Abstract
We describe the functioning of a two-region economy characterized by asymmetric wage setting. Labour market tightness in the leading-region affects wages in the whole economy. In equilibrium, net labour demand shifts towards the leading region raise unemployment elsewhere and leave regional wages unchanged, causing an increase in aggregate unemployment. Based on SHIW micro-data on earnings, we find strong evidence that wages in Italy only respond to Northern unemployment. We estimate that around 33% of the increase in Italian unemployment during 1977–1998 can be explained by regional mismatch, mainly due to an excess labour supply growth in the South.
Similar content being viewed by others
Notes
To check the robustness of our results to the parametric specification of preferences, in Appendix A we allow for CES preferences, with an arbitrary value of the elasticity of substitution between c 1r and c 2r and we estimate the impact of regional mismatch as σ ranges between 0 and 2.
Note that \(p_{1} c_{{1r}} + p_{2} c_{{2r}} = c^{\alpha }_{{1r}} c^{{1 - \alpha }}_{{2r}}\) implies \(\alpha = {{\left( {p_{1} c_{{1r}} } \right)}} \mathord{\left/ {\vphantom {{{\left( {p_{1} c_{{1r}} } \right)}} {c^{\alpha }_{{1r}} c^{{1 - \alpha }}_{{2r}} }}} \right. \kern-\nulldelimiterspace} {c^{\alpha }_{{1r}} c^{{1 - \alpha }}_{{2r}} }\). Given the market-clearing condition, this in turn implies \(\alpha = {{\left( {p_{1} Y_{1} } \right)}} \mathord{\left/ {\vphantom {{{\left( {p_{1} Y_{1} } \right)}} {Y^{\alpha }_{1} }}} \right. \kern-\nulldelimiterspace} {Y^{\alpha }_{1} }Y^{{1 - \alpha }}_{2} = {{\left( {w_{1} N_{1} } \right)}} \mathord{\left/ {\vphantom {{{\left( {w_{1} N_{1} } \right)}} {{\left[ {{\left( {A_{1} N_{1} } \right)}^{\alpha } {\left( {A_{2} N_{2} } \right)}^{{1 - \alpha }} } \right]}}}} \right. \kern-\nulldelimiterspace} {{\left[ {{\left( {A_{1} N_{1} } \right)}^{\alpha } {\left( {A_{2} N_{2} } \right)}^{{1 - \alpha }} } \right]}}\).
Previous concepts of mismatch (see Jackman et al. 1991) focus on the dispersion of relative unemployment rates, rather than on the direct evolution of sectoral demand and supply of labour. By focusing on the (endogenous) unemployment dispersion, the LNJ index does not distinguish pure demand and supply imbalances from adjustments in relative wages and unemployment rates due to different sources. Some later work (Nickell and Bell 1995) focused directly on demand/supply measures, but used absolute rather than relative measures of mismatch, given by dln(α=l), which would not necessarily have the same absolute magnitude and opposite signs for the two groups of workers considered. Relative measures of mismatch similar to the one adopted in this paper are used by Manacorda and Petrongolo (1999).
The existence of an inverse relationship between wages and unemployment is largely acknowledged in empirical research (Blanchflower and Oswald 1994; Card 1995), although no single micro-foundation is to date recognized as superior to others. It is not in the scope of this paper to investigate such micro-foundations. It has been argued that a downward sloping relationship between wages and unemployment may stem from wage bargaining (Manning 1993), efficiency wages (Shapiro and Stiglitz 1984) or search frictions (Pissarides 2000). See Card (1995) for a discussion.
The SHIW does not allow the computation of ILO unemployment rates, as the only available information on labour market status is whether an individual ever worked during the year preceding the survey. For further details on the SHIW, see Cannari and Gavosto (1994).
We exclude the 1987 wave, when the variable denoting the region of residence is coded at a somewhat less detailed level.
North includes: (1) Piedmont-Val d'Aosta-Liguria, (2) Lombardy, (3) Trentino Alto Adige-Veneto-Friuli Venezia Giulia, (4) Emilia Romagna, (5) Tuscany-Umbria-Marches, (6) Latium. South includes: (7) Campania, (8) Abruzzi-Molise-Apulia, (9) Basilicata-Calabria, (10) Sicily-Sardinia.
Clearly, the bulk of the increase in unemployment took place before 1989 (see Fig. 1). Therefore, most of the explanatory power of the regional mismatch story also refers to the 1977–1989 sub-period.
This result however is somewhat sensitive to our specification of preferences. In the appendix we illustrate how departures from the Cobb–Douglas assumption may potentially affect our results, which suggests that the point estimates of this section should be treated with some caution.
In order to make computations we have used data on net migration rates between the Southwest and the rest of the country and the Northwest and the rest of the country in 1970, as provided by Attanasio and Padoa-Schioppa (1991), (Table 6.4, p. 289).
