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Characteristics of seismic activity before and after the 2018 M6.7 Hokkaido Eastern Iburi earthquake
Earth, Planets and Space volume 71, Article number: 130 (2019)
Abstract
We applied the epidemic type aftershock sequence (ETAS) model, the twostage ETAS model and the nonstationary ETAS model to investigate the detailed features of the series of earthquake occurrences before and after the M6.7 Hokkaido Eastern Iburi earthquake on 6 September 2018, based on earthquake data from October 1997. First, after the 2003 M8.0 TokachiOki earthquake, seismic activity in the Eastern Iburi region reduced relative to the ETAS model. During this period, the depth ranges of the seismicity were migrating towards shallow depths, where a swarm cluster, including a M5.1 earthquake, finally occurred in the deepest part of the range. This swarm activity was well described by the nonstationary ETAS model until the M6.7 main shock. The aftershocks of the M6.7 earthquake obeyed the ETAS model until the M5.8 largest aftershock, except for a period of several days when small, swarmlike activity was found at the southern end of the aftershock region. However, when we focus on the medium and larger aftershocks, we observed quiescence relative to the ETAS model from 8.6 days after the main shock until the M5.8 largest aftershock. For microearthquakes, we further studied the separated aftershock sequences in the naturally divided aftershock volumes. We found that the temporal changes in the background rate and triggering coefficient (aftershock productivity) in respective subvolumes were in contrast with each other. In particular, relative quiescence was seen in the northern deep zones that includes the M5.8 largest aftershock. Furthermore, changes in the bvalues of the whole aftershock activity showed an increasing trend with respect to the logarithm of elapsed time during the entire aftershock period, which is ultimately explained by the spatially different characteristics of the aftershocks.
Background
The epidemic type aftershock sequence (ETAS) model (Ogata 1988) provides a good fit to standard earthquake occurrences. However, there are nonstandard earthquake series that appear under transient stress changes caused by external seismic or internal aseismic forces such as slow slips or fluid intrusions (Terakawa et al. 2013; Terakawa 2014; Yoshida et al. 2017, 2018a, b). These events trigger transient nonstandard earthquake swarms, and they are poorly fitted by the stationary ETAS model (Kumazawa and Ogata 2013; Kumazawa et al. 2017a, b). In this study, we examine nonstationary extensions of the ETAS model that cover nonstandard cases. These models allow the parameters to be timedependent and can be estimated by the empirical Bayes method. The best model is selected among the competing models to provide the inversion solutions of nonstationary changes. As a case study we investigated seismic activity in the Hokkaido Eastern Iburi region, before and after the M6.7 earthquake on September 16, 2018, based on a series earthquake occurrence data after October 1997.
On September 6, 2018, a M6.7 earthquake occurred at a depth of 37 km in the Mideastern part of the Iburi region in Hokkaido, Japan. This earthquake occurred within the plate of the land (North American plate). The earthquake exhibited a reverse fault type focal mechanism with a pressure axis in the ENE–WSW direction. The earthquake occurred near the major active faults (the Ishikari Lowland Faults), but at greater depths (Earthquake Research Committee 2010). From the crustal deformation caused by the M6.7 earthquake observed by SAR and GNSS, estimations suggested that a reverse fault motion in a high angle fault plane with an almost north–south trend had occurred; the upper end of the ruptured fault was located at a depth of about 16 km and its moment magnitude was estimated to be Mw 6.6 (Geographical Survey Institute 2018). See also Kobayashi et al. (2019) in the current special issue.
Fourteen months before this main shock, a swarm cluster occurred, followed immediately by a M5.1 earthquake and subsequent aftershocks near the focal zone of the main shock.
The aftershock activity of the 2018 Eastern Iburi earthquake occurred predominantly within an area approximately 30 km in length that extended in a north–south direction. The time decay of this activity shows various characteristics that will be discussed in this paper. On February 21 2019, a M5.8 earthquake occurred at a depth of about 35 km, in the northern part of the primary aftershock zone. The focal mechanism of the earthquake was marked by a pressure axis in the east–west direction.
