Study population
This study utilized five surveys of the Norwegian nationwide Survey of Living Conditions on work environment from 2006, 2009, 2013, 2016, and 2019, with a total sample of 43,977 individuals. The purpose of using five surveys is to reach a larger number of observations, which may increase the accuracy of JEM performance. Data collection was conducted by Statistics Norway. The personal interviews conducted by telephone with computer assistance are on average 24–30 min long. Less than 0.5% of the interviews were conducted face-to-face. Since 2006, the survey on work environment has been funded by the Ministry of Labor and Social Inclusion to expand the sample and develop the survey as a panel.
The sample of the Norwegian nationwide Survey of Living Conditions on work environment was randomly drawn from the population aged 18–69 years, which represented active working-age people in the country. In the 2006 survey, the number of observations was 12,550 (with 67.2% response rate); in the 2009 survey, the number was 12,555 (with 61% response rate); in the 2013 survey, the number was 10,857 (with 53.1% response rate); in the 2016 survey, the number was 10,665 (with 52.6% response rate); and in the 2019 survey, the number of observations was 11,212 (with 57% response rate).
In 2007, the register data population consisted of people aged 18–55 who had a valid occupational code. In total, this included 1,589,535 individuals. Tables
1 and
2 below show the background characteristics of the study population. In both the survey data and register data, the number of men was slightly higher than women (23,062 men and 20,915 women in the survey data, 819,232 men and 770,303 women in the register data). The survey data had a lower proportion of respondents aged 25–44 but a higher proportion of respondents aged 45–69 (43.6% of the total sample aged 25–44 and 46.2% of the total sample aged 45–69) than that of the register data (56.2% and 29.2% of the total sample, respectively). The respondents in the survey data have a higher educational level than the population in the register data, as 42.5% of total respondents in the survey data have college or university education, compared with 34.1% in the register data. However, the distribution of the major occupational groups in both samples was not likely to be different.
Table 1
Background characteristics of the study population (survey data)
Age (years) |
17–24 | 4,484 | 10,2 | 2,308 | 10,0 | 2,176 | 10,4 |
25–44 | 19,160 | 43,6 | 9,880 | 42,8 | 9,280 | 44,4 |
45–69 | 20,333 | 46,2 | 10,874 | 47,2 | 9,459 | 45,2 |
Educational level |
Primary school | 11,116 | 25,3 | 5,979 | 25,9 | 5,137 | 24,6 |
Secondary/High school | 14,007 | 31,9 | 8,524 | 37,0 | 5,483 | 26,2 |
College/university 4 years | 13,328 | 30,3 | 5,508 | 24,9 | 7,820 | 37,4 |
College/university > 4 years | 5,366 | 12,2 | 2,969 | 12,9 | 2,397 | 11,5 |
Major occupational groups (STYRK-98) |
Legislators, senior officials, and managers | 4,569 | 10,4 | 3,032 | 13,1 | 1,537 | 7,4 |
Professionals | 7,921 | 18,0 | 4,170 | 18,1 | 3,751 | 17,9 |
Technicians and associate professionals | 11,818 | 26,9 | 5,236 | 22,7 | 6,582 | 31,5 |
Clerks | 2,743 | 6,2 | 1,100 | 4,8 | 1,643 | 7,9 |
Service workers, shop and market sales workers | 8,480 | 19,3 | 2,514 | 10,9 | 5,966 | 28,5 |
Skilled agricultural and fishery workers | 822 | 1,9 | 670 | 2,9 | 152 | 0,7 |
Craft and related trade workers | 3,911 | 8,9 | 3,665 | 15,9 | 246 | 1,2 |
Plant and machine operators and assemblers | 2,552 | 5,8 | 2,235 | 9,7 | 317 | 1,5 |
Elementary occupations | 1,161 | 2,6 | 440 | 1,9 | 721 | 3,5 |
Long-term sick leave (previous month) |
Yes | 7,046 | 16,0 | 2,946 | 12,8 | 4,100 | 19,6 |
No | 36,931 | 84,0 | 20,116 | 87,2 | 16,815 | 80,4 |
Anxious symptoms |
Severely/Somewhat | 1,195 | 2,7 | 498 | 2,2 | 697 | 3,3 |
A little/Not at all | 42,782 | 97,3 | 22,564 | 97,8 | 20,218 | 96,7 |
Depressive symptom |
Severely/Somewhat | 1,021 | 2,3 | 430 | 1,9 | 591 | 2,8 |
A little/Not at all | 42,956 | 97,7 | 22,632 | 98,1 | 20,324 | 97,2 |
