Abstract
This paper presents the nonparametric quantile regression estimation for the regression function operator when the functional data with the responses missing at random are considered. Then, the large sample properties of the proposed estimator are established under some mild conditions. Finally, a simulation study is conducted to investigate the finite sample properties of the proposed method.
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Acknowledgements
The authors are grateful to the Editor and the referee for their valuable suggestions and comments that greatly improved the manuscript. Xu’s work was supported by National Natural Science Foundation of China (No. 11801514) and Zhejiang Provincial Natural Science Foundation of China (No. LY17A010026). Du’s work was supported by National Natural Science Foundation of China (Nos. 11971045, 11771032), China Postdoctoral Science Foundation funded project (No. 2019M653502), the Science and Technology Project of Beijing Municipal Education Commission (KM201910005015), and the International Research Cooperation Seed Fund of Beijing University of Technology (No. 006000514118553) .
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Appendix A. Proofs of main theorems
Appendix A. Proofs of main theorems
Throughout this paper, we will introduce the following notations. We use \({\mathcal {F}}_n\) to denote the set of the random variables \((X_1,\ldots , X_n)\) and \(\psi (\cdot )\) denote the score function of \(\rho _\tau (\cdot )\). For fixed random function \(\chi \), denote \(R_i=m(X_i)-m(\chi )\), \(\theta (\alpha )=\sqrt{n\phi (h)}(\alpha -m(\chi ))\) and \({\hat{\theta }}=\theta ({\hat{\alpha }}).\) Then, let
We first introduce the following lemmas.
Lemma 1
Suppose that conditions C1–C6 hold, then
Proof
By the condition C6, we have
where the last equality holds by Lemma 4.
On the other hand, we have
Then, by the condition \(h^\beta \sqrt{n\phi (h)}\rightarrow 0 \), we have
\(\square \)
Lemma 2
Suppose that conditions 1–6 hold, then for any \(L>0\), it has
Proof
By the Knight’s identity, we have
Then, by direct calculation, we have
Denote \( \zeta _i(\theta )=\eta _i(\theta ) + \frac{\theta }{\sqrt{n\phi (h)}}\frac{\delta _i}{ \pi (X_i)}K_h(d(\chi ,X_i))\psi (\varepsilon _i+R_i).\) Invoking Lemma 19.24 of Van der Vaart (1998), we have
Then, according to Lemma 1, one has
Combining this with Eq. (A.1), we can obtain
\(\square \)
Lemma 3
Suppose that conditions 1–6 hold, then for any \(L>0\), it has that
Proof
To prove Lemma 3, it is sufficient to show that
By the Knight’s identity, one has
where the definitions of \(I_{n1}\) and \(I_{n2}\) are clear from the context.
First, we consider \(I_{n1}.\)
It is easy to show \(E(I_{n11})=0.\) By conditions C3-C4 and Proposition 2 of Laib and Louani (2010), one has
Thus, one has \( I_{n11}=O_p\left( \sqrt{\frac{\log \log (n)}{n\phi (h)}}\right) =o_p(1)\) by condition C3. Similar to \(I_{n11},\) we have \(E(I_{n12})=O\left( \frac{h^\beta }{\phi (h)}\sqrt{{\log \log (n)}}\right) \) and \(E(I^2_{n12})=O\left( \frac{h^\beta \log \log (n)}{n\phi (h)}\right) .\) Therefore, we have \(I_{n12}=O_p\left( \frac{h^\beta }{\phi (h)}\sqrt{{\log \log (n)}}\right) .\) Thus \(I_{n1}=o_p(1).\)
Next, we consider \(I_{n2}.\) By straightforward algebra, one has
Combining the above arguments with condition C5, we have
\(\square \)
Lemma 4
Suppose that conditions 1–6 hold, then we have
and
The proof of Lemma 4 is similar to Lemma 1 of Laib and Louani (2010). By Lemma 4 and the Lindeberg–Feller central limit theorem, we have the following Lemma 5.
Lemma 5
Suppose that conditions 1–6 hold, then we have
where \(\sigma ^2(\chi )=\tau (1-\tau )M_2\frac{f_1(\chi )}{\pi (\chi )}.\)
Lemma 6
Suppose that conditions 1–6 hold, then we have that
Proof
By the Knight’s identity, we have
Invoking the fact \(EI_{\{\varepsilon _i<0\}}=\tau ,\) we have
where the last equality holds by Lemma 4. \(\square \)
Proof of Theorem 1
where the last equality holds by Lemma 5, \(W_n\) is normal random variable with zero mean and variance \(\sigma ^2(\chi )=\tau (1-\tau )M_2\frac{f_1(\chi )}{\pi (\chi )}.\) Invoking the epiconvergence results of Geyer (1994), we have
Combining this with Lemma 5, we have
where \(\varpi (\chi )= \tau (1-\tau )\frac{M_2}{M_1^2}\frac{1}{ f_1(\chi )\pi (\chi ) f^2(0|\chi )}.\)\(\square \)
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Xu, D., Du, J. Nonparametric quantile regression estimation for functional data with responses missing at random. Metrika 83, 977–990 (2020). https://doi.org/10.1007/s00184-020-00769-z
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DOI: https://doi.org/10.1007/s00184-020-00769-z
Keywords
- Quantile regression
- Functional data analysis
- Missing at random
- Inverse probability weighting estimator
- Asymptotic normality