 Letter
 Open Access
 Published:
Statistical monitoring of aftershock sequences: a case study of the 2015 Mw7.8 Gorkha, Nepal, earthquake
Earth, Planets and Spacevolume 68, Article number: 44 (2016)
Abstract
Early forecasting of aftershocks has become realistic and practical because of realtime detection of hypocenters. This study illustrates a statistical procedure for monitoring aftershock sequences to detect anomalies to increase the probability gain of a significantly large aftershock or even an earthquake larger than the main shock. In particular, a significant lowering (relative quiescence) in aftershock activity below the level predicted by the Omori–Utsu formula or the epidemictype aftershock sequence model is sometimes followed by a large earthquake in a neighboring region. As an example, we detected significant lowering relative to the modeled rate after approximately 1.7 days after the main shock in the aftershock sequence of the Mw7.8 Gorkha, Nepal, earthquake of April 25, 2015. The relative quiescence lasted until the May 12, 2015, M7.3 Kodari earthquake that occurred at the eastern end of the primary aftershock zone. Space–time plots including the transformed time can indicate the local places where aftershock activity lowers (the seismicity shadow). Thus, the relative quiescence can be hypothesized to be related to stress shadowing caused by probable slow slips. In addition, the aftershock productivity of the M7.3 Kodari earthquake is approximately twice as large as that of the M7.8 main shock.
Background
On April 25, 2015, a strong earthquake of Mw7.8 occurred along the Himalayan front close to Kathmandu, Nepal. Seventeen days after the main shock, the largest aftershock of May 12, the M7.3 Kodari earthquake, occurred in the eastern extension of the primary aftershock zone. The dip angle of the rupture fault zone is similar to that of the main fault zone on the plate boundary between the Indian and Eurasian plates.
The global probability forecast of the aftershocks of this earthquake (Michael et al. 2015) was implemented on the basis of nearrealtime data of the National Earthquake Information Center (NEIC), refer to Page et al. (2015) for the method and procedure for the nearrealtime global forecast. The initial forecast used the Reasenberg and Jones (1989) model with generic parameters of the region, which combine the Omori–Utsu law for the decay of aftershock frequency (Omori 1894; Utsu 1961) and the Gutenberg–Richter law for magnitude frequency (Gutenberg and Richter 1944). The model was subsequently updated to reflect a lower productivity and higher decay rate based on the observed aftershocks. This proved to be consistent with the main topic addressed in this paper. In fact, the forecast of the size distribution of aftershocks due to the Reasenberg–Jones predictor assumes the Gutenberg–Richter law. However, when precursory anomalies that can raise the probability gain of a large earthquake were detected, the probability forecast of the M7.3 aftershock was significantly small using this predictor only.
Retrospectively, we think that the forecast in this case could have yielded a higher likelihood of largemagnitude aftershocks than that predicted under the Gutenberg–Richter law. Relevant to this issue, Utsu (1979) and Aki (1981) emphasized the role of seismic anomalies in predicting the enhancement of the likelihood (probability gain) of having a substantially larger earthquake than the secular probability of the same size of earthquake. After the appearance of an anomaly, we need to evaluate the probability that it will be a precursor to a large earthquake; i.e., we need to forecast whether the probability in a space–time zone will increase to an extent, relative to that of the reference probability. Hence, it is desirable to search for anomalous phenomena that enhance the probability gains.
Seismic quiescence has attracted attention as a precursor candidate of large earthquakes (Inouye 1965; Utsu 1968; Ohtake et al. 1977; Wyss and Burford 1987; Kisslinger 1988). This anomaly concept is extended to include aftershock activity that can be significantly lower than the prediction of the Omori–Utsu formula (Matsu’ura 1986) or than the epidemictype aftershock sequence model (ETAS model; Ogata 1988, 1992, 2001a, for example). The quiescence relative to the ETAS model is useful for the detailed description of aftershock sequences as well as general seismicity. Development of the statistical models and analysis methods of aftershock sequences can be found in Utsu et al. (1995).
From comprehensive study, the retrospective statistical results from Japanese data (Ogata 2001a) suggest that the probability gain of having another large earthquake of a similar size to the main shock becomes several times greater relative to the normal probability if the aftershock activity shows significant lowering. Therefore, it is necessary to pay careful attention to anomalous activity by monitoring the aftershock sequence, especially in the early stage.