Sleeping difficulty symptoms |
Severely/Somewhat | 3,538 | 8,0 | 1,427 | 6,2 | 2,111 | 10,1 |
A little/Not at all | 40,439 | 92,0 | 21,635 | 93,8 | 18,804 | 89,9 |
Table 2
Background characteristics of the study population (register data)
Age (years) |
18–24 | 221,568 | 13,9 | 113,520 | 13,9 | 108,048 | 14,0 |
25–44 | 903,754 | 56,9 | 472,831 | 57,7 | 430,923 | 55,9 |
45–55 | 464,213 | 29,2 | 232,881 | 28,4 | 231,332 | 30,0 |
Educational level |
Primary school | 321,207 | 20,2 | 176,392 | 21,5 | 144,815 | 18,8 |
Secondary/High school | 714,616 | 45,0 | 399,202 | 48,7 | 315,414 | 41,0 |
College/university 4 years | 424,436 | 26,7 | 167,405 | 20,4 | 257,031 | 33,4 |
College/university > 4 years | 117,827 | 7,4 | 70,469 | 8,6 | 47,358 | 6,2 |
Major occupational groups (STYRK-98) |
Legislator, senior officials, and mangers | 174,674 | 11,0 | 93,566 | 11,4 | 81,108 | 10,5 |
Professionals | 188,963 | 12,0 | 101,577 | 12,4 | 87,386 | 11,3 |
Technicians and associate professionals | 326,718 | 20,6 | 147,123 | 18,0 | 179,595 | 23,3 |
Clerks | 125,183 | 7,9 | 50,160 | 6,1 | 75,023 | 9,7 |
Service workers, shop, and market sales workers | 383,242 | 24,1 | 111,858 | 13,6 | 271,384 | 35,2 |
Skilled agricultural and fishery workers | 9,810 | 0,6 | 7,176 | 0,9 | 2,634 | 0,3 |
Craft and related trade workers | 170,450 | 10,7 | 161,664 | 19,7 | 8,786 | 1,1 |
Plant and machine operators and assemblers | 127,104 | 8,0 | 107,531 | 13,1 | 19,573 | 2,5 |
Elementary occupations | 83,391 | 5,24 | 38,577 | 4,7 | 44,814 | 5,8 |
Disability benefits (2008–2017) |
Yes | 4,878 | 0,3 | 1,939 | 0,2 | 2,939 | 0,4 |
No | 1,584,657 | 99,7 | 817,293 | 99,8 | 767,364 | 99,6 |
Mortality (2008–2017) |
Dead | 18,467 | 1,2 | 11,484 | 1,4 | 6,983 | 0,9 |
Not dead | 157,068 | 98,8 | 807,748 | 98,6 | 763,320 | 99,1 |
Ten long-term sick leave periods or more (2008–2015) |
Yes | 428,510 | 26,9 | 152,019 | 18,6 | 276,491 | 35,9 |
No | 1,161,025 | 73,1 | 668,213 | 81,4 | 493,812 | 64,1 |
As shown in Table
1, 16% of respondents in our survey data had experienced long-term sick leave during the previous 12 months. The percentage of respondents who experienced different mental health symptoms was 2.7% for anxiety, 2.3% for depression, and 8.0% for sleeping difficulty. More women than men in our survey sample reported different mental health problems.
As presented in Table
2, there is a low percentage receiving disability benefits, and mortality is low, with 0.3% and 1.2% of the study population, respectively. Approximately 27% of our register study sample took ten long-term sick leave periods or more during 2008 and 2015, 35.9% of women compared to 18.6% of men.
Constructing the job exposure matrix
In line with the previous study of Hanvold et al. [
4], we constructed a gender-specific matrix with group-based exposure estimates at each intersection between occupations (rows) and psychosocial job exposures (columns) [
4]. Hanvold et al. decided to have at least 19 respondents with the same occupational codes when constructing the JEM groups to enhance reliable estimates [
4]. They reported that two of the authors grouped the occupations and discussed them further with a third author and two experts at the Norwegian Institute of Occupational Health. In total, they constructed 268 JEM groups based on occupational codes and answers from 18,939 respondents in the 2006 and 2009 surveys. Although this study used the same approach as Hanvold et al. to construct the JEM, we included a higher number of respondents, given the fact that we also included the 2013, 2016, and 2019 surveys. As a result, our study had a higher mean number of respondents in each JEM group, ranging from 176, as reported in Hanvold et al.’s study, to 412 in our study (Table
3). This table also shows a higher number of occupational codes (333 occupational codes) and a higher number of occupational codes with at least ⩾19 respondents (243 occupational codes). From 333 titles, we constructed the 268 JEM groups following Hanvold et al. [
4].
