Repeated job quits: stepping stones or learning about quality?
© Gielen; licensee Springer. 2013
Received: 14 June 2013
Accepted: 23 July 2013
Published: 7 August 2013
Increasing labor mobility is high on the political agenda because of its supposedly positive effects on labor market functioning. However, little attention has been paid to information imperfections, and to what extent they limit potential efficiency gains of labor mobility. When the quality of a new job offer is known ex ante, job quits serve as a stepping stone to better jobs. Yet, if job quality is only observed ex post, job quits may lead to worse matches. This paper argues that actual job quit behavior is characterized by a mixture of both, and investigates the relative empirical content of both extremes in quit decisions. A variance decomposition shows that for nearly 70% of job quits job quality was observed ex-ante; the remaining 30% was learned ex post. Hence, stimulating job mobility mostly improves labor market outcomes, though governments may aim to further reduce information imperfections in order to maximize the efficacy of labor policies.
KeywordsJob search Job satisfaction Labor mobility
During recent decades, enhancing labor market flexibility has been one of the main pillars of European labor market policy. A flexible labor market is considered desirable because of its ability to quickly adapt to fluctuations and changes in society, leading to more efficient labor market outcomes. It allows, for example, workers to move jobs in order to build a career or to find a job that better matches their personal and family circumstances. However, this is only true if there is sufficient information available to workers to identify good jobs. Looking at some particular patterns in labor mobility, one may wonder whether this is the case. Labor mobility patterns across workers exhibit a great deal of variety (see e.g. Kambourov and Manovskii (2008)). Long-term employment relationships are quite common, yet some workers are involved in many job quits within a short time period (Farber (1999)). Given the recent evidence that workers usually gain in job satisfaction and obtain higher wages after a job quit (e.g. Perez and Rebollo (2005); Chi et al. (2008)), the fact that many decide to change jobs again shortly after an initial quit raises the question whether these job changes always contribute to better matching efficiency or whether some changes simply constitute a relocation of labor without any increase (or even a loss) in match quality. In the latter case, policy aimed at stimulating job mobility may not improve labor market outcomes as much as is expected by policy makers. Better information about the nature of job mobility is essential for formulating effective labor policy.
From a theoretical point of view, job changes can be explained by the presence (or absence) of ex ante information about job quality. At the one extreme, job quality may be perfectly observable at the time a job offer arrives, and hence workers may decide to quit (again) if they receive an offer which is better than their current job. This can be denoted the stepping-stone mechanism, based on the on-the-job search theory by Burdett (1978). At the other extreme, repeated job quits can be explained by the complete absence of ex ante information about job quality − the so-called learning model pioneered by Jovanovic (1979). In this model, job quality is revealed over the time spent in the job. In case job quality turns out to be lower than expected, workers may decide to leave the job again, although the quality of a new job offer cannot be ascertained in advance. Obviously, these two theories can be considered two ends of a continuum representing the degree to which ex ante job quality information is available. In practice, workers may decide to change jobs in a situation where some information about job quality is known ex ante, and the rest has to be learned while in the job. This paper argues that actual job quit behavior is characterized by a mixture of both. The main aim of the paper is to study the extent to which repeated job quits can be explained by the stepping-stone theory versus the learning model, and hence to determine the relative importance of both models in job quit decisions. This information is crucial for policy makers aiming to improve labor market functioning by stimulating labor mobility.
Studying the relationship between job mobility and worker-job match quality is not easy, since match quality is usually not observable. Earlier studies have looked at wages as being an observable outcome of unobserved match quality. Job quits are usually found to be associated with wage gains (Perez and Rebollo (2005), Light (2005)), though not neccesarily (Postel-Vinay and Robin (2002), Neumark (2002)). In addition, a job quit may improve the job match if a job change facilitates moving from a temporary position to a permanent position (Booth et al. (2002)) or if it leads to an improvement of other non-monetary aspects of the job (Altonji and Paxson (1986)). Munasinghe and Sigman (2004) point to the importance of a fundamental search process in order to explain these positive effects on match quality, since unobservable individual effects alone cannot explain the relationship between mobility and wages. A study by Light and McGarry (1998) used the NLSY data to empirically distinguish between several models explaining the relationship between job mobility and wage outcomes. They find that after taking into account the role of individual fixed effects and the ex ante observability of job quality there is still a significant effect of mobility on wage outcomes, which they interpret as evidence for the learning model. However, these previous studies looked for evidence for one model by eliminating one-by-one the other models. This paper will build on this by investigating the relative importance of each model.