Methods
Statistical models to monitor aftershock sequences
Shortterm probability prediction of an earthquake of magnitude M _{ z } or larger in a nearfuture period (t, t + dt) is given by \(\lambda_{\theta } (tH_{t} )\,{\text{d}}t\) where \(\lambda_{\theta } (tH_{t} )\,\) is the historydependent occurrence rate, for example, the ETAS model developed by Ogata (1985, 1988, 1989)
where t = 0 is the main shock time of the aftershock observation and M _{ z } represents the reference magnitude (i.e., the main shock magnitude) of earthquakes to be treated in the dataset. M _{ i } and t _{ i } indicate the magnitude and the occurrence time of the ith earthquake, respectively, and H _{ t } represents the occurrence series of earthquakes (t _{ i }, M _{ i }) before time t. The parameter set θ thus consists of five elements (μ, K _{0}, c, α, p). In fact, the second term of Eq. (1) is a weighted superposition of the Omori–Utsu empirical function (Utsu 1961) for aftershock decay rates;
where t is the elapsed time from the occurrence of a main shock.
These parameters are obtained by maximizing the loglikelihood function (Ogata 1983, 1988, 1989) with respect to the parameter set θ. The loglikelihood function of the ETAS model,
is maximized with respect to the parameter set θ = (µ, K, c, α, p). Here, ‘ln’ is a natural logarithm, and {(t _{ i }, M _{ i }), M _{ i } ≥ M _{ c }; i = 1, 2, …} are occurrence times and magnitudes of earthquakes in the target time interval [S, T] for the fitting. Note here that the fitted data in the target interval [S, T] do not contain the main shock and immediately following aftershocks during the period [0, S), but that \(\lambda_{\theta } (tH_{t} )\) include the data of the main shock and aftershocks during the period [0, S) as the preceding history. Note also that the Omori–Utsu model is not history dependent except for the elapsed time since the main shock, and it is possible to apply the same loglikelihood function as (3) with θ = (K, c, p). The obtained parameter values are called the maximum likelihood estimates (MLE).
The Reasenberg and Jones method combines the Omori–Utsu aftershock decay, Utsu productivity scaling (Utsu 1970), and Gutenberg–Richter magnitude distribution (Gutenberg and Richter 1944), such that \(\lambda (t) \cdot 10^{{  b(M  M_{c} )}}\). Similarly, \(\lambda (tH_{t} ) \cdot 10^{{  b(M  M_{c} )}}\) can yield a better forecast for the case of multiple sources of earthquake clustering.
In terms of prediction, the goodness of fit of the model is measured using the Akaike information criterion (AIC; Akaike 1973), which is described as
where ln L(θ) represents the log likelihood (3) of the statistical model and k is the number of parameters to be estimated. With this criterion, the model with a smaller value of the AIC is expected to perform better prediction. The difference in the AIC values, ΔAIC, between the two competing models is useful, because exp{−ΔAIC/2} can be interpreted as the relative probability of how the model with the smaller AIC value is superior to the other, see the selected papers of Akaike (Parzen et al. 1998). Hence, for an aftershock sequence, a simpler model with a smaller number of adjusted parameters will yield a smaller AIC value if the difference in the maximum loglikelihood values is smaller than 1.0. Therefore, we may sometimes assume fixed parameter values μ = 0 or generic parameters such as p = 1.0 in the aftershock sequence to compare the AIC value of the ETAS model or the Omori–Utsu model.
When a seismicity change is suspected, we may look at the most likely candidate for the changepoint time T _{0} in a given period [S, T]. First, we separately fit suitable statistical models for the divided periods [S, T _{0}] and [T _{0}, T] (twostage model), and then we compare their total performance against the model fitted over the whole period [S, T] by the AIC. Then the most likely estimate of changepoint should minimize
or maximize the likelihood (e.g., Bansal and Ogata 2013)
with respect to the changepoint candidate parameter T _{0}, which can be called the MLE of the changepoint with respect to the time.
