Large-N and Large-T Properties of Panel Data Estimators and the Hausman Test



NT(β (βg β)

Nttw - β)

+   1 σ2v    (P2,2 - P2,1)

√T σU (q2,2 - q2,ι + σ2)

+op √Jf) ;

N( (βb - β)


(24)


√NT2 (βw — βg )


-V    (P2,2 - p2,ι)

σU (q2,2 - q2,ι + σ2)


n (βb - β) + op(1)


n 0  σV    (p2,2 - p2,1)

(25)


, -U (q2,2 - q2,ι + σ^)2

σ4    (p2 2 - p22 1 )

plimN,τ→∞NT2[Var(βw) - Var(βg)] = -v ,     , 2   ,1 2λ2 .      (26)

w            g      σ2u (q2,2 - q22,1 + σe2)2

Note that (22) - (26) are essentially the same as (13) - (17) except that they do
not include the time trend
Tm.

CASE 2.2: Now, we consider the case in which the Θ2,i are constant over
different
i; that is, p2,2 - p22,1 =0. If the model contains no intercept term
(ζ =0) and it is estimated with this restriction, all of the results (22) - (26) are
still valid with
p2,2 replacing (p2,2 - p22,1). However, if the model contains an
intercept term, the assumption of cross-sectional homoskedasticity affects the
convergence rates of the between estimator and the Hausman statistic, while
it does not to the within and GLS estimators. To see this, we assume that
Θ
2,i =0, for all i, without loss of generality. Then, we can show

N (βb - β)→ N μ0, -u ) ;


(27)


-—^ ^   ^         —2       2        /n ^

NT3(β(βw - βg)   =  --v7-------2r—. ʌNr (βb -β) + op(i)

w g             -2u (q22,2 - q222,1 + -e2)   T b

= N (0, -v 7-------2- . J ;          (28)

-2u (q22,2 - q222,1 + -e2)2

-4 -2

plimN,τ→∞NT3[Var(βw) - Var(βg)] = -27-------2---:—2τ2,     (29)

w            g     -2u(q22,2 - q222,1 +-e2)2

as (N, T → ∞). Observe that the between estimator is ypN-consistent as in
CASE 1.2.

CASE 3: So far, we have considered the cases in which the time-varying
regressor x
it and the time invariant regressor zi are uncorrelated. We now

13



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