Table 3
Number of occupational titles according to number of respondents and number of respondents per JEM group
Number of occupational titles according to number of respondents | N | % | N | % | N | % |
1–18 | 90 | 27 | 126 | 40 | 151 | 54 |
⩾ 19 | 243 | 73 | 191 | 60 | 130 | 46 |
Mean respondents per occupational title | 132 | 73 | 74 |
Min–Max respondents per occupational title | 1 | 2224 | 1 | 831 | 1 | 1503 |
Respondents per JEM group | All (N = 268) | Men (N = 209) | Women (N = 195) |
Median | 261 | 218 | 385 |
Mean | 412 | 276 | 562 |
Min–Max | 19 | 1,503 | 19 | 831 | 19 | 1,503 |
The construction of the 268 JEM groups was based on the occupational codes provided in our survey data. The Norwegian occupational standard is based on international classifications and follows the updated version of the international standard of the International Labor Organization. Data on occupations in the 2006 and 2009 surveys consist of 4-digit STYRK-98 codes, which are based on the International Standard Classification of Occupations, ISCO 88 [
25]. In 2008, a new version of the International Standard Classification of Occupations 2008 (ISCO-08) was launched. Thus, Norway published a new Norwegian standard for occupational classification named STYRK-08, which is based on ISCO-08, with some adjustments in order to make the occupational classification suitable for occupations in the Norwegian labor market. This change led to differences in occupational codes between the previous surveys in 2006 and 2009 and the three later surveys in 2013, 2016, and 2019 [
26].
Since our register data included the 4-digit STYRK-98 codes, we chose to transfer the 4-digit STYRK-08 to STYRK-98. There is no official table of correspondence between the 4-digit STYRK-98 codes and 4-digit STYRK-08 codes. When faced with the choice of having more than one STYRK-98 code to select, we chose to convert to the STYRK-98 code with the highest N in the 2006 and 2009 surveys combined. This applied to 28% of the 4-digit STYRK-08 occupational codes; thus, 72% remained unchanged.
Variables
Constructing the job strain index
The JSI in our study is based on self-reported information with measured items for psychosocial exposures developed by the Statistics Norway (SSB). Following Karasek’s Demand-Control Model [
6], the index is a combination of the psychological demand index (job demand) and decision-latitude index (job control). The measurement of psychological demands and job control followed the guidance of the General Nordic Questionnaire (QPS
Nordic) [
27]. In our study, psychological job demand was measured by four items: (1) quantitative demands, (2) conflicting ways of doing things, (3) insufficient resources, and (4) contradictory requests. Job control or decision-latitude was measured by six items: (1) decide how to go about the work, (2) decide the pace of work, (3) make important decisions, (4) use skills, (5) develop skills, and (6) monotonous work. The item variables were dichotomized as non-exposed and exposed, as described in Tables
4 and
5. Although the construction of Job Strain Index in our study is based on the idea of demand/control model by Karasek (1979), our measured items for psychosocial work exposure included only 10 items represented for two dimensions job demand and job control, compared to the original version of Job Content Questionnaire (JCQ) by Karasek (1979), which included 49 items to reflect the psychological job demands, job control, social support and other factors such as job insecurity, physical demands [
28]. The measured items we used to construct the Job Strain Index in this study is thus a shortened version of JCQ, which is closer to the Swedish version [
29]. The measured items for job strain in Swedish version are validated in the study of Chungkham et al. (2013) [
30].