Furthermore, the current paper will focus on job satisfaction as a measure for the workers’ perceived match quality, as this not only includes the monetary but also the non-monetary aspects of the job (see section 2.3.1 for a more detailed discussion)1. Earlier studies have shown that people with low job satisfaction are more likely to quit (e.g. Freeman (1978), Akerlof et al. (1988), Clark et al. (1998), Sousa-Poza and Henneberger (2004), Levy-Garboua et al. (2007), Bockermann and Ilmakunnas (2009), Green (2010))2. However, little is known about why sequential job quits might arise. Sequential job search might arise to achieve better occupational matching (e.g. McCall (1990)). For example, Neal (1999) shows that workers always change careers first before they search for their preferred firm to work in. However, sequential job search might also be the result of a poor new job match. We can learn more about this by looking at ex post job quality. Note that there may be other models which can explain job quit behavior. For example, the mover-stayer model which argues that some underlying personality characteristics determine whether someone quits his job often or not. However, the study by Light and McGarry (1998) has shown that the relationship between job mobility and match quality is hardly changed once you control for individual fixed effects. Given the marginal relevance of this model for explaining post-mobility job quality, the current paper will focus only on the two most important models. The role for unobserved individual effects will, however, shortly be addressed when discussing the results.
This paper investigates the role of ex ante information imperfections in job quits using data from the British Household Panel Survey (BHPS), which provides information to distinguish worker-initiated job quits from other job separations. Information about repeated job quits is studied to observe how match quality is affected by subsequent job changes. If match quality always improves following each job quit, then job quit behavior can be considered a stepping stone mechanism, contributing to matching efficiency. Alternatively, in the learning model where job quality is not observable ex ante there is more variation in match quality in the new job. Job quality improves only in expected terms; some workers’ match quality may improve after a job change while for others it may worsen unexpectedly. By using the theoretical predictions from both models, a variance decomposition of job satisfaction in the new job allows me to determine the relative importance of both models. The results illustrate that nearly 70 percent of job characteristics can be observed and exploited to improve job quality by changing jobs (stepping-stone), while there is a 30 percent chance that the new match turns out to be different than expected, either better or worse (learning).
The structure of the paper is as follows. The next section presents a simple theoretical model which sets out possible motivations for repeated job quits. Section 3 describes the data and some stylized facts. In Section 4, the results from the empirical analysis are presented; and Section 5 concludes.
2 Theoretical model
This section presents a model, based on Jovanovic (1984), which combines elements of the stepping stone model (Burdett (1978)), where alternative jobs vary over time due to the arrival of new job offers, with elements of the learning model (Jovanovic (1979)), where the value of the current job match varies due to learning. For presentational simplicity the model is rather stylized (e.g. excluding worker heterogeneity and endogenous changes in match quality), but it captures the essence of the alternative mechanisms that drive worker mobility3. For the purpose of this paper this is sufficient since this section only serves to provide some intuition for how we can identify the relative importance of both models in the data.
For simplicity, workers are assumed to be infinitely lived and risk neutral optimizers. They search in the labor market for their optimal job match, based on several job characteristics such as the wage, working hours, benefits, location, job security, and working conditions. The quality of the match, denoted by μ, is drawn from a normal distribution with mean and variance, i.e.. Workers can obtain information about the true match quality in two steps.
Before the start of the match, workers try to evaluate the quality of the match. This ex ante assessment m = μ + ε is a noisy estimate of the true match quality μ due to. The smaller σ m the easier it is to make a good ex ante assessment of the true match quality. For example, workers’ ability to assess the quality of a job may be imperfect ex ante due to the fact that the ex ante job quality anticipation differs from the way people ex post live the job (Stutzer and Frey (2008)). Put differently, the larger σ m , the more has to be learned about match quality when the employment relationship is ongoing.
and variance. The parameters,,, and are known to the worker.
The extent to which workers can assess true job quality during the job search process before the employment relationship starts may vary between perfect observability and a complete absence of any ex ante job information. I discuss the first of these polar cases in the next subsection.
2.1 Stepping stone model
which shows that a job change always leads to a new job that is at least as good as the previous job. Furthermore, note that F(·) is a cumulative distribution function, which is increasing in J S∗. As a result, Equation (5) is decreasing in J S∗, showing that workers in poor matches are more likely to change to a better job. All in all, when match quality is perfectly observable, repeated job quits serve as a stepping stone to higher quality jobs.
2.2 Learning model
The other extreme is the situation where no information about job quality is available ex ante, i.e. σ m = ∞. In this situation, as is shown by Equation (1), all information about match quality has to be obtained from quality revelations − which can be both surprising or disappointing − while the employment relationship is ongoing (cf. Jovanovic (1979)). Hence, variation in job quality mostly comes from within the job (rather than across jobs). Hence, a worker will decide to quit his job if the revealed quality turns out to be lower than the expected alternative offer, as can be seen from Equation (4). Note that, because of the learning dimension, the new accepted job is not by definition better than the old job, but only in expected terms. Hence, changing jobs generally leads to a better match quality, but there is a certain risk that the match turns out to be worse than expected and that in fact new job quality falls below the quality of the previous job.