Theoretical cumulative function and time transformation
Suppose that the parameter values θ = (μ, K, c, α, p) of the ETAS model (1) are given. Then the integral of the conditional intensity function,
provides the expected cumulative number of earthquakes in the time interval [S, t]. The time transformation from t to τ is considered based on this cumulative intensity;
transforms the ordinary occurrence times of aftershocks; (t _{1}, t _{2}, …, t _{ N }) into the sequence (τ _{1}, τ _{2}, …, τ _{ N }) in the time interval [0, Λ(T)], which we call the residual point process (RPP). If the model is a good approximation to the real seismicity, we expect its integrated function (7) and the empirical cumulative counts N(t) of the observed earthquakes to be similar to each other. This implies that the transformed sequence (the RPP) appears to be a stationary Poisson process (uniformly distributed occurrence times) with unit intensity (occurrence rate) if the model is sufficiently correct, but it appears to be heterogeneous otherwise.
Let N(σ, τ) be the number of events in the interval (σ, τ) in the transformed time axis. If no change in aftershock activity occurs, the extrapolated RPP is also the standard stationary Poisson process with the same unit intensity, and the deviation \(N(\tau_{0} ,\,\,\tau )  (\tau  \tau_{0} )\) of the empirical cumulative function is approximately distributed according to the normal distribution \({\mathbf{N}}(0,\Delta \tau )\) where Δτ = τ − τ _{ 0 }. However, when the number of events \(N(\sigma ,\,\tau_{0} )\) in the target interval \((\sigma ,\,\tau_{0} )\) is not large enough, the significance actually depends on the sample size, due to the estimation accuracy of the parameters for the transformation. Thus, taking such accuracy into consideration, the error distribution of \(\Delta N(\tau_{0} ,\tau )\) is modified to be \({\mathbf{N}}\left( {0,\,\,\,\Delta \tau + (\Delta \tau )^{2} /N(\sigma ,\tau_{0} )} \right)\), derivation of which is provided in Appendix B of Ogata (1992). Hereafter we define the anomaly in the case where the empirical cumulative function deviates outside the parabola of 95 % significance \(2\left\{ {\Delta \tau + (\Delta \tau )^{2} /N(\sigma ,\tau_{0} )} \right\}\).
The FORTRAN program package associated with manuals regarding the ETAS analysis is available to calculate the MLE of θ and also to visualize model performances (Ogata 2006c), which has been extended to the program package XETAS (Tsuruoka and Ogata 2015a, b) using graphical user interface (GUI).
Data and results
We first used the NEIC Preliminary Determination of Epicenters (PDE) for datasets of the onfault aftershocks in the rectangular area bounded by the 84.4°E and 86.4°E meridians and 27.2°N and 28.4°N parallels obtained on May 13, 2015 (the day after the M7.3 Kodari earthquake; hereafter termed the first PDE data). Results similar to those of this study using this dataset were reported in early June 2015 at a workshop (Ogata 2015; Tsuruoka and Ogata 2015a). In addition, we used the second PDE data obtained on July 22, 2015 (Tsuruoka and Ogata 2015b), and herein we also incorporate the final datasets from the Advance National Seismic Network (ANSS) obtained on October 31, 2015.
We used the TSEIS visualization program package (Tsuruoka 1996) for selection of datasets from the catalogs. The identified aftershocks in the PDE catalog increase as time evolves, and the ANSS catalog includes about twice as many primary aftershocks before the M7.3 event as the first PDE data. In addition to the relocated epicenters and reevaluated magnitudes of the same aftershocks, newly detected aftershocks are listed as time proceeds. Figure 1a, b shows such differences between the first PDE data and the ANSS data; as far as the sequences of occurrence times and magnitudes are concerned, the second PDE data and the ANSS data are almost identical.
We use the GUI program package XETAS (Tsuruoka and Ogata 2015a, b), efficiently implementing the abovementioned methods in the following statistical analysis. The estimation results are summarized in Table 1.
First, as nearrealtime monitoring, we analyze the primary aftershocks of the first PDE data until the occurrence time of the largest aftershock of M7.3. The threshold magnitude is taken as M4.5 for completeness in the period from 1 h after the main shock occurrence time, as shown in Fig. 1. We apply the ETAS model and the Omori–Utsu model to this entire period. Table 1a indicates that the ETAS model fits better than the Omori–Utsu model according to the AIC values. The estimated decaying parameter p values of both the Omori–Utsu and ETAS models are seemingly quite large; this may be explained as follows.