Table 4
Exposures, Questions, and Non-exposed or Exposed for Job Demand
Quantitative demands | How often do you have to skip lunch due to a heavy workload? “Daily”, “a few days a week”, “once a week”, “a few days a month”, “never” | 1 = Exposed (Daily, a few days a week, once a week), 0 = Non-exposed (A few days a month, never) |
Conflicting ways of doing things | How often do you have to do things you think should have been done differently? “Very often or always”; “Quite often”, “occasionally”; “Quite rare”; “Very rarely or never” | 1 = Exposed (Very often or always, quite often, occasionally), 0 = Non-exposed (Very rarely or never, quite rare) |
Insufficient resources | How often do you get job tasks without sufficient resources? “Very often or always”; “Quite often”; “Occasionally”; “Quite rare”; “Very rarely or never” | 1 = Exposed (Very often or always, quite often, occasionally), 0 = Non-exposed (Very rarely or never, quite rare) |
Contradictory requests | How often do you get contradictory requests from two or more people? “Very often or always”; “Quite often”; “Occasionally”; “Quite rare”; “Very rarely or never” | 1 = Exposed (Very often or always, quite often, occasionally), 0 = Non-exposed (Very rarely or never, quite rare) |
Table 5
Exposures, Questions and Non-exposed or Exposed for Job Control
Decide how to go about the work | Can you decide yourself how to go about doing your work? “To a very high degree”; “To a high degree”; “To some degree”; “To little degree”; “To very little degree” | 0 = Non-exposed (To a high degree or to a very high degree), 1 = Exposed (To some degree, to little degree, to very little degree) |
Decide pace of work | To what extent can you decide your own work pace? “To a very high degree”; “To a high degree”; “To some degree”; “To little degree”; “To very little degree” | 0 = Non-exposed (To a high degree or to a very high degree), 1 = Exposed (To some degree, to little degree, to very little degree) |
Important decisions | Can you influence decisions that are important to your work? “To a very high degree”; “To a high degree”; “To some degree”; “To little degree”; “To very little degree” | 0 = Non-exposed (To a high degree or to a very high degree), 1 = Exposed (To some degree, to little degree, to very little degree) |
Use skills | What are the opportunities in your job to utilize the skills, knowledge and experience you have gained through education and work? “Very good”; “Good”; “Bad”; “Very bad” | 0 = Non-exposed (Very good, good), 1 = Exposed (Very bad, bad) |
Develop skills | How are the opportunities in your job to further develop skills in the areas you desire? “Very good”; “Good”; “Bad”; “Very bad” | 0 = Non-exposed (Very good, good), 1 = Exposed (Very bad, bad) |
Monotonous work | Does your work consist of constantly repeated work tasks? “Almost all the time”, “About three quarters”; “Half the time”; “A quarter of the time”; “Never” | 0 = Non-exposed (A quarter of the time, never), 1 = Exposed (Almost all of the time, about three-quarters, half the time) |
Each item was dichotomized following the same procedure as Hanvold et al. [
4], splitting each scale at the median to identify those who are exposed vs. non-exposed (see Table
4 and
5). Hanvold et al. underscores that defining those who are exposed, in the sense that the level of demands and control poses a health risk, is difficult. Thus, they decided to use the median as a cut-off, following Solovieva [
12] which used the same approach in a Finnish validation study of a job exposure matrix for psychosocial factors. For the individual exposures, we calculated the median value for each item using the raw values and then used the median as a cut-off as to identify the exposed versus non-exposed individuals based on the individual information. The response categories defining exposed vs. non-exposed, which are shown in Table
4 and
5, are based on the median. In example for “Quantitative demands” the median value on the five-point scale was 2. Thus, those with a value above 2 (Daily = 5, a few days a week = 4, once a week = 3) were defined as exposed. Whereas for the occupation-based exposures, we calculated the share of exposed individuals for each item within each JEM group and used the median as a cut-off as to identify individuals defined as exposed and non-exposed based on their occupational code.
We constructed the psychosocial exposure variables in such a way that all variables reflected the proportion of individuals within each of the JEM groups being exposed. The scale of psychosocial exposure variables goes from 0–100%. The occupational codes with a value of 0 indicate that none of these occupational codes have provided an answer that involves exposure. The occupational codes with a value of 100 indicate that all respondents in this occupational code have provided an answer that involves exposure.
In the scholarly literature, job strain has been measured in numerous ways, the most common being the quadrant approach. However, a validation of alternative formulations of job strain shows that using a continuous variable measuring the degree of strain best predicts stress and back pain [
9]. In accordance with this study and the fact that we do not want to lose information by dichotomizing continuous measures, as is the case with the quadrant approach, we constructed a continuous JSI. For the occupational based JSI, we first calculated the mean proportion of individuals within each JEM group reporting to be exposed on the four items measuring demands (see Table
4). A higher value represents a larger share within a JEM group reporting to be exposed to a high degree of demands. Secondly, we calculated the mean proportion of individuals within each JEM group reporting to be exposed on the six items measuring control (see Table
5). A higher value represents a larger share within a JEM group reporting to be exposed to lower degree of control. Thirdly, we added these two numbers together and divided by two. Accordingly, higher values on the index represent higher degrees of demand and lower degrees of control, whereas lower values represent lower degrees of demand and higher degrees of control. The individual JSI was calculated in the same manner, however using the individual based exposures.
