Abstract
In recent years, temporary employment has risen in almost all European countries, and atypical contracts have been used to obtain labour market flexibility and to respond to the high level of European unemployment. The standard arrangement of Italian employees has traditionally been full-time, permanent, and characterized by a high degree of employment protection. However, recent labour market reforms1 have changed the institutional set-up, and atypical employment forms, among them temporary contracts, have been growing in importance.
As part of my PhD thesis, this study has been financed by the Marche Polytechnic University doctoral fellowship.
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- 1.
The SHIW and further details on the dataset are available on the web-server of the Bank of Italy: http://www.bancaditalia.it/statistiche/indcamp/bilfait.
- 2.
2 An individual is unemployed if s/he declares him/herself to be either a first-job seeker or unemployed in section B (Employment and Incomes) question ‘Apqual’ of the SHIW questionnaire. The information about the employees' contract type comes from the answer to question ‘Contratt’ of annex B1 (information about the employees' job).
- 3.
The scaled estimates of the parameters are required to estimate the average partial effects. See e.g. Wooldridge (2002), pp. 495, for further details.
- 4.
The parental dummies are: four dummies indicating the parents' maximum attained educational levels and one dummy indicating whether one of the parents is a public employee.
- 5.
See Appendix A-1 for more details on the definition and estimation of the APEs.
- 6.
The estimation results of a simple dynamic pooled probit model are available from the author but not reported for the sake of brevity.
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Appendices
Appendix
Estimation of the Average Partial Effects
In the analysis reported, the APEs, or marginal effects, were estimated following Stewart (2007): I estimated the counter-factual outcome probabilities evaluated at the sample means, \( \bar{x}_{1} . \)
Let us call \( p_{U} ,p_{P} , \) and \( p_{T} \) the probability of permanent employment given, respectively, unemployment, permanent employment, and temporary employment at time \( t - 1. \) Hence, on performing the Wooldridge’s analysis, I had that
and
where \( \hat{c}_{1i} \) is the estimated linear approximation (7.5) of unobserved heterogeneity. When I adopted the Heckman’s estimator, the outcome probabilities had to be rescaled because of a different normalisation, so that the arguments of the standard normal c.d.f were multiplied by \( (1 - \hat{\lambda })^{1/2} . \) Moreover \( \hat{c}_{1i} \) is, in this case, the estimated correlated random effect according to specification (7.3).
Hence, the estimated APEs were defined as \( A\hat{P}E_{H}^{J} = \hat{p}_{J} - \hat{p}_{H} \) with J,H = U,P,T. For example, \( A\hat{P}E_{U}^{T} \) was the effect of a temporary job at time \( t - 1, \) rather than unemployment, on the probability of being a permanent worker at time t.
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Picchio, M. (2012). The Dynamics of Unemployment, Temporary and Permanent Employment in Italy. In: Addabbo, T., Solinas, G. (eds) Non-Standard Employment and Quality of Work. AIEL Series in Labour Economics. Physica-Verlag HD. https://doi.org/10.1007/978-3-7908-2106-2_7
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