By applying the ETAS model to the dataset for a whole target period, we preliminarily search a time interval in which changepoints seem to exist, inspecting the deviations of the cumulative curve of the transformed time (8) from the straight line. We then calculate exp(−ΔAIC/2) of the likelihood of changepoint time (see “Methods” section above). Thus, as given in Table 1, the 1.7 days from the main shock occurrence are the most likely (MLE) candidate of changepoint time. Incidentally, we cannot detect a significant local peak around the time (1.04 days) of the second largest aftershock of M6.7.
After the MLE of the changepoint, the number of aftershocks of M4.5 and larger become markedly low, so we suspect that there was a change in the seismicity pattern at the time. According to Table 1a, the Omori–Utsu model with very high p value fits better than the ETAS model in the period from 1 h until the suspected changepoint time (1.7 days) before the M7.3 aftershock. The difference in the AIC/2 values is small, and thus the simpler model is preferred for the prediction, probably due to the small number of events at this threshold magnitude. Figure 2a–c shows the bestfit models for the entire period (ETAS) and for the separate periods (the Omori–Utsu model and stationary Poisson model). Figure 2b, d shows the fit of the Omori–Utsu cumulative curve to the empirical cumulative function before the changepoint at 1.7 days after the main shock and also show the deviation from the empirical cumulative function after the changepoint. These show that about 20 potentially expected aftershocks of M4.5 or larger did not occur during the quiet period.
Next, to examine the stability of the above results, we also use the ANSS data for similar analysis of the aftershocks before the M7.3 event for various target periods and lower threshold magnitudes as described in Table 1b to ensure completeness of the datasets in accordance with Fig. 1. In these data from the ANSS catalog, the likely changepoint estimate is also 1.7 days. The results of the O–U and the ETAS models are similar to each other according to Table 1b. For the primary aftershocks throughout the entire period until the M7.3 event, the ETAS model fits better than the Omori–Utsu model, and the p values of the both models are rather high, namely 1.4–1.7. In the target period before the suspected changepoint, the ETAS model shows a slightly better fit than the Omori–Utsu model, possibly because of the increased data size, but the p values of the both models remain generic, namely p = 1.0 in this case. Figure 3 shows the case where the target interval is from 0.01 days (approximately 15 min) until the suspected changepoint at 1.7 days and with a threshold magnitude of M4.5. Relative quiescence is also likely to have occurred. Figure 3b, d also shows that about 20 potentially expected aftershocks of M4.5 or larger did not occur during the quiet period.
We further examined aftershocks from the ANSS catalog with the possible lowest homogeneous threshold magnitude of M = 4.2 in the period from 1 h until the M7.3 event, in accordance with Fig. 1. The most likely changepoint candidate in this case is 2.0 elapsed days as given in Table 1c, but Fig. 4a, b shows that the aftershock activity after day 2 until the M7.3 event appears to have decayed normally as predicted. Hence, we may conclude that aftershock activity with M ≥ 4.2 was normal throughout the entire period before the M7.3 event.
We examine whether any seismicity change occurred after the M7.3 event. The results of the ETAS fitting are given in Table 1d, and Fig. 4c, d shows that secondary aftershocks of M ≥ 4.2 occurred significantly more often than predicted. From the plot of magnitude versus transformed time in Fig. 4d, there are a substantial number of missing aftershocks of M ≥ 4.2 immediately after the M7.3 event. Hence, the actual number of secondary aftershocks was about twice as large as that predicted from the primary aftershock activity, and the aftershock productivity of the M7.3 event was twice as large as that of the main shock of M7.8. This finding implies that a single ETAS model does not always provide a proper forecast of the secondary aftershock sequence from the fit of the primary aftershock sequence, as illustrated in Fig. 4. This is because the ETAS model assumes the same productivity coefficient for every earthquake, but this is not always true in real seismicity (cf. Ogata 2001b).
It is also worthwhile to assess the space–time evolution of aftershock occurrences in Fig. 5 with respect to the transformed time using the Omori–Utsu cumulative curves. Although the detection rate of smaller aftershocks gradually increased with elapsed time, we used all the located aftershocks in both the nearrealtime PDE catalog and the ANSS catalog and fitted the Omori–Utsu model to them to obtain detrended space–time aftershock occurrences with respect to transformed time. Here, we should note that such space–time occurrence is not always uniform with respect to the transformed time at any place, and nonuniform occurrence times of aftershock activity are often observed in some local regions with respect to the transformed time, such as transient lowering or activation (Ogata 2010a).