2.3 Empirical implementation
2.3.1 Job satisfaction to measure match quality
This paper exploits self-reported job satisfaction as a measure for unobserved job quality. Since true job quality is not observable, job satisfaction is not a direct and error-free measure. However, for several reasons it is likely to be a better measure than wages, which has been used as a proxy for job quality in many previous studies (e.g. Cornelißen (2009))5.
First, job satisfaction is a more general measure than wages, because it not only includes satisfaction with the wage, but also satisfaction with non-monetary characteristics of the job.
Therefore, job satisfaction is more systematically tied to the true job quality.
Second, wages are one of the few job characteristics that can be observed and agreed upon ex ante. Hence, learning is less likely to occur when it comes to wages, but learning might occur for other non-wage characteristics of the job. Hence, taking wages as a measure for job quality is likely to overstate (understate) the relative importance of the stepping-stone (learning) model.
In general, the patterns in wages and job satisfaction are not too far apart in the data (more details on the data see Section 3.1). Following a job quit about 17 percent of the individuals experiences a drop in job satisfaction, whereas 51 percent experiences a gain in job satisfaction. When looking at real hourly wages, both these shares are higher: 23 and 62, respectively6.
This implies that for some of the individuals who experience a wage gain the job as a whole is not evaluated as being better. Similarly, for some individuals with a wage loss the total match is not evaluated as being worse. For the reasons mentioned above, this paper will use self-reported job satisfaction as a measure for job quality.
The models presented in Sections 2.1 and 2.2 provide some testable predictions. First, both models predict that in expected terms job quality in the new job exceeds that in the old job (see Equation (4)). Empirical support for this first prediction is found by investigating the effect of job quits on self-reported job satisfaction. Second, although on average match quality increases in both models following a job quit, the probability of facing unexpectedly low quality only exists in the learning model. To test the validity of the learning model in the data, the probability of experiencing a loss in job satisfaction in the years after a job quit is also studied. The results show both models appear to have some empirical validity in the data.
Though both models represent either ends of a continuum of ex ante observable job quality, reality might be somewhere in the middle. Workers may search for jobs in a situation where some information about job quality might be available ex ante but not all; full information will be revealed while the worker is in the job. In the last − and most important − part of this paper testable predictions from both theoretical models concerning the variance in match quality in the new job are used to investigate the relative empirical content of the stepping stone and the learning model. Both models differ in their predictions concerning the variance in match quality in the new job. Hence, changes in job satisfaction following a job quit are the main source of information about the extent to which workers can observe job quality ex ante.
From Equation (5) it is clear that, according to the stepping stone model, satisfaction in a new job after a job quit is always at least as high as job satisfaction in the current job k. For example, if satisfaction is measured on a 7-point scale, a worker who is very unsatisfied in his current job (J S k = 1) has a low reservation utility and will accept any job offer he receives (J Sk+1 = 1,…,7), while a rather satisfied worker (J S k = 6) will only accept a job offer which will yield a job satisfaction level equal to 6 or higher (J Sk+1 ≥ 6). As a result, the expected variance in job satisfaction in the new job for workers who used to be in a poor quality job is larger than the expected variance in job satisfaction in the new job for workers who used to be in a better quality job, hence Var SS (J Sk+1| for each.
Alternatively, in the learning model the true quality of the new job is unknown ex ante and is a random draw from the job offer distribution. As a result, even though in expected terms new job satisfaction is higher than job satisfaction in the current job, job satisfaction in the current job is unrelated to job satisfaction in the new job. As a result, in the learning model the variance of job satisfaction in new, accepted job offers is a constant regardless of current job quality (Var LM ), while it is decreasing with job satisfaction in the current job according to the stepping stone approach, i.e. ∀.
The importance of both models in actual job quit behavior is tested by relating actual variance in job satisfaction in accepted jobs to the variance that would be expected according to both models. I calculate the expected variances in job satisfaction for both models (Var SS and Var LM ) using the satisfaction distribution among job offers (see Section 4.2 for more details). The actual variance in job satisfaction in accepted job offers Var(J Sk+1) is taken from the data and used to calculate a weight s such that Var(J Sk+1) = s ∗ Var SS (J Sk+1) + (1 − s)∗Var LM . This s is interpreted as the relative importance of the stepping stone model. When s = 1 the stepping stone model perfectly explains quit behavior in the labor market, when s = 0 the learning model is the driving force of job quits. All values of s between 0 and 1 imply that actual job quit behavior is characterized by elements of both models. The larger s, the more effective is labor policy aimed at improving labor market outcomes through increased labor mobility.
3 Data description
The analyses in this paper are based on information from the British Household Panel Survey (BHPS) for the period 1991-2008. The BHPS collects data annually from a representative sample of approximately 16000 individuals from 9000 households. The dataset contains extensive information on labor market positions and transitions, individual and household income, and other job-related characteristics. The analyses are restricted to working-age male workers, as these workers usually have a strong labor force attachment and job changes for this group most likely serve as a means to improve their employment match7.