References
Abraham K, Katz L (1986) Cyclical unemployment: sectoral shifts or aggregate disturbances? J Polit Econ 94(3):507–522
Attanasio O, Padoa-Schioppa F (1991) Regional inequalities, migration and mismatch in Italy, 1960–1986. In: Padoa-Schioppa F (ed) Mismatch and labour mobility. Cambridge University Press, Cambridge, pp 237–320
Becker S, Bentolila S, Fernandes A, Ichino A (2004) Job insecurity and children's emancipation. IZA Discussion Paper No1046
Bentolila S, Ichino A (2002) Unemployment and consumption: are job losses less painful near the Mediterranean? CEPR Discussion Paper No. 2539
Blanchard OJ, Diamond PA (1989) The beveridge curve. Brookings Pap Econ Act 0(1):1–76
Blanchflower D, Oswald A (1994) The wage curve. MIT, Cambridge
Bodo G, Sestito P (1991) Le vie dello sviluppo. Il Mulino, Bologna
Bodo G, Sestito P (1994) Squilibri territoriali nel mercato del lavoro e infazione. In: Dell'Aringa C (ed) Caratteri strutturali dell'inflazione Italiana. Il Mulino, Bologna
Brunello G, Lupi C, Ordine P (2000) Regional disparities and the Italian NAIRU. Oxf Econ Pap 52(1):146–177
Brunello G, Lupi C, Ordine P (2001) Widening differences in Italian regional unemployment. Labour Econ 8(1):103–129
Cannari L, Gavosto A (1994) L'indagine della Banca d'Italia sui bilanci delle famiglie: Una descrizione dei dati sul mercato del lavoro. Econ Lav 28:63–79
Card D (1995) The wage curve: a review. J Econ Lit 33(2):785–799
Casadio P (1999) Diffusione dei premi di risultato e differenziali retributivi territoriali nell'Industria. Lavoro Relaz Ind 1:57–81
Casavola P, Gavosto A, Sestito P (1995) Salari e mercato del lavoro locale, Banca d'Italia. Servizio Studi Banca d'Italia
Cella P, Treu T (1989) Relazioni industriali. Il Mulino, Bologna
Daveri F, Faini R (1999) Where do migrants go? Oxf Econ Pap 51(4):595–622
Faini R (1999a) Trade unions and regional development. Eur Econ Rev 43(2):457–474
Faini R (1999b) Flessibilità e mercato del labouro nel mezzogiorno: una terapia senza controindicazioni? In: Biagioli M, Caroleo FE, Destefanis S (eds.) Struttura della contrattazione, differenziali salariali e occupazione in ambiti regionali. Edizioni Scientifiche Italiane. Napoli, pp 1–25
Faini R, Galli G, Gennari P, Rossi F (1997) An empirical puzzle: falling migration and growing unemployment differentials among Italian regions. Eur Econ Rev 41(3–5):571–579
Fujita M, Thisse JF (2002) The economics of agglomeration. Cambridge University Press, Cambridge
Fujita M, Krugman P, Venables AJ (2000) The spatial economy, cities, regions, and international trade. MIT, Cambridge
Hall R (1970) Why is the unemployment rate so high at full employment? Brookings Pap Econ Act 3:369–402
Harris J, Todaro M (1970) Migration, unemployment and development: a two-sector analysis. Am Econ Rev 60(1):126–142
IMF (2000) Italy: selected issues. Country Reports
ISTAT (1995) Rapporto annuale. La situazione del Paese nel 1994, Roma
ISTAT, Annuario Statistico Italiano. various issues
Jackman R, Layard R, Savouri S (1991) Mismatch: a framework for thought. In: Padoa-Schioppa F (ed) Mismatch and labour mobility. Cambridge University Press, Cambridge, pp 44–101
Layard R, Nickell S, Jackman R (1991) Unemployment: macroeconomic performance and the labour market. Oxford University Press, Oxford
Lilien D (1982) Sectoral shifts and cyclical unemployment. J Polit Econ 90(4):777–793
Lipsey R (1960) The relation between unemployment and the rate of change of money wages in the United Kingdom, 1862–1957: a further analysis. Economica 27(105):1–31
Manacorda M (2004) The fall and rise of earnings inequality in Italy: a semipara-metric analysis of the role of institutional and market forces. J Labour Econ 22(3):586–613
Manacorda M, Moretti E (2003) Intergenerational transfers and household structure: why most Italian youths live with their parents? Mimeo, CEP (LSE)
Manacorda M, Petrongolo B (1999) Skill mismatch and unemployment in OECD countries. Economica 66(262):181–207
Manning A (1993) Wage bargaining and the Phillips curve: the identification and specification of aggregate wage equations. Econ J 103(416):98–118
Nickell S, Bell B (1995) The collapse in demand for the unskilled and unemployment across the OECD. Oxf Rev Econ Policy 11:40–62
Padoa-Schioppa F (1999) Regional aspects of unemployment in Italy and Europe. CEPR Discussion Paper No. 2108
Paniccia I (2002) Industrial districts: evolution and competitiveness in Italian firms. Edward Edgar, Cheltenham
Pissarides C (2000) Equilibrium unemployment theory, 2nd edn. MIT, Cambridge
Pissarides C, Wadsworth J (1987) Unemployment and the interregional migration of labour. Econ J 99(397):739–755
Shapiro C, Stiglitz J (1984) Equilibrium unemployment as a worker discipline device. Am Econ Rev 74(3):433–444
Author information
Authors and Affiliations
Corresponding author
Additional information
Responsible editor: Alessandro Cigno
We are grateful to David Card, Richard Jackman, Alan Manning, Roberto Torrini, seminar participants at the LSE and UCL and two anonymous referees. Barbara Petrongolo gratefully acknowledges financial support from CNR (grant no. 97.01231.CT10).