On the basis of the space–time plots of aftershocks from both catalogs including the transformed time until the M7.3 event in Fig. 5, we can conclude that the spatial distribution of the primary aftershocks was heterogeneous, as detailed below.
The plots of epicenter longitudes against transformed times indicate that the eastern part of the aftershock zone was more active than the western part, which includes the main shock; and the western sparser area of aftershocks expanded toward the east. In the shrinking active eastern zone, the M6.7 large aftershock occurred on April 26 (approximately 1 day after the main shock), and then the active zone became quiet until the appearance of densely populated smaller aftershocks near the location of the M7.3 event around 86.1°E. Relevantly, Matsu’ura (1986) commented that relative quiescence is probably activated just before large aftershocks; hence, these may represent some type of foreshocks of a large aftershock.
The plot of epicenter latitudes against transformed times in Fig. 5 indicates that the early aftershocks near the main shock were very sparse but recovered to some extent in about a day. This result suggests that triggering of aftershocks around the main shock was delayed. Then the northern region become quiet and also shows expansion toward the eastern end near the Kodari earthquake of M7.3.
Discussion
Seismicity quiescence and empirical mediumterm forecasting
Although quite a number of years have passed since seismologists said that seismic quiescence could be effective in prediction, there have not been many examples of quiescence that have been pointed out in advance of a major earthquake. Also, the number and conditions of the parameters that describe the involved relationship between the space–time domain of quiescence and potential large earthquakes for general seismic activity are too large to yield a definite answer.
Notwithstanding, it may be easier to address the issue by restricting the subject to aftershock sequences. From the nearrealtime aftershock data, it is sometimes possible to observe probable relative quiescence that may follow a large aftershock with a higher probability gain than the case of normally decaying aftershock activity. It will be desirable to know the probability gain of a specified size of large aftershock. When aftershocks occur significantly less frequently in comparison with the number predicted by the Omori–Utsu or the ETAS model when aftershocks are attenuated as expected by the model, we empirically expect a higher possibility of a significantly large aftershock, which will probably occur on a fault boundary.
This type of empirical probability gain has been obtained in a large number of case studies. For example, Ogata (2001a) investigated 76 aftershock sequences in Japan, detected relative quiescence in 34 cases, and evaluated the probability gain of a large earthquake as follows. First, if a large earthquake has occurred in a particular location, the probability per unit area that another earthquake of similar magnitude will occur in the vicinity is greater than the probability for a distant area. This is the result of empirical statistics regarding the selfsimilarity feature (inversepower law correlations) and also physically suggests that the neighboring earthquake will be more likely to be induced by a sudden stress change on the periphery because of the abrupt slip of the earthquake. Moreover, if aftershock activity becomes relatively quiet, it becomes more likely that large aftershocks will occur around the boundary of the aftershock area. Furthermore, if relative quiescence lasts for a sufficiently long time (more than a few months), the probability of another earthquake of similar magnitude will increase to about three times the probability gain within 6 years in the vicinity of the aftershock area (within 200 km distance). Similar evaluations may be carried out to obtain the probability gain for an aftershock that is larger than magnitude M _{0} − 0.5 for a main shock of magnitude M _{0}, for example, in a shorter period of relative quiescence.
If the detection rates of aftershocks regarding magnitudes are same throughout the target period, we can make use of a homogeneous dataset under a smaller threshold magnitude instead of the dataset of completely detected threshold magnitudes to allow lessuncertain inference and prediction (Ogata and Katsura 1993, 2006). It is also desirable to recover information on missing aftershocks using modeling of detection rates, particularly in the early stage of aftershocks (Omi et al. 2013, 2014a, b).
The physical meaning of seismic quiescence
When a significant quiescence has been detected, it is necessary to question whether and how this leads to large earthquakes, if any occur. There are various conditions such as tectonics and stress fields that can be used for quantitative representation of the quiescence phenomenon to be addressed. A comprehensive physical study of the seismic quiescence preceding a large earthquake is essential for enhancement of the probability gain of the anomaly. These elements must be incorporated to achieve a predicted probability that exceeds the predictions of typical statistical models. Specifically, using the model, some retrospective case studies (Ogata 2013; and references therein) have been concerned with the phenomenon that the stress shadow (e.g., Harris 1998) inhibits normal aftershock activity.
