golden Age" that followed World War II, ended with the global economic crisis in the 1970s. As a response to this, flexible employment schemes have been introduced along with restrictions in social protection programs [1] . Since then, there has been a wide range of flexible work practices under different names, including piecework, casual work, contingent work and so forth [1] . In Germany, deregulations have led to a rise of employment in fixed-term contracts, agency work and marginal part-time work [2] [3] [4] [5] . In a European comparison, employees in Germany showed an average level of job insecurity but one of the highest fractions of low wage earners.

Several scholars have brought forward the notion of precarious work in order to grasp the increased flexibilization of work in light of its possible consequences for health [6, 7] . Most definitions of precarious work have the concept of insecurity in employment in common [8] [9] [10] [11] [12] . This concept includes two aspects. The first indicates the presence of insecure contracts (e.g., fixed-term, temporary agency or lack of contract) [8] [9] [10] 13] . The second relates to the experience of job insecurity [11] , reflecting the subjective anticipation of risk For more details, see Table A2 . 1 See internet appendix of the cited paper. The table is based on published analyses on baseline attrition [43] and participation in the cohort in the present study (before exclusion of participants with depressive symptoms; see Figure 1 , second last box to the left). 

The present study is based on data from the German Study on Mental Health at Work For more details, see Table A1 . 1 In combination with locked job experience, i.e., being in a job without the possibility to change jobs. For more details, see Table A2 . 1 See internet appendix of the cited paper. The table is based on published analyses on baseline attrition [43] and participation in the cohort in the present study (before exclusion of participants with depressive symptoms; see Figure 1 , second last box to the left).

In the present study, we focused on five aspects of precarious work as risk factors for depressive symptoms among workers in Germany: (a) job insecurity, (b) working in a fixed-term contract, (c) marginal part-time, (d) low wage and (e) unemployment. We hypothesized that specific as well as concurrent experiences of precarious work elevate the risk of depressive symptoms. We also examined possible gender-related differences in these associations.

The present study is based on data from the German Study on Mental Health at Work (S-MGA): a nation-wide employee cohort study with a baseline in 2012 and a follow-up in 2017 [43] . At baseline, the population consisted of all employees in Germany aged 31-60 years included in a social security scheme set up by the government (i.e., without civil servants, self-employed individuals and freelancers) on the reference date of the 31 December 2010. Of the 13,590 employees who were randomly selected from 206 municipalities in Germany (stratified by region and population size), 4511 people completed the baseline personal interview that was conducted 13 months (range 11-17 months) after the sampling procedure was completed (baseline response rate: 33%) ( Figure 1 ). During these 13 months, 308 people ceased to be employed, leaving 4203 employed participants at baseline; of these, 2485 also participated in the follow-up interview (follow-up participation among baseline participating employees was 59%, while the cohort participation was 20%; see Table 3 ). Cohort participation was independent of gender, but was dependent on age and socioeconomic position (SEP): participants 30-39 years of age and in a lower socioeconomic position had lower participation (Table 3) . From these, 313 people were excluded, predominantly due to missing information on depressive symptoms. For the main analysis, 163 participants with depressive symptoms at baseline were excluded (see analysis section below). Thus, the final sample on which the present study is based amounts to 2009 employees. 59 20 The table is based on published analyses on baseline attrition [43] and participation in the cohort in the present study (before exclusion of participants with depressive symptoms; see 

All information, with only the exception of depressive symptoms, was obtained through interviews conducted in the respondents' homes [43] . Information on depressive symptoms was obtained through a paper questionnaire filled in by the participants in the absence of the interviewer [43] .