The wave 1 data were collected in late 1991 - early 1992, the wave 2 data were collected in late 1992 - early 1993, etc. Information on all individual labor market spells that fall between two interview dates is also collected. For each spell information is available on the spell start and end date, as well as the reason for terminating the spell. Workers may report to have terminated the spell for several reasons: promoted, left intentionally, made redundant, dismissed, temporary job ended, took retirement, stopped for health reasons, look after family, care of other person, moved away, started college/university, or left for another reason. This detailed information allows me to pin down job quit behavior. The ending of an employment spell is denoted as a quit if the worker has experienced a job-to-job change from one year to another and reported to have left intentionally8. About 28 percent of all employment spells end for this reason9. Note that job and worker characteristics are only observed for spells that are active on the day of the interview. Therefore, only these spells can be used in the analysis. However, all quits within two interviews are used to determine whether someone had quit multiple times within the survey year. The sample consists of working-age men who had only one quit per year, such that I can compare the quality of the previous job to the quality of the preceding job. Note that the results found in the paper do not change if I include individuals with multiple quits within the survey year, even though for them I can only compare the quality of the previous job with the quality of the (second/third/etc.) new job at the next interview date. Also, including individuals who experience short unemployment or inactivity spells (i.e. less than 3 months) between two jobs does not affect the findings.
Job satisfaction distribution (row %)
Job satisfaction level
Average job satisfaction
< 2 years
≥ 2 years
< 30 hours
≥ 30 hours
Real hourly wage
p25 - p50
p50 - p75
3.2 Descriptive figures
Frequency of job quits, by initial level of job satisfaction (row percentages [No. of persons])
Total number of quits observed
Prob. of having multiple quits (%)
3 or more
Job satisfaction in year before first quit *
No. of observations
4 Empirical results
4.1 Job satisfaction
Job satisfaction after a job quit
I. JS t - FIXED EFFECTS ORDERED LOGIT RESULTS
log L = − 15700.81
B. Including total number of quits sofar
Total number of quits
Q * Total number of quits
log L = − 15637.32
II. P(JS t < JS t −1 ) - FIXED EFFECTS LOGIT RESULTS
J S t−1
log L = − 11911.56
Second, in order to test the predictions regarding (unexpected) drops in new match quality, Part II studies the probability of a reduction in job satisfaction from one year to the other. Although both the stepping stone and the learning model predict an average gain in job satisfaction following a job quit, in the stepping stone model this is the result from only positive changes in job satisfaction, while in the learning model this is a positive sum of all positive and negative changes in job satisfaction. Hence, to distinguish between both models it is necessary that some workers quitting their job experience a decline in job satisfaction. The results from a fixed effects logit model are presented in the lower part of Table 3. The results indicate that job quitters are less likely to experience a reduction in job satisfaction than job stayers. Furthermore, a reduction in job satisfaction is more likely if workers leave a good job. This confirms earlier evidence from the raw data that job satisfaction reductions occur after a job quit, which means that there is a role for the learning model. The relative importance of both models is investigated in the next section.
4.2 Decomposing job satisfaction variance
The evidence thus far indicates that repeated job quit behavior can be characterized both by stepping stone and learning elements. Since the stepping stone model and the learning model represent both ends of a continuum of ex ante observable job quality, in this section I investigate the relative empirical content of the theoretical approaches by decomposing the variance in job satisfaction in newly accepted jobs. Note that the predictions concerning this variance are the main distinction between both models (see also Section 2.3.2). When mobility costs are assumed to be nonexistent, in the stepping stone model workers are expected to accept any job which offers them at least the satisfaction level that they currently experience in their job. As a result, expected variance in satisfaction of accepted job offers will be decreasing with the initial level of job satisfaction. Alternatively, in the learning approach workers accept a job which is expected to offer a higher satisfaction level than they currently experience in their job. However, since job quality in the new job is a random draw and unobservable ex ante the new quality may well be worse and hence the expected variance is independent of job quality in the current job18.
where p r represents the probability of receiving a job offer with satisfaction level equal to r, with R = 1,…,7 and r = 1,…,7. Note that the variance in Equation (7) is decreasing in the level of job satisfaction in the current job, while that in Equation (8) is independent of the current job satisfaction level.