Table 1 summarizes the hypocenter data and the mechanisms of the Fnet catalog of National Research Institute for Earth Science and Disaster Resilience (2019) of the abovementioned conspicuous earthquakes as supplied by the Japan Meteorological Agency (JMA). In this work, we analyze seismic activities in detail, including those associated with such conspicuous earthquakes, by using statistical models and methods that are summarized in the next section.
Models and methods
The reference ETAS model
The ETAS model (Ogata 1988, 1989; Utsu et al. 1995) is a pointprocess model representing the activity of earthquakes of magnitude M_{c} and above in a certain region during a certain time interval. The seismic activity includes the background activity at a constant occurrence rate μ (Poisson process). The model assumes that each earthquake (including the aftershock of another earthquake) is followed by aftershocks, although only aftershocks of magnitude M_{c} and larger are included in the data. The aftershock activity is represented by the Omori–Utsu formula (Utsu 1961) in the time domain. The rate of aftershock occurrence at time t following the ith earthquake (time: ti, magnitude: Mi) is given by
where K_{0}, α, c, and p, are constants, which are common to each target aftershock sequence in a region. The rate of occurrence of the whole earthquake series at time t becomes
The summation is performed for all i satisfying ti < t. Here, H_{t} represents the history of occurrence times with associated magnitudes from the data {(t_{i}, M_{i})} before time t. The parameter set θ = (µ, K, c, α, p) represents characteristics of the seismic activity of a focal region; hereafter, the unit of the parameters are ‘event number/day’, ‘event number/day’, ‘day’, ‘magnitude^{−1}’, and no dimension’, respectively. In this manuscript, we are particularly concerned with the parameters μ (the background rate) and K_{0} (the triggering coefficient). See Additional file 1: S1 for more details.
We estimate the parameters using the maximumlikelihood method where the loglikelihood function,
is maximized with respect to the parameters θ = (µ, K, c, α, p), and we call such an estimate the maximumlikelihood estimate (MLE), denoted by \(\hat{\theta } = (\hat{\mu },\hat{K}_{0} ,\hat{c},\hat{\alpha },\hat{p})\). Here, S is the starting time for the analysis, and {(t_{i}, M_{i}), M_{i} ≥ M_{c}; i = 1, 2, …} are the occurrence times and magnitudes of earthquakes in a time interval [0, T_{end}], which is divided by a precursory time interval [0, S] and a target time interval [S, T] for the fitting, and a prediction interval [T, T_{end}].
The precursory period is necessary to avoid biased estimations because the ETAS model is historydependent. Note, for example, in the case where we fit ETAS model to an aftershock sequence, the data in the target interval [S, T] in the loglikelihood (3) are required detection completeness; but the aftershocks immediately followed after the large main shock are imperfectly detected. On the other hand, we need to set in the precursory period [0, S) because the main shock and such large aftershocks are very influential to the occurrences of aftershocks in the target period; namely, \(\lambda_{\theta } (tH_{t} )\) always includes the data of the main shock and aftershocks during the period [0, S) as the precursory history. Even for the case of general seismic activity, we need a suitable precursory period in the very beginning of the available occurrence data.
In Supplemental Information of this manuscript (abbreviated by SI, hereafter), the respective MLEs are listed for each target time interval [S, T] where S and T indicated in the tables stands for “tstart” and “zte” in the notation of (4), respectively, those in (4) are variables set in the FORTRAN package SASeis2006 (Ogata 2006a, b), and the Xwindowbased interactive graphical software XETAS (Tsuruoka and Ogata 2015a, b; Ogata and Tsuruoka 2016). Again, in fitting the ETAS model, earthquake data in the target and prediction interval should be completely detected above the cutoff magnitude of M_{c}.
Then, using the MLE, we can visualize how well or how poorly the model fits to the earthquake sequence by comparing the cumulative number N (S, t) of earthquakes with the rate calculated by the model
for the time interval S < t < T. If the model presents a good approximation of observed seismicity, we can expect that its integral function \(\varLambda_{{\hat{\theta }}} (S,tH_{S} )\) of t is closely overlap the observed function of the cumulative counts N(t) of the events. Furthermore, plots of N(t) against the transformed time \(\tau = \varLambda_{{\hat{\theta }}} (S,tH_{S} )\) shows nearly straight line. See Additional file 1: S2 for more details.