The Patient Health Questionnaire (PHQ-9) was used to measure depressive symptoms at both baseline and follow-up [44] . The scale consists of the following nine items, measuring the intensity of symptoms as experienced by the respondent within the past two weeks: 'Little interest or pleasure in doing things'; 'Feeling down, depressed or hopeless'; 'Difficulty falling asleep or sleeping or increased sleep'; 'Tiredness or lack of energy'; 'Decreased appetite or excessive need to eat'; 'Bad opinion of yourself'; 'Difficulty concentrating on something'; 'Slowed speech/movement or restlessness ("fidgety")'; and 'Thoughts that you would rather be dead or want to inflict pain on yourself'. The response categories are: 'Not at all' (0), 'Several days' (1), 'More than half the days' (2), and 'Nearly every day' (3). The scale for depressive symptoms was calculated as the sum of the nine items, resulting in a score ranging from 0 to 27 [44, 45] . Cronbach's α was 0.82, with inter-item correlations ranging between 0.20 and 0.49. For the main analysis, the scale was dichotomized using ≥10 as the cut-off point, which represents a clinically validated cut-off for depression cases [46] . In the sensitivity analysis, the scale was treated as a continuous measure.

Precarious work was measured through five indicators, of which four were measured at baseline (job insecurity, marginal part-time, fixed-term contract, low wage), and one at follow-up (events of unemployment during follow-up).

Self-reported job insecurity in 2012 was measured as a scale calculated as the mean of the following two items from the job insecurity scale [47, 48] : 'Are you worried about becoming unemployed?' and 'Are you worried about it being difficult for you to find another job if you became unemployed?'. These included the response options: 'To a very large extent' (4), 'To a large extent' (3), 'Somewhat' (2), 'To a small extent' (1) and 'To a very small extent' (0). Cronbach's α was 0.52, with an inter-item correlation of 0.35. The job insecurity scale was dichotomized, with a score of 2.5 or higher indicating job insecurity.

Marginal part-time (German term: 'mini-/midi-job' [5, 49] ) in 2012 was assessed as a dichotomous variable based on the questions: 'What is your main activity?' and 'Are you currently . . . ?', with the response option 'Marginally, occasionally or irregularly, also in mini-jobs up to 400 euros or midi jobs up to 800 euros a month' considered as an indicator of marginal part-time. All the other options, e.g., 'Working full time at least 35 h per week' and 'Unemployed', were not regarded as marginal part-time. Marginal part-time covers a type of contract introduced in the German employment legislation called 'minor employment', characterized by part-time employment with a comparatively low income and limited obligations for the employer regarding social security contributions [5, 49] .

Fixed-term contract in 2012 was measured as a dichotomous variable based on the question: 'Is your current employment contract . . . ?', with the two response options being 'fixed term' and 'open ended'.

Low wage in 2012 was measured as a dichotomous variable; participants with low wages were considered as those obtaining below 60% of the median personal hourly net wage in the present cohort (i.e., below €6.4/$7.3). We calculated hourly net wage based on two questions: one regarding current monthly net income (calculated as a scale) and one regarding working hours. Current monthly net income was divided by working hours, and the resulting variable was used as the basis for the dichotomization. Information on wage was calculated as a scale based on the question: 'Please report how much of your current monthly net income comes from your professional activity', with the following response options: 'Up to €400 (450$)', 'Over €400 to €800 (>$455-910)', 'Over €800 to under €1000 (>910-<$1135)', '€1000 to under €1500 (1135-<$1705)', '€1500 to less than €2000 (1705-<$2270)', '€2000 to less than €2500 (2270 < $2840)', '€2500 to less than €3000 (2840 < $3405)', '€3000 to under €4000 (3405 < $4540)', '€4000 to less than €5000 (4540-<$5675)' and '€5000 and more (≥$5675)'. Each of these response options was coded based on the midpoint of the respective range of income. Information on working hours was collected with the following two questions: 'How many hours a week do you normally work, including regular overtime, overtime, etc.?' and-for people with a second job(s)-'How many hours do you usually work there each week?'. Weekly working hours were recalculated into monthly working hours.