In a next step, the expected variance following the learning model needs to be calculated. The theoretical model predicts that the expected variances following the stepping stone and the learning model should be the same at JS k = 1 if individuals receive one job offer at the time. However, the variances can be different if individuals receive multiple offers at a given point in time: in the stepping stone model they can pick the best offer, in the learning model they cannot distinguish which is the best offer. From Figure 3 it can be seen that it is a likely assumption that individuals receive multiple job offers in a certain time interval, since the model cannot explain the actual variance in satisfaction in the new job for JS k = 1 if both expected variances are the same (because the actual variance at JS k = 1 is higher; 2.28 versus 1.43). This also explains the high number of “good” offers in the observed accepted job satisfaction distribution from Figure 2. Hence, in order to calculate the expected variance for the learning model, where the underlying assumption is that ex ante job quality is not observable, we need to infer the true job offer distribution (i.e. including those offers which were worse than the offer that was accepted) that underlies the observed accepted job offer distribution among labor market entrants. This can easily be done using an optimization program (e.g. in MATLAB) that simulates the true job offer distribution and the true number of job offers that people receive in a certain period such that the combination of both - given the assumption that people can pick the best available offer - would lead to a simulated accepted job offer distribution, which best approximates the observed accepted job offer distribution in Figure 220. As can be seen in Figure 2 the simulated accepted job offer distribution, which has a mean of 4.67 and a standard deviation of 2.37, makes a rather good fit to the observed distribution of accepted job offers. This is based on the simulated number of offers each person receives in a period being equal to two. Now, the simulated true job offer distribution is used to calculate the expected variance following the learning model, which is presented in Figure 3. Since the stepping stone model and the learning model represent both ends of a continuum, it is not surprising to find the actual variance in Figure 3 to be in between both extreme variance predictions.
Variance decomposition - proportion explained by stepping stone theory
Job satisfaction in old job:
Multiple time job
B. JS for new hires from unemployment
C. Ordinal variation measure
D. JS in final year of new job
E. Conditioning on wage and hours worked
where Var, Var(LM), and Var(SS) represent the actual variance (observed in the data) and the expected variance following the learning model and stepping stone model, respectively. The share s and its standard error are obtained from a non-parametric bootstrap with 5000 replications, which is used to calculate Var. From Panel A it appears that close to 70 percent of the job quits arises from a stepping stone motive22. This implies that labor policies aimed at improving labor market outcomes through stimulated job mobility can be quite effective. As part of a sensitivity analysis, Panel B replicates the results using an alternative accepted job offer distribution. Because labor market entrants lack any labor market experience they may receive relatively more poor job offers and hence low job offers may be over-represented in the accepted job offer distribution. Alternatively, labor market entrants may have started their job search well before the end of their studies and hence could have acted more selectively than other workers. Therefore, Panel B uses the distribution of accepted job offers by those workers who were hired from unemployment. These workers are also expected to accept any job offer (as suggested by Christensen et al. (2005)) and the results show that the importance of the stepping stone model is somewhat higher here23. As part of a sensitivity analysis, Panel C takes into account the ordinal nature of the job satisfaction variable. That is, because satisfaction is not a cardinal variable, the variance may not be the best measure of dispersion, because it imposes a supraordinal assumption about the nature of the continuum underlying the different categories (Blair and Lacy (2000)). Therefore, in Panel C I use an index for ordinal variation based on Berry and Mielke (1992) to calculate s. It appears that the results are not much different from those in Panel A.
The role of the stepping stone model might be overrated in Panels A to C for several reasons. First, if mobility costs are existent and positive, workers will only accept a new job if it yields a strictly higher utility than the current job24. As a result, variance resulting from workers accepting a new job of the same quality as the previous job will no longer be attributed to the stepping stone model but to the learning model. Though for unsatisfied workers this will happen rarely (up to 6 percent of the cases), satisfied workers are much more likely to accept a new job with similar job satisfaction rating (about 50 percent of the cases). As a result, the shares presented in Panels A to C should be considered as an upper bound. Alternatively, the importance of the stepping stone model might be misstated if workers have not completely learned the true job quality during the first year in the job, because Panels A to C relate job satisfaction in the old job to job satisfaction reported in the first year of the new job. Therefore, in Panel D, I use job satisfaction reported in the final year of the new job when learning is expected to be completed25. Note that the share of variance attributed to the stepping stone model is similar. Alternatively, the importance of learning could be overstated if individuals answer differently to job satisfaction questions in different waves (which could occur for example if they happen to be in a very bad mood when filling in the questionnaire). Finally, in Panel E I look at job satisfaction while conditioning on wages and hours worked. After running a job satisfaction estimation (similar to the one presented in Table 3), one can predict what job satisfaction in the new job would have been if the real hourly wage and the number of working would have been the same as in the old job. Since wages and working hours are usually job characteristics that are observable ex-ante, it is not surprising that the role of the stepping stone theory is smaller once you condition on having no change in these job characteristics. Nevertheless, the results are not very different from the results in Panel A.