Health outcome variables
To test the criterion-related validity of the psychosocial JEM, we examined the association between the JSI and different health outcomes based on both the survey and register data. Information on long-term sick leave and three different mental health symptoms, including anxiety, depression, and sleeping difficulty, were derived from survey data to test the concurrent validity of the constructed JSI. To ascertain the information on sick leave, the following question was asked: ‘During the last 12 months, have you had continuous sick leave of more than 14 days?’ ‘1. Yes, 2. No’. The anxious symptom was tapped by the question: “During the last month, have you been bothered by nervousness, anxiety, or restlessness?” “1. Very bad, 2. Pretty bad, 3. A little, 4. No”. The depressive symptoms were asked by question: “During the last month, have you been bothered by depression?” “1. Very bad, 2. Pretty bad, 3. A little, 4. No”. We recoded these two variables in such a way that people who answered, ‘very bad’ and ‘pretty bad’ were ‘exposed’, and people who answered, ‘A little’ and ‘No’ were ‘non-exposed’.
The sleeping difficulty symptom was asked by the question: “During the last three months, have you had difficulty sleeping because thoughts of work kept you awake?” “1. A few days a week, 2. About once a week, 3. A few times a month, 4. Seldom or never”. We recoded this variable such that people with sleeping difficulty symptoms ‘a few days a week’ and ‘about once a week’ were ‘exposed’ and those who experienced symptoms ‘A few times a month’ and ‘seldom and never’ were ‘non-exposed’. Information on long-term sick leave, mortality, and disability was obtained from register-based data to test the predictive validity of the occupational-level JEM. The long-term sick leave variable identifies individuals having ten long-term sick leave periods or more during 2008 to 2015. Disability was measured by whether individuals received disability benefits during the period 2008 to 2017. The mortality variable provided information on whether the individual died during the period 2008 to 2017.
Summary and discussion
In this paper, we investigated the reliability and validity of our constructed psychosocial JEM, i.e., the JSI. These assessments involved comparisons of individual job strain with occupational job strain, and of their respective psychosocial dimensions and components, as well as an appraisal of the reliability and criterion validity of the occupational JSI itself. Measured by kappa, agreement between individual-based and occupation-based psychosocial exposures was poor to fair. However, the internal consistency of the two dimensions that make up occupation-based job strain, job demand, and job control was clearly acceptable. According to the factor analysis, the construct validity of the JEM was also fully acceptable. As for concurrent validity, assessed by the survey data, individual- and occupation-based job strain were significantly associated with anxiety and depression for men. For women, the significant associations between job strain and anxiety and between job strain and depression were observed only for individual-based job strain but not for occupation-based job strain. With respect to predictive validity, occupation-based job strain was significantly related to all three health outcomes (disability, sick leave, and mortality) in the register data for both genders.
The results pertaining to the reliability of the JSI were somewhat mixed. The measures that compared individual exposures and occupation-based exposures (kappa, sensitivity, and specificity) tended to be poor, although they varied. On the other hand, the measure of consistency of the two dimensions of job strain performed well. The interpretation of the results related to agreement, sensitivity, and specificity is not straightforward since no gold standard exists. In other words, since individual psychosocial estimates cannot be perceived as the gold standard, poor agreement is subject to several interpretations. This may imply that occupation-based results are far from the mark, but it may equally be that they are close to the mark due to systematic bias in the individual estimates. Hence, due to these interpretive challenges, we would argue that poor agreement and occasionally low sensitivity and specificity do not provide evidence implying that our measures of occupation-based job strain, or job demand or job control were unreliable [
36,
37].
Our positive results regarding the predictive validity of the JSI corresponded well with previous studies examining the validity of the JEM in other countries, such as the French psychosocial JEM [
11] and the Finnish psychosocial JEM [
12]. Since the ultimate purpose of this paper was to construct a validated measure of occupation-based psychosocial work environments for use in register data, we find this specific result rather assuring. We are inclined to put more trust in this finding than in the findings emanating from the analysis of the survey data, which were more mixed. Evidence pertaining to future outcomes (the predictive aspect) is generally considered more robust than evidence related to associations established in cross-sectional data (the concurrent aspect) because of the common variance problem [
36]. See also the discussion of limitations below.