Unemployment between 2012 and 2017 was coded as a dichotomous variable based on the following questions at follow-up, inquiring about episodes of unemployment that occurred since baseline: 'What was your main activity then?'. With one of the response options being 'Unemployed', all the other options, e.g., 'Working full time at least 35 h per week' and 'Marginally, occasionally or irregularly, also in mini-jobs up to 400 euros or midi jobs up to 800 euros a month', were regarded as not indicating unemployment [50] . We constructed a dichotomous variable reflecting experiences of at least one spell of ≥1 month with unemployment between baseline in 2012 and follow-up in 2017.

A summary index including all indicators of precarious work was constructed (precarious work index); only the indicators being significantly associated with depressive symptoms at follow-up in at least one gender were included in the index [40] . As the number of employees experiencing more than two indicators was small, the highest category of the index was '≥2 indicators', with 6% (118 people) experiencing at least two indicators at the same time, 25% (498 people) only one indicator and 69% (1393 people) none of the indicators.

Information about participants' gender and age was obtained through the interview. Squared age was introduced in the analysis as the incidence of depression increased up to the start of the forties and then decreased slightly in the fifties [51, 52] .

The socioeconomic position (SEP) was assessed according to the four-level International Standard Classification of Education (ISCED), based on the International Standard Classification of Occupations 2008 (ISCO) [53] . Managers were placed in the same group as professionals in accordance with similar classifications [54] . The main groups of ISCO 2008 1 and 2 were placed in skill level category 4, the main group 3 in level 3, the main groups 4-8 in level 2 and the main group 9 in level 1.

Partner status was assessed by means of questions on cohabitation and partner status.

In the main analyses, which include employees without depressive symptoms at baseline (PHQ9 < 10, see description of this variable above), the gender-stratified associations between dimensions of precarious work at baseline (job insecurity, fixed-term contract, marginal part-time, low wage and unemployment) and depressive symptoms at follow-up were examined by means of a multiple logistic regression, with estimates calculated as odds ratios (OR) and their relative 95% confidence intervals (95% CI). We estimated two models, each comprising two steps. In the first model, each dimension of precarious work was entered separately. In the first step, we adjusted for the baseline covariates age and partnership status. In the second step, we additionally adjusted for the socioeconomic position (SEP, entered as categorical variable). The second model followed the same procedure, except that all dimensions of precarious work were entered simultaneously in both steps.

We then examined the association with the precarious work index (see description above) at baseline and depressive symptoms at follow-up, following the same adjustment procedure described above. Based on this index, the population attributable fraction (PAF) of depressive symptoms due to precarious work was computed according to the method developed by Miettinen [55] . PAF can be understood as the fraction of depressive symptoms at follow-up attributable to precarious work. It can be illustrated graphically as the fraction of the area of bars (surplus cases) over the odds ratio 1 out of the total area of bars (total cases) [55] .

In a first set of sensitivity analyses (Appendix A), we repeated the main analyses while treating depressive symptoms as a continuous, instead of dichotomous, variable in multiple linear regressions. In these analyses, the change in depressive symptoms was treated as the dependent variable, adjusting for baseline depressive symptoms, partnership status, age and-in a consecutively adjusted model-socioeconomic position. This was done to check if the estimates obtained in the main analyses were dependent of how the depressive symptoms' variable was treated (dichotomized versus continuous).