Variance decomposition - sensitivity
Job satisfaction in old job:
B. Single vs. multiple quits
Single time job quitters
Multiple time job quitters
C. Young vs. older workers
Age < 30
Age ≥ 30
D. Low vs. high educated
E. Occupational change
F. 1990s vs 2000s
Variance decomposition - quit vs. stay
Job satisfaction in old job:
Multiple time job quitters
B. Job stayers
Difference (A - B)
This paper studies repeated job quit behavior to investigate whether such job changes contribute to better matching efficiency or whether they constitute a relocation of labor without any increase in match quality. This information is crucial for labor market policy, in which increased labor mobility is often an important tool used by policy makers to improve labor market outcomes. Theoretical studies often adopt either the stepping stone model or the learning model as the explanatory mechanism for labor mobility. The main difference between these two is that the former assumes perfect observability of job quality before the job starts and hence only allows for job quality improvements after a job quit, whereas in the latter job quality cannot be assessed ex ante and hence job quality is expected to improve after a job quit but may as well end up being lower. This paper argues that actual job quit behavior is characterized by a mixture of both. Therefore, the main aim of the paper is to investigate the relative empirical content of both models in job quit decisions. The results from a variance decomposition help improve our understanding of job quit behavior, a key phenomenon determining the functioning of the labor market, which is essential for formulating effective labor policy.
Using UK data over the period 1991-2008, the analyzes in this paper show that on average job satisfaction increases with each job quit, though at a decreasing rate. This finding is consistent with both the stepping stone and the learning model. However, the fact that some job quitters experience a reduction in job satisfaction suggests that at least some quits can be explained by the learning model. This paper is the first to quantify the relative empirical content of both models. A decomposition of variance in satisfaction in the new job shows that close to 70 percent of job quits arises from a stepping stone motive. This implies that repeated job quits mainly serve as a stepping stone to more happiness at work and as such may contribute to matching efficiency.
This result indicates that government policy aiming to increase labor mobility can be very effective in improving labor market outcomes. However, the efficacy can be even higher if policy is more specifically targeted to elicit within-occupation job changes, where ex ante information seems more easily observable. Furthermore, there is still room for improvement if policy makers would not only focus on increased job mobility, but also would invest in transparency of labor markets. If workers would be more capable of observing job quality ex ante, they can better distinguish good jobs from bad jobs, and job mobility is more likely to improve matching efficiencies.
1 Some economists are skeptical about using a self-reported satisfaction measure, because of measurement issues and difficulties in interpersonal comparisons. Recent papers by Blanchflower D (2008) and Oswald and Wu (2009) address a number of those reservations by illustrating the robust findings in the satisfaction literature and how satisfaction is related to more objectively observable measures of wellbeing.
2 Note that this follows a large psychological literature, where these effects have been investigated before.
3 Earlier studies such as MacDonald (1988) have extended this baseline framework to allow for e.g. heterogeneous workers and/or firms.
4 For simplicity, search and mobility costs are assumed to equal zero. However, the predictions of the model are not affected when positive search costs are introduced in the model.
5 Note that job duration is often considered to be an indicator of quality. However, job duration is theresult of high job quality, but not so much a good indicator. That is, some recently started employment relationships can be very good, even though tenure in the job is still very low. Job satisfaction however is able to measure job quality even for such jobs.
Cross-tabulation wage and job satisfaction changes
Change in JS:
7 For women, job changes may serve to gradually leave the labor market for child care reasons, while job mobility after that may serve to facilitate re-entering the labor market gradually. Though interesting, these job changes may not serve to find the most productive match in the labor market. Note that some older workers may already be at the end of their job search process. However, sensitivity results indicate that the results remain unchanged when I restrict the sample to individuals who are observed in the data from early ages onwards.
8 Note that promotions are not being part of this quit definition, which only covers employer changes.
9 Note that the distinction between quits and layoffs is not always straightforward (see also McLaughlin (1991)), as someone may report having left intentionally after being notified of an upcoming dismissal. Nevertheless, the distinction between quits and layoffs seems economically meaningful since the share of workers reporting a drop in job satisfaction after a job change (without an intervening unemployment spell) is much higher for workers who changed jobs due to layoff (30 percent) than for workers who left for a better job (19 percent).
10 A similar picture can be made for those who change jobs following a layoff and for those who get promoted (not presented in paper; available from the author upon request). However, contrary to the graph for job quitters, both graphs are rather flat, the only difference being that average job satisfaction among those being promoted is similar to that of stayers while the average job satisfaction among those being laid off is slightly lower.
11 The difference in job satisfaction in the year after the job quit are significantly different.
12 Note from Figure 1 that after two years job satisfaction of multiple-time quitters seems to catch up again. This might be the result of a subsequent job quit: about 64 percent of all multiple-time quitters changes jobs again within two years.
13 The advantage of this approach is that all observations for individuals whose satisfaction score changes at least once are included, while a common threshold implies that only those individuals are included whose satisfaction score crosses the given threshold.
14 Note that the results are unchanged when y it is defined as y it = 1 if J S it > c i and 0 otherwise.
15 Including a dummy variable for other types of separations does not improve the model fit. Furthermore, job satisfaction appears to decrease after a layoff, while a small positive effect is found for promotions.