Somewhat surprisingly, the occupation-based job strain indicated an elevated risk of anxiety and depression among men but not among women. This does not agree with earlier results showing that higher levels of anxiety and depression were typically reported for women rather than for men [
38,
39]. There are two plausible explanations for this gender difference. First, women may be more familiar with working conditions in high-stress and female-dominated occupations than men, such as teachers, social workers, and nurses [
40]. Hence, women may tend to underreport their exposure at work compared with men, while mental health outcomes are reported to be higher for women than for men (see descriptive statistic results, page 9–10). There is also evidence that male nurses report more work-related disturbances than female nurses [
41], and men working in traditional female jobs may perceive a higher level of social stress than women due to their internalization of the masculinity role [
42]. Second, there is evidence of gender differences in job satisfaction, i.e., that men have more difficulties in achieving job satisfaction and are also more willing to express frustration with working conditions than women [
43]. Thus, our results suggest that an occupation-based JSI may enhance the ability to identify gender differences in the effect of job strain on health outcomes better than an individual JSI.
Although our results support the idea that a JEM is a reproducible and efficient method for examining work-related health risks in epidemiological studies, some limitations should be considered. The JEMs were converted from individual exposure measurements, which may lead to errors in the JEM assignments due to the imprecise information of exposure for each job and other errors in job coding and duration for individuals [
44]. Furthermore, one may argue that JEM is only helpful when job demands within an occupation are comparable, and because JEM assigns the same exposure estimates to all workers with identical job titles, which may affect inter-individual variability, especially in cases where workers have specific tasks [
3], or in the case of digitalization of jobs. Another caveat using the JEM developed by the survey data is the risk of differential misclassification. The risk of misclassification is likely to increase when exposure and health outcomes are assessed simultaneously. The individual characteristics of the workers may additionally contribute to the error in self-reported questionnaires in the sense that workers who constantly “complain about everything” may overreport their working exposures and the situation of their health, while another group who “complain about nothing” may underreport their occupational environment and health [
36]. This approach may also increase subjective bias and the threats of false positive results, as it reflects the individual perception of the work exposure and health outcomes [
45] in cases where workers with health problems tend to report a higher degree of psychosocial exposures than healthy workers. Hence, despite the fact that JEM may provide more objective measures for occupational exposure than self-reported information, this method cannot be seen as a gold standard measure for examining job exposure at work [
36,
37]. As discussed above, neither method can. Our study only constructed a JEM based on Norwegian data; thus, it is only appropriate for generalization within Norway and countries that share the same conditions as Norway. To achieve a better applicable JEM, the idea of constructing an international-level JEM (Job Exposure Matrix International-JEMINI) should be further developed [
46].
We used the same approach as Hanvold et al. [
4] and Solovieva [
12] when defining the exposed versus non-exposed as basis for constructing the JEM. Using the median as a cut-off point may, however, be somewhat arbitrary. Thus, in further developments of the JEM one should experiment with different cut-off points to identify possible thresholds for increased health risks.
The JSI could have been constructed by dividing demands by decision latitude which, in contrast to our chosen approach, would have given distributions approaching second degree functions (hyperboles). The advantage of such an approach is the avoidance of defining subjects in extreme "active" and "passive" groups. With our chosen approach there is a risk of labeling subjects as exposed to job strain, who have extremely high demands and rather high control as well and in the other end those who have low demands and extremely low control. However, we have no reason to believe this being an issue of any significance for the results presented in this paper. Dividing demands by decision latitude would exclude more of such problem cases. In further development of the JSI, dividing demands by decision latitude should also be tested.
The Norwegian labor force remains gender- and class-segregated [
47]. Our study also indicated that men and women have distinct patterns of psychosocial job exposure that may stem from certain occupations, such as nursing. Although current scholarship has documented evidence of the relationship between job strain, occupational class, and gender [
48], few studies have used JEMs. The question of how the risks for different health outcomes are explained by job exposures differentiated by gender and occupational class remains unanswered in our study. Hence, one recommendation is that future research on occupational epidemiology should consider both gender and occupational class when investigating the risk of occupational exposure to health.