In a second set of sensitivity analyses (Appendix A), we repeated the main analyses while also including employees with depressive symptoms at baseline (PHQ-9 ≥ 10), adjusting for baseline depressive symptoms, partnership status, age and-in a consecutively adjusted model-socioeconomic position. This was done to check the impact on the results due to excluding participants with depressive symptoms at baseline who might have already developed these symptoms as a result of precarious work [56] . Table 4 shows the distribution of the sociodemographic characteristics and the indicators of precarious work for the study sample of employees aged 31-60 years at baseline. Among the participants, 35% were exposed to some type of precarious work. Women reported significantly more marginal part-time and low wage than men. However, the prevalence of job insecurity and fixed-time work was not statistically different between genders. Job insecurity significantly increased with age. In general, all indicators of precarious work were strongly correlated with each other, with a prevalence two to three times higher in the exposed than in the unexposed group. Only marginal part-time and job insecurity were not significantly associated. In all, 5% (n = 54) developed depressive symptoms among male workers, and 9% (n = 89) among female workers (Tables 5 and 6) As shown in Table 5 , among male employees without depressive symptoms at baseline, job insecurity (odds ratio (OR): 2.47; 95% confidence interval (95% CI): 1.37-4.48) and low wage (OR: 3.79; 95% CI: 1.64-8.72) at baseline were significantly associated with depressive symptoms at follow-up when entered separately in the regression model and after adjustment for age, partnership status and SEP. The associations also remained significant, despite being slightly attenuated, in the model wherein all indicators of precarious work were entered simultaneously. The associations were all non-significant among women (Table 6 ). Among employees without depressive symptoms at baseline, the experience of unemployment between baseline and follow-up was associated with depressive symptoms at follow-up among men but not among women (OR: 3.07; 95% CI: 1.28-7.37; Table 7 ). The associations were similar when including employees with depressive symptoms at baseline (Tables A6-A8). Table 8 shows the associations between the precarious work index at baseline and depressive symptoms at follow-up. The index included job insecurity, low wage and unemployment, as these were the indicators significantly associated with depressive symptoms in at least one gender. Among men without depressive symptoms at baseline, the precarious work index was associated with subsequent depressive symptoms (exposure to one indicator, OR: 1.84; 95% CI: 0.94-3.60; concurrent exposure to ≥2 indicators, OR: 7.65; 95% CI: 3.30-17.73). Among women, the associations were non-significant. The sensitivity analysis, including employees with depressive symptoms at baseline, showed similar results (Table A9 ). If one disregarded low wage in the precarious work index, the odds for both one and two indicators dropped to around 2 (table not shown). Based on the estimates of the precarious work index (Table 8) , the PAF (population attributable fraction) of depressive symptoms due to precarious work was 32% among men. In the male sample, including those with depressive symptoms, the PAF was 27%. Figure 2 presents an illustration of this latter PAF. If we disregarded unemployment during follow-up in the index, the PAF was still around 30% among men when including all indicators of precarious work (data not shown). If one disregarded low wage from the index, the PAF dropped to 21% (data not shown). Table A9 . The total area of the three bars represents all cases of depressive symptoms at follow-up. The area above the odds ratio of 1 of the two bars to the right represents those cases attributable to the elevated odds of experiencing job insecurity, unemployment or low wage. This area makes up 27% of the total area of all tree bars.

The present prospective study of employees in Germany aged 31-60 years suggests that precarious work is a risk factor for depressive symptoms, and that such a risk is higher among men than women. The odds of depressive symptoms were three times higher among men with unemployment and low wage, and two times higher among men with job insecurity. With regards to women, however, we did not observe any significant associations between precarious work and depressive symptoms. Among men exposed to two or more indicators of precarious work, the odds were five times higher. Our study indicates that the PAF (population attributable fraction) of depressive symptoms due to precarious work among employed men in Germany is around 30%.

It has been suggested that uncertainty about one's ability to sustain a living is a key explanation for the role of precarious work in the development of depressive symptoms [57, 58] . In the present study, job insecurity and unemployment predicted depressive symptoms among men; these could therefore be considered as the key sources of uncertainty among male employees. Multiple studies carried out in European countries generally support our finding that precarious work has a stronger effect on depressive symptoms among men than among women [20, [25] [26] [27] [28] [29] 31, 42] . It should be noted that, in several studies, the effects for women were statistically significant but of a lower size than those observed among men. There might be a number of possible explanations for such a gender difference. One could be that in Germany-as in the case of other countries wherein studies about precarious work were performed-men contribute to the household's income to a higher degree than women [59] . For this reason, precariousness can be expected to be a stronger stressor among men because of their typical role as breadwinners. We are only aware of one longitudinal study that has examined such a role [31] ; in this study, the authors found that the risk of depressive symptoms due to job insecurity was elevated only among men who were contributing the most to the household, but not among other men (no clear results could be obtained among women due to the lack of power). Another explanation could be that men tend to identify more strongly with their work role than women do, whereas women identify more with family obligations [60] . We are not aware of more recent explanations based on work role. In addition, it might be that men and women have different preferences in relation to precarious work. For example, for some workers, fixed-term contracts offer an opportunity to collect various work experiences in order to gain skills and experience [61] . However, in Germany there is no gender difference regarding the voluntary choice of fixed-term contracts [62] . We are not aware of data on the voluntary choice of other types of precarious work among German employees.