17 The number of job quits before the start of the sample is censored. However, this is assumed to be captured by the individual fixed effect.
18 Note that this is conditional on the worker having decided to leave his job. The probability of leaving a job if lower for people in good jobs, regardless of ex ante information availability.
19 The implicit assumption here is that accepting any job offer that comes along is preferred over having no job at all. This assumption is based on empirical evidence showing that (i) the quality of job offers received is better for employed than for non-employed (e.g. Boheim and Taylor (2002)) and that (ii) employed job search is more effective than unemployed search (e.g. Blau and Robins (1990), Longhi and Taylor (2011)). Labor market entrants are defined as those whose main labor market position is fulltime education in one year and being employed in the next. Note that job satisfaction in the first year of the new accepted job is used. Sensitivity checks, where different distributions are chosen, will be presented later in this section.
20 Here, I assume that the underlying “true” distribution is normally distributed. When I would assume a uniform distribution with multiple job offers, the optimization procedure could not converge to a likely distribution.
21 Hence, 1 minus this share represents the importance of learning about job quality.
22 A similar variance decomposition for promotions yields approximately similar results (0.669). For layoffs, however, starting in a new job is much more risky (0.443).
23 The results for those with job satisfaction in the old job less than or equal to 2 should be interpreted with caution. This number is slightly higher than 1, because the actual variation is nearly equal to the variation as predicted by the stepping-stone model. However, there were very few men who were hired from unemployment who reported job satisfaction of level 1 or 2 (N = 42 and N = 62, respectively). Hence, the predicted variance, and hence the result, is probably not be very precise.
24 Note that in this situation job changes by workers who reported being completely satisfied in the old job (JS k = 7) can still occur if JS∗,k < JS∗,k+1 although only JS k = JSk+1 = 7 is observed in the data.
25 The final year is either the year before a new job quit occurs, or the last year in which the worker is observed in the sample.
26 The extremely high variance for the most dissatisfied job stayers may be due to a relatively low number of observations. Alternatively, it may be the case that this extreme dissatisfaction may make people try very hard to achieve a certain change in their job, where this turns out to be either very successful (i.e. high satisfaction in the next year) or very unsuccessful (i.e. very low satisfaction in the next year). Alternatively, satisfied workers may also receive such offers, but the low variance results from their satisfaction level being close to the upper limit of the satisfaction scale already.
The author would like to thank Lex Borghans, Arnaud Dupuy, Bart Golsteyn, Dan Hamermesh, Erzo Luttmer, Rob McMillan, Bob Pollak, Trudie Schils, Jeffrey Smith, an anonymous referee, seminar participants at Maastricht University, IZA and AIAS, and conference participants at the 2008 EALE and SOLE, and the 2009 IZA/SOLE conferences for helpful suggestions.
Responsible editor: Alan Barrett
- Akerlof G, Rose A, Yellen J, Hall L, Hall R: Job switching and job satisfaction in the u.s. labor market. Brookings Paper on Econ Act 1988, 2: 495–594.View ArticleGoogle Scholar
- Altonji J, Paxson C: Job characteristics and hours of work. Res in Labor Econ 1986,8(A):1–55.Google Scholar
- Berry K, Mielke P: Assessment of variation in ordinal data. Percept Mot Skills 1992, 74: 63–66. 10.2466/pms.19220.127.116.11View ArticleGoogle Scholar
- Blair J, Lacy MG: Statistics of ordinal variation. Sociol Methods & Res 2000,28(3):251–280. 10.1177/0049124100028003001View ArticleGoogle Scholar
- Blanchflower D: Happiness economics. NBER Reporter 2. 2008.Google Scholar
- Blau F, Robins P: Job search outcomes for the employed and unemployed. J Pol Econ 1990,98(3):637–655. 10.1086/261698View ArticleGoogle Scholar
- Bockermann P, Ilmakunnas P: Job disamenities, job satisfaction, quit intentions, and actual separations: Putting the pieces together. Ind Relat 2009,48(1):73–96. 10.1111/j.1468-232X.2008.00546.xView ArticleGoogle Scholar
- Boheim R, Taylor M: The search for success: Do the unemployed find stable employment? Labour Econ 2002,9(6):717–735. 10.1016/S0927-5371(02)00074-XView ArticleGoogle Scholar