As discussed in Ogata (2005a, b, c, 2006a, b, 2007, 2010b, 2011), Ogata et al. (2003), Kumazawa et al. (2010), and Kumazawa and Ogata (2013), we should consider and demonstrate the relationship of seismicity lowering (seismicity shadow) in the space–time aftershock occurrence patterns together with slow slips on the plate boundary using geodetic studies for the present Gorkha case (e.g., Avouac et al. 2015; Zhang et al. 2015; Fielding et al. 2015; Grandin 2015; Ingleby et al. 2015). Specifically, scenarios explaining the relative quiescence can rely on the seismicity rate change based on the rateandstate friction law of Dieterich (1994) as the quantitative basis of the triggering (Ogata et al. 2003; Ogata 2004, 2010a; Ogata and Toda 2010).
Although transient slow slip is promising as a possible precursor to a strong earthquake in mediumterm and shortterm predictions, this should in some way be discriminated from habitual slip or postseismic slip. It is necessary to identify these types of slip statistically based on space–time seismicity patterns to allow empirical evaluation of the probability gain of large earthquakes. Furthermore, if it is possible to identify the precursory slips more clearly by constraining the physical setup based on other data, such as various kinds of geodetic observations, the probability gain may become higher.
Conclusions
Operational quasirealtime statistical monitoring of anomalies of aftershock sequences should be implemented together with probability forecasting based on realtime earthquake datasets using either the Omori–Utsu model or the ETAS model. Diagnostic analysis based on fitting the models is helpful in detecting various anomalies, such as the seismic quiescence, relative to the models; such an anomaly can enhance the probability gain of the occurrence of neighboring strong earthquakes. In this study, we illustrate this type of statistical monitoring for the early aftershock sequence of the Gorkha earthquake of M7.8 using the PDE datasets and the ANSS catalog.
We recommend that readers use the XETAS program (Tsuruoka and Ogata 2015a, b), which requires a small amount of memory and is a robust software kit with a GUI interface for making quick estimates of the ETAS and Omori–Utsu models and for various diagnostic analyses. This package also includes display of space–time plots of aftershocks relative to the transformed time; this allows exploration of the transient part of a relatively quiet area (seismicity shadow) and activated area, which is useful to identify the stressshadow area and the area of stress increase, respectively, and eventually to search for suspected aseismic slips on a fault or its vicinity.
Moreover, it is necessary to estimate the uncertainty in the nature and urgency of abnormal phenomena relative to their roles as precursors to major earthquakes. For this purpose, it is necessary to study a large number of normal and anomalous cases for potential precursory links to large earthquakes. Thus, incorporation of this information in the design of a prediction model for probability that exceeds the underlying probability is important. Also, such comprehensive monitoring experiments with examination of speculative physical scenarios may eventually clarify the tectonic mechanisms that cause significantly large aftershocks with higher probability gains than that of ordinary aftershock activity, which follows the empirical laws of aftershocks. In conclusion, based on such quantitative studies, we hope that it will eventually be possible to say that the probability of the occurrence of a large earthquake in a certain period and a certain region has increased by a certain extent compared with the reference probability.
Abbreviations
 AIC:

Akaike information criterion
 ANSS:

Advance National Seismic Network
 ETAS model:

epidemictype aftershock sequence model
 GUI:

Graphical user interface
 MLE:

maximum likelihood estimates
 NEIC:

National Earthquake Information Center
 O–U model:

Omori–Utsu model
 PDE:

Preliminary Determination of Epicenters
 RPP:

residual point process
 XETAS:

Xwindowsbased ETAS applications
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Authors’ contributions
YO organized the study, carried out the analysis, and drafted the manuscript. HT has written the XETAS programs, modified and extended the functions for the current research, and checked the results and manuscript. Both authors read and approved the final manuscript.
Acknowledgements
We have benefited from the editor and anonymous reviewers for their constructive comments which clarified the present paper. The present study was supported by JSPS KAKENHI Grant 26240004.
Competing interests
The authors declare that they have no competing interests.
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Keywords
 Epidemictype aftershock sequence (ETAS) model
 Omori–Utsu formula
 Changepoint
 Probability gain
 GUI software package XETAS
 Relative quiescence
 Seismicity shadow