Parametric approaches to welfare measurement
1 / 23

Parametric Approaches to Welfare Measurement - PowerPoint PPT Presentation

  • Uploaded on

Parametric Approaches to Welfare Measurement. Background.

I am the owner, or an agent authorized to act on behalf of the owner, of the copyrighted work described.
Download Presentation

PowerPoint Slideshow about ' Parametric Approaches to Welfare Measurement' - mahogony-fernandez

An Image/Link below is provided (as is) to download presentation

Download Policy: Content on the Website is provided to you AS IS for your information and personal use and may not be sold / licensed / shared on other websites without getting consent from its author.While downloading, if for some reason you are not able to download a presentation, the publisher may have deleted the file from their server.

- - - - - - - - - - - - - - - - - - - - - - - - - - E N D - - - - - - - - - - - - - - - - - - - - - - - - - -
Presentation Transcript


  • Up until now our examination of welfare has been essentially non-parametric in a statistical sense, we have not specified or estimated the parametric structure of the size distributions of income rather we have compared distributions via the empirical distributions functions directly.

  • When we know the parametric structure of distributions some welfare implications can be inferred directly. (e.g. x~N(10,10), y~N(10+ε,10) → y FOD x and x~N(10,10), y~N(10,10-ε) → y SOD x). (There also exist explicit formulae for many of the inequality indices).

  • There is an old and more recent literature which considers specifying and estimating size distributions of income and making such comparisons.

A processes that generate log normal y under clt arguments
[A] Processes that Generate Log Normal Y under CLT arguments.

  • Letting Y=ln(y=Income) yields what is called the Law of Proportionate Effects. Used most frequently in a time series context from the notion that yt=yt-1(1+et) where et is considered i.i.d. and E(et) = growth rate with V(et) small relative to 1.

  • Gibrats Law (Gibrat (1930),(1931)): Yti = μi + Yt-1i + Uti implies for process of life length T, Y ~ N(μT,σ2T) i.e. y is non-stationary

  • Kalecki’s modification (Kalecki(1945)): Yti = μi + βiYt-1i + Uti where |βi| < 1; a stationary version of Gibrat’s Law. Y ~ N(μ/(1-β),σ2/(1-β2)).

Models of the size distribution of income y ln per capita income
Models of the Size Distribution of Income (Y=ln(per capita income)

  • [B] Processes that generate “Pareto” type distributions under CLT arguments (Pareto (1897))

  • Gabaix (1999); Y(i,t)= μ(i) + Y(i,t-1) + u(i,t) (with Y(i,t) bounded from below)

  • Champernowne (1953) Markov Chain Process where f(yt)=Mf(yt-1) with M a lower triangular transition matrix

  • Double Pareto (Reed(2001)) Y(i,t)= μ(i) + Y(i,t) + u(i,t) (“t” governed by an exponential process)

Models of the size distribution of income y ln per capita income1
Models of the Size Distribution of Income (Y=ln(per capita income)

  • [C] Ad Hoc Parametric Generalizations Mandelbrot(1960) Singh and Maddala (1976) McDonald (1984) Houthakker (2002)

Tests for verifying the model specification
Tests for verifying the model specification. income)

  • Pearson’s Goodness of Fit Test. Partition the range of x into K mutually exclusive and exhaustive intervals then for a sample of size n let Ei be the number of observations expected in the i’th interval and let Oi be the number of observations actually observed in the i’th interval i=1,..,K then ΣKi=1(Oi-Ei)2/Ei ~ χ2(K-1-h) where h is the number of estimated parameters needed to calculate the Ei.

  • Kolmogorov- Smirnov Test (see previous lecture)

  • Hall Yatchew Expected Squared Difference Test.(see previous lecture).

Poverty rates under gibrat s law
Poverty rates under Gibrat’s Law income)

  • For an absolute poverty line x*

  • limT->∞ Φ([(ln(x*/x0)-T(μ+0.5σ2))/(σ√T)])

  • Growth exceeding -0.5σ2 implies a poverty rate of 0 in the limit, for growth less than -0.5σ2 the poverty rate would be 1.

  • For a relative poverty line (0.6 of median income) the poverty rate would be Φ([ln(0.6)/(σ√T)]) which increases with time reaching .5 at infinity.

Poverty and inequality under pareto s law
Poverty and Inequality Under Pareto’s Law income)

  • Poverty and inequality measures would be constant over time

  • The Gini for a Pareto distribution is 1/(2θ-1) which is 1 when the shape coefficient is one because in this case the Pareto distribution has no moments or an infinite mean.

  • If the poverty frontier is a real lower boundary below which no-one is allowed to fall, the income distribution would end up as Pareto – hence a very strong test of the efficacy of such a frontier.

The gini under gibrat s law
The Gini under Gibrat’s Law income)

  • Gini may be written as: 2F(exp(ln(x0)+T(μ+0.5σ2))| exp(ln(x0)+T(μ+0.5σ2)),Tσ2 ) – 1 where F(z | θ, γ ) is the log normal distribution function with mean and variance θ, γ respectively

  • This will tend to zero as T => ∞ when μ < -0.5σ2 and will tend to 1 otherwise, note particularly for zero growth Gini will tend to 1.

Polarization and mixtures
Polarization and Mixtures income)

  • If we think of societal income distributions as mixtures then we can analyze the progress of rich and poor groups as distinct entities.

  • Use the Trapezoidal Index as a measure of relative poverty.

  • 0.5(wpfp(xmp)+(1-wp)fr(xmr))(xmr-xmp)

Parametric approaches to mixture distributions
Parametric Approaches to Mixture Distributions. income)

  • To facilitate modeling one can fit distributions to the data and track the fitted sub distributions.

  • To illustrate these issues data on per capita GDP for 47 African countries together with their populations were drawn from the World Bank African Development Indicators CD-ROM for the years 1985, 1990, 1995, 2000, 2005 were used

Comments income)

  • Growth rate in the mean and variance greater in the un-weighted sample than in the weighted sample

  • Much more evidence for Log normality than for Pareto.