- Booth A, Francesconi M, Frank J: Temporary jobs: Stepping stones or dead ends? The Econ J 2002,112118(480):F189-F213.View ArticleGoogle Scholar
- Burdett K: A theory of employee job search and quit rates. The Am Econ Rev 1978,68(1):212–220.Google Scholar
- Chamberlain G: Analysis of covariance with qualitative data. Rev Econ Stud 1980, 47: 225–238. 10.2307/2297110View ArticleGoogle Scholar
- Chi W, Freeman R, Kleiner M: Does changing employers improve job satisfaction? Mimeo. 2008.Google Scholar
- Christensen B, Lenz R, Mortensen D, Neumann G, Werwatz A: On-the-job search and the wage distribution. J Labor Econ 2005,23(1):31–58. 10.1086/425432View ArticleGoogle Scholar
- Clark A, Georgellis Y, Sanfey P: Job satisfaction, wage changes and quits: Evidence from germany. Res Labor Econ 1998, 17: 95–121.Google Scholar
- Cornelißen T: The interaction of job satisfaction, job search, and job changes. an empirical investigation with german panel data. J Happiness Stud 2009, 10: 367–384. 10.1007/s10902-008-9094-5View ArticleGoogle Scholar
- Farber HS: Mobility and stability: The dynamics of job change in labor markets. In Handbook of labor economics, Volume 3B. Edited by: Ashenfelter O, Card D. Amsterdam: Elsevier; 1999:2439–2483.View ArticleGoogle Scholar
- Ferrer-i Carbonell A, Frijters P: How important is methodology for the estimates of the determinants of happiness? The Econ J 2004,114(July):641–659.View ArticleGoogle Scholar
- Freeman R: Job satisfaction as an economic variable. Am Econ Rev 1978,68(2):135–141.Google Scholar
- Green F.: Well-being, job satisfaction and labour mobility. Labour Econ 2010, 17: 897–903. 10.1016/j.labeco.2010.04.002View ArticleGoogle Scholar
- Jovanovic B: Job matching and the theory of turnover. J Pol Econ 1979, 87: 972–990. 10.1086/260808View ArticleGoogle Scholar
- Jovanovic, B: Matching, turnover, and unemployment. J Pol Econ 1984,91(1):108–122.View ArticleGoogle Scholar
- Kambourov G, Manovskii I: Rising occupational and industry mobility in the united states: 1968–97. Int Econ Rev 2008,49(1):41–79. 10.1111/j.1468-2354.2008.00473.xView ArticleGoogle Scholar
- Levy-Garboua L, Montmarquette C, Simonnet V: Job satisfaction and quits. Labour Econ 2007, 14: 251–268. 10.1016/j.labeco.2005.08.003View ArticleGoogle Scholar
- Light A: Job mobility and wage growth: Evidence from the nlsy79. Monthly Labor Rev 2005,128(2):33–39.Google Scholar
- Light A, McGarry K: Job change patterns and the wages of young men. Rev Econ Stat 1998,80(2):276–286. 10.1162/003465398557519View ArticleGoogle Scholar
- Longhi S, Taylor M: Explaining differences in job search outcomes between employed and unemployed job seekers. IZA Discussion Paper 5860, Bonn. 2011.Google Scholar
- MacDonald G: Job mobility in market equilibrium. The Rev Econ Stud 1988,55(1):153–168. 10.2307/2297535View ArticleGoogle Scholar
- McCall B: Occupational matching: A test of sorts. The J Pol Econ 1990,98(1):45–69. 10.1086/261668View ArticleGoogle Scholar
- McLaughlin A: A theory of quits and layoffs with efficient turnover. The J Pol Econ 1991,99(1):1–29. 10.1086/261738View ArticleGoogle Scholar
- Munasinghe L, Sigman K: A hobo syndrome? mobility, wages, and job turnover. Labour Econ 2004, 11: 191–218. 10.1016/j.labeco.2003.05.001View ArticleGoogle Scholar
- Neal D: The complexity of job mobility among young men. J Labor Econ 1999,17(2):237–261. 10.1086/209919View ArticleGoogle Scholar
- Neumark D: Youth labor markets in the united states: Shopping around vs. staying put. The Rev Econ Stat 2002,84(3):462–482. 10.1162/003465302320259475View ArticleGoogle Scholar
- Oswald AJ, Wu S: Objective confirmation of subjective measures of human well-being: Evidence from the usa. Science 2009,327(5965):576–579.View ArticleGoogle Scholar
- Perez JI, Rebollo YS: Wage changes through job mobility in europe: A multinomial endogenous switching approach. Labour Econ 2005, (4): 531–555.View ArticleGoogle Scholar
- Postel-Vinay F, Robin JM: The distribution of earnings in an equilibrium search model with state-dependent offers and counter-offers. Int Econ Rev 2002,43(4):989–1016. 10.1111/1468-2354.t01-1-00045View ArticleGoogle Scholar
- Sousa-Poza A, Henneberger F: Analyzing job mobility with job turnover intentions: An international comparative study. J Econ Issues 2004,38(1):113–137.Google Scholar
- Stutzer A, Frey BS: Stress that doesn’t pay: The commuting paradox. The Scandinavian J Econ 2008,110(2):339–366. 10.1111/j.1467-9442.2008.00542.xView ArticleGoogle Scholar
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