Abstract
We study the properties of the quantile regression estimator when data are sampled from independent and identically distributed clusters, and show that the estimator is consistent and asymptotically normal even when there is intra-cluster correlation. A consistent estimator of the covariance matrix of the asymptotic distribution is provided, and we propose a specification test capable of detecting the presence of intra-cluster correlation. A small simulation study illustrates the finite sample performance of the test and of the covariance matrix estimator.
Acknowledgments
We thank the Editor Jason Abrevaya and an anonymous referee for many useful comments and suggestions; the usual disclaimer applies. Santos Silva also gratefully acknowledges partial financial support from Fundação para a Ciência e Tecnologia (Programme PEst-OE/EGE/UI0491/2013).
Appendix
Throughout the Appendix cr, CS, M, and T denote the cr, Cauchy-Schwarz, Markov, and triangle inequalities, respectively. LLN denotes the Khintchine’s Weak Law of Large Numbers, UWL denotes a uniform weak law of large numbers such as Lemma 2.4 of Newey and McFadden (1994), and CLT is the Lindeberg-Lévy central limit theorem.
Proof of Theorem 1: We use Theorem 2.7 of Newey and McFadden (1994). Note that
We have to show that SG(β)–SG(β0) converges uniformly to a function. In this case pointwise convergence suffices as pointwise convergence of convex functions implies uniform convergence on compact subsets. Note that
where δ=β–β0. Note that Knight’s identity (Koenker 2005, 121) tells us that
where ψθ(u)=θ–I(u<0). Thus
Now by a LLN
Note that
Proof of Theorem 2: We adapt the proof of Koenker (2005, 121). Consider the objective function
This function is convex and minimized at
Now Z1G(δ)=–δ′W, where
Now write
and
where
Note also that
Now by CS
Note that E[RG(δ)]=0 and that by cr, (8), and CS we have
Thus RG(δ)=op(1). Hence by a LLN
Therefore
The convexity of –δ′W+δ′Bδ/2 assures that the minimizer is unique and therefore
Now note that
Proof of Theorem 3: The proof is similar to that of Lemma 5 of Kim and White (2003). Let
To prove (i) consider the (h, j)th element of
Now using the facts that
where
Let 𝒟1G={U1G>η},
Now as
under Assumptions 3. Now take Δ arbitrarily small and consequently
To prove (ii), note that
Proof of Theorem 4: For simplicity of notation we write
where
Now by Lemma 1
where
By a Taylor expansion around β0 we have
where
where i≠j. Now notice that
by a UWL. Since
and consequently
by two applications of cr and one of CS. ■
Let
Lemma 1 Suppose that Assumption 4 holds. Then, under H0, for any δG=o(1) we have
where
Proof: Note that
where
Now taking the expected value of hgij(β) conditional on xg we have
where the last line follows from H0 and i≠j.
Note now that
Since the indicator functions I(ugi≤x′ig(β–β0)) and I(ugj≤x′gi(β–β0)) and the conditional distribution functions F(x′gi(β–β0)|xgi) and F(x′gj(β–β0)|xgj) are functions of bounded variation (and hence type I class of functions in the sense of Andrews 1994) and as Assumptions 1 (a) and 4 (a) hold, it follows that
is stochastic equicontinuous by Theorems 1, 2 and 3 of Andrews (1994). ■
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