Abstract
In this paper, we propose two ratio-type statistics to sequentially detect the memory parameter change-points in the long-memory time series. The limiting distributions of monitoring statistics under the no-change-point null hypothesis as well as their consistency under the alternative hypothesis are proved. In particular, a sieve bootstrap approximation method is proposed to determine the critical values. Extensive simulations indicate that the new monitoring procedures perform well in finite samples. Finally, we illustrate our monitoring procedures by two sets of real data.
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Acknowledgements
We are grateful to the editor and two anonymous referees for their detailed comments and valuable suggestions. This work was supported by the National Natural Science Foundation of China (Nos. 11661067, 61966030), Natural Science Foundation of Qinghai Province (No. 2019-ZJ-920).
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Appendix
Appendix
Proof of Theorem 3.1
Let \(t=[Tr],\ n=[Ts],\ m=[T\tau ]\), then if \(\gamma _t=1\), we have \({\hat{\varepsilon }}_{0,i}=X_i-[T\tau ]^{-1}\sum \nolimits _{j=1}^{[T\tau ]}X_j\), and
Then,
When \(\gamma _t=(1,t)'\), let \(\delta =(\alpha ,\beta )'\), then by the definition of LS we have
where \(\sum =\sum \nolimits _{t=1}^{m}\), if we estimate \(\delta \) using the samples \(y_{1},\ldots ,y_{m}\), \(\sum =\sum \nolimits _{t=n-m+1}^{n}\), if we estimate \(\delta \) using the samples \(y_{n-m+1},\ldots ,y_{n}\), and \(\sum =\sum \nolimits _{t=m+1}^{n}\), if we estimate \(\delta \) using the samples \(y_{m+1},\ldots ,y_{n}\). Since
Hence, by a tedious calculation, we have
Let
Then, a similar arguments gives that if \(n\le 2m\),
If \(n> 2m\),
Combining (14)–(18), together with the result \(\frac{T^k}{m^k} \rightarrow \tau ^{-k},\ \frac{T^k}{(n-m)^k} \rightarrow (s-\tau )^{-k}, \ k=2,3\), as \(T\rightarrow \infty \), Theorem 3.1 can be proved similar to Lavancier et al. (2013).
In the remainder of this section, we omit the proof for the case of \(\gamma _t = (1, t)'\); this follows the same logical development as those presented for the case of \(\gamma _t = 1\). In addition, we omit the proofs of Theorems 3.3 and 3.4, for these are similar to those of Theorems 3.1 and 3.2, respectively. \(\square \)
Proof of Theorem 3.2
From the proof of Theorem 3.1, we have the denominator of \(\varGamma _T(s)\) is \(O_p(T^{2+2d_0})\). If \(2\tau \ge s> \tau ^*\), then
Note that \(d_1>d_0\), so
This indicates the numerator of \(\varGamma _T(s)\) is \(O_p(T^{2+2d_1})\) if \(2\tau \ge s> \tau ^*\). Similar calculation gives that this conclusion is still hold if \(s>2\tau \). Hence,
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Chen, Z., Xiao, Y. & Li, F. Monitoring memory parameter change-points in long-memory time series. Empir Econ 60, 2365–2389 (2021). https://doi.org/10.1007/s00181-020-01840-4
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DOI: https://doi.org/10.1007/s00181-020-01840-4