In the following, we restrict the comparison of the results obtained in the present study with those obtained in other prospective studies only [41, 63] .

Our finding that the concurrent exposure to indicators of precarious work was associated with an elevated risk of depressive symptoms among men corroborates the results obtained in a number of previous studies, including a study on the German SOEP cohort [19] [20] [21] [22] [23] [24] (Table 1 ). In the present study, the OR related to the exposure to at least two indicators of precarious work was markedly higher that the risk observed in the studies included in the comparison. None of these studies considered low wage as indicator; when in the present study we excluded low wage in the calculation of the precarious work index, we found ORs of the same magnitude as in the other studies. One study on Swedish workers, which defined precarious work through three indicators (unemployment, temporary employment and perceived job insecurity), found that 18% of all cases of poor mental health could be attributed to precarious work. This fits with our estimate of 20% when not considering low wage as an indicator; our estimate rose to around 30% when low wage was also considered. Calculations of attributable fractions are advantageous as they can form a basis for prioritization of public health measures. Obviously, one should take into account to what extent prevention is feasible and if the associations observed are of a causal nature.

Regarding the effects of job insecurity on depressive symptoms, a meta-analysis of thirteen longitudinal studies-including the above-mentioned German SOEP study [22] -found an average elevated risk [40] (Table 2 , first columns). In three studies not considered in this meta-analysis, the observed risks were of a similar size [22, 28, 31] . In some of these studies, the risk was higher among men than among women [26] [27] [28] [29] 31] . Overall, these findings are in line with the present study, wherein we found an OR of 2.47 (95% CI: 1.37-4.48) among men and of 1.41 (95% CI: 0.83-2.40) among women.

Regarding fixed-term contracts, three studies examined the effects on mental health; among these, two found an elevated risk while one did not observe any significant associations [32] [33] [34] (Table 2 , middle columns). In the latter study, the outcome was sickness absence with depressive symptoms as the diagnosis, which might explain the non-significant association; it might be that diagnosed depressive symptoms do not reflect the underlying prevalence of disease. None of these studies were stratified by gender. The fact that in our study we did not detect a significant risk could be due to lack of power.

Regarding unemployment, we are aware of two studies that found an elevated risk for depressive symptoms, namely the above-mentioned German SOEP study and a Swedish one [22, 25] (Table 2 , last columns). In particular, in line with the present study, the latter found a higher risk among men than among women.

To our knowledge, no previous longitudinal studies have examined the effect of marginal part-time (German: "mini-or midi-job") or low wage on mental health (see also Section 2.2.2, 'Precarious work', in the present paper).

National welfare state contexts may play a role in the association between precarious work and mental health. High levels of social protection might buffer the effects of precarious work on health [1, 64] . The developed German welfare state might have played such a buffering role; although, since the turn of the millennium, it has restricted its level of social protection [2] [3] [4] [5] . As the number of prospective studies is limited-especially outside Scandinavia-it is not possible to assess clearly if national welfare state contexts play a role in the effects of precarious work on mental health [64] .

If we break down the body of literature on precarious work discussed above, the number of studies (apart from job insecurity) seems limited, both internationally and in Germany (Tables 1 and 2 ). We acknowledge that in our literature review, being not systematic, we might have overlooked some relevant studies. A reason for this could be that aspects of precarious employment were not included in cohort studies outside of Scandinavia. Alternatively, such data might exist but have not been analysed due to a lack of focus on precarious work in the field of occupational health and safety [6].