Appendix
Appendix
CES utility function
One of the building blocks of our model is Cobb–Douglas preferences. Below we check how sensitive our results are to this assumption, by adopting (more general) CES preferences.
Suppose that consumers in both regions have CES preferences over regional goods, while the specification of technology in both regions remains unchanged from Eq. (1). Consumers solve the following problem
,where σ=1/(1−ρ) represents the elasticity of substitution between the two commodities.
The first-order conditions to the maximization in Eq. (18) are:
Eqs. (19) and (20) can be rewritten as
Equation (22) implies c 11/c 21=c 12/c 22. Combining this with the market-clearing conditions \(Y_{1} = c_{{11}} {\left( {N_{1} + \frac{{c_{{12}} }}{{c_{{11}} }}N_{2} } \right)}\) and \(Y_{2} = c_{{21}} {\left( {N_{1} + \frac{{c_{{22}} }} {{c_{{21}} }}N_{2} } \right)}\) gives \({c_{{11}} } \mathord{\left/ {\vphantom {{c_{{11}} } {c_{{21}} = }}} \right. \kern-\nulldelimiterspace} {c_{{21}} = }{c_{{12}} } \mathord{\left/ {\vphantom {{c_{{12}} } {c_{{22}} }}} \right. \kern-\nulldelimiterspace} {c_{{22}} } = {Y_{1} } \mathord{\left/ {\vphantom {{Y_{1} } {Y_{2} }}} \right. \kern-\nulldelimiterspace} {Y_{2} }\) and finally
The profit maximization condition for firms implies w r =p r A r , r=1, 2. Therefore Eq. (23) can be rewritten as
or, alternatively,
According to Eq. (26), the regional mismatch index under CES preferences is
with \(D^{1}_{{12}} = D_{{12}} \).
In Table 5 we estimate the trend in \(D^{\sigma }_{{12}}\) for values of σ in the range [0,2]. The first column reports the annual change in the South–North unemployment differential. The second column reports estimates of \(D^{\sigma }_{{12}}\), as the sum of the annual average change in u 2−u 1 and the proportional annual average change in w 1/w 2, multiplied by σ. Note that, given Eq. (27), \(D^{\sigma }_{{12}}\) represents the part of the change in the South–North unemployment differential that can be explained by regional mismatch.
As σ increases, the estimated mismatch index is reduced due to the higher weight on relative wage changes. Since wage differentials evolved in favor of the South, it turns out that for high-enough values of σ, relative wage changes overweight changes in the unemployment differential and the demand index switches sign. In any case, the change in net relative demand is not significantly different from zero for values of σ above 1.5. For σ=0, corresponding to Leontieff preferences, the demand shift is exactly equal to the change in unemployment differentials: relative wage changes do not induce any substitution between the two labour inputs. For σ=0.5, observed demand shifts account for approximately 60% of the total change in unemployment differentials. When σ=1, which is the Cobb–Douglas case, this accounts for approximately 40% of the rise in the unemployment rate differential. Note that such predicted change in u 2−u 1 is simply equal to the rise in u 2, given that Northern unemployment is not affected by regional mismatch when preferences are of Cobb–Douglas type, as illustrated in Sect. 2.
Rights and permissions
About this article
Cite this article
Manacorda, M., Petrongolo, B. Regional mismatch and unemployment: theory and evidence from Italy, 1977–1998. J Popul Econ 19, 137–162 (2006). https://doi.org/10.1007/s00148-005-0001-7
Received:
Accepted:
Published:
Issue Date:
DOI: https://doi.org/10.1007/s00148-005-0001-7