A first strength of this study is that it is based on a prospective design and on a large sample of employees. Secondly, this is the first study examining a broader range of indicators of precarious work in Germany. A previous study of more than 7000 employees examined two indicators concurrently, namely job insecurity and unemployment [22] . Thirdly, we were able to control for SEP to reduce the potential confounding role of other social factors in the observed associations.

It is a limitation that the study is observational, which might introduce selection bias. Previous studies performed in countries other than Germany have shown that poor mental health prior to work entry predicts subsequent participation in the labour market [65] [66] [67] [68] . In addition, during a work career, depressive symptoms seem to be related to the development of a poorer work environment, but to a limited degree [69] [70] [71] [72] [73] . Regarding the German context, we are not aware of the impact of such selection processes. Response bias can also play a role, especially in light of the low participation in the cohort. In the present study, cohort participation was not associated with gender, but it was with age and SEP. Among workers 30-39 years of age and unskilled workers, the response rate was lower than the response rate of older workers and that of professionals, managers and semi-professionals (Table 1) . However, such differences in attrition should not alter the present findings considerably. It is also a drawback that people below the age of 31 were not invited for the study. As indicators of precarious work are more prevalent among younger workers, the present study underestimates the prevalence of precarious work [2] . We could not establish if the inclusion of younger workers would have affected the associations observed in the present study. Furthermore, the job insecurity scale is based on two items only, which resulted in a low internal consistency [74] . Some of the indictors of precarious work presented a low prevalence, limiting the statistical power of the study. This was the case for marginal part-time and fixed-term contracts among men. Moreover, we assessed SEP through the occupational level, which overlooks important aspects of SEP such as household and lifetime biographies.

In line with previous studies, the present study suggests that precarious work is an important risk factor for the subsequent development of depressive symptoms among men, but not-or to a lower degree-among women. This might have implications for both practice and research.

The prevalence of precarious employment has increased in the last couple of decades, not only in Germany [75] . Such an increase might continue due to recent developments, such as the impact of the COVID-19 pandemic on the labour market. It must be noted that specific types of precarious work vary strongly across countries [49] , and national contexts might play a role in their effects on health [64] .

From the practical point of view, possible undesired health consequences of precarious employment should be taken further into account in legislation, regulation and collective agreements. Workplaces and health and safety professionals should also be aware of such undesired consequences. It is important to distinguish between forms of precarious work employment that are chosen voluntarily by workers from those that are chosen involuntary because of failed attempts to find a more stable job [61] .

From the research point of view, longitudinal studies on the effects on mental health of different aspects of precarious work such as fixed-term contracts, unemployment and low wage are scarce; in addition, the impact of issues related to gender needs to be examined further [6] . Reasons for the suggested stronger effect among men should be investigated in order to understand what role economical and attitudinal aspects may play. In addition, aspects such as voluntary preferences for precarious work and health selection into precarious work should be considered. Finally, we suggest that future studies attempt to calculate fractions of unwanted health outcomes attributable to precarious work. This might further highlight the possible public health impact of this type of exposure. Informed Consent Statement: Informed consent was obtained from all subjects involved in the study. All employees in the sample were contacted by mail and the interviews at the baseline were only conducted after each respondent gave their informed oral consent [41] . Written consent was given for the willingness to participate at follow-up. 

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The longitudinal Study on Mental Health at Work (S-MGA) was conducted in collaboration with the Institute for Employment Research (IAB). The S-MGA was based on samples from statistics of the Federal Employment Agency (BA), which have been merged with Integrated Employment Biographies by the IAB. We thank the participating employees, the infas (Institute of Applied Social Sciences) for collecting the data, and Dagmar Pattloch, BAuA, for data preparation. The authors also wish to thank the four anonymous reviewers of the present paper.

The authors declare no conflict of interest. 1 Total number of cases with depressive symptoms at follow-up; men: 54 (5%); women 89 (9%). 2 Socioeconomic position. 3 Number of indicators of precarious work experienced: (a) Job insecurity at baseline, (b) low wage at baseline, and (c) unemployment experience during follow-up.