Twostage ETAS model and changepoint problem
When the stationary ETAS model (2) does not fit a dataset well, the simplest alternative model is a “twostage ETAS model” that takes different parameter values in subperiods before and after a particular time, called a “changepoint”. In changepoint analysis, we divide the whole period into two disjoint periods to fit the ETAS models separately (twostage ETAS model). This is one of the ways to treat the nonstationary data and can be best applied to the cases where there is a clearcut time instant across which the ETAS parameters change. We occasionally observe such a changepoint when a notably large earthquake or slow slip event (regardless of observed or unobserved) occur in or near the target region. Many of the preceding works (e.g., Ogata et al. 2003; Ogata 2005, 2006a, 2007, 2010; Kumazawa et al. 2010) adopted this method to their case studies, and the details can be found therein.
Testing whether or not the seismicity pattern changes at a time T_{0} in a given period [S, T] is reduced to a problem of model selection method by using the Akaike information criterion (AIC; Akaike 1973, 1974, 1977). In this procedure, we separately fit the ETAS models on the divided periods [S, T_{0}] and [T_{0,} T], then compare their total goodnessoffit against the one fitted over the whole period [S, T] by the minimum AIC principle as follows:
Let AIC_{0} be the AIC of the stationary ETAS model estimated on the whole period [S, T], AIC_{1} be that on the first period [S, T_{0}] and AIC_{2} on the second period [T_{0}, T] where the data in the first period is used for the precursory period, then
where dim θ_{0}, dim θ_{1} and dim θ_{2} are the number of adjusted parameters, respectively.
If a changepoint T_{0} is hypothetically prefixed based on some information other than the occurrence data themselves, such as a notable geophysical event or a notable outside large earthquake, then we can compare AIC_{0} with \({\text{AIC}}_{ 1} {\text{ + AIC}}_{ 2}\) to select the model with the smaller value, which performs better fit to the data in the entire target period [S, T]. Here, it is useful to remember that, if the difference \(\Delta {\text{AIC}} = {\text{AIC}}_{ 1} {\text{ + AIC}}_{ 2}  {\text{AIC}}_{0}\) takes negative value, the quantity exp{− 0.5ΔAIC} indicates the relative probability how the twostage model outperform the single stationary ETAS model (Akaike 1980).
On the other hand, if the changepoint T_{0} is searched from target data, the twostage model becomes harder to be accepted. Namely, AIC_{12} as the AIC of the twostage ETAS model should be calculated as follows:
here the additional term q is the degree of freedom to search for the best candidate T_{0} (MLE of a changepoint) from the data. The value of q depends on sample size (number n of earthquakes in the target period [S, T]), ranging 4–5 monotonically for n between 100 and 1000 (Ogata 1992, 1999; Kumazawa et al. 2010; Bansal and Ogata 2013). This penalty term q in addition to the increased number of parameters imposes a hurdle for the twostage ETAS model to be selected. See Additional file 1: S3 for more details.
Theoretical cumulative function and the time transformation
Suppose that the MLE \(\hat{\theta } = (\hat{\mu },\hat{K}_{0} ,\hat{c},\hat{\alpha },\hat{p})\) of the ETAS model in the first period [S, T_{0}] are given. Then the integral (3) extended over the time interval [T_{0}, t] provides the expected cumulative number of earthquakes on the extended period. We consider time transformation
from t to τ, which transforms the ordinarytime sequence of earthquakes; (t_{1}, t_{2}, …, t_{N}) into the transformedtime sequence (τ_{1}, τ_{2},…, τ_{N}) in the time interval [0, Λ(T_{0}, T)], which we call the residual point process (RPP). If the sequence continues in the remaining period, we expect the integrated function (3) and the empirical cumulative counts N(t)–N(T_{0}) of the observed earthquakes to be close to each other. This implies that the transformed sequence, or RPP, (τ_{1}, τ_{2},…., τ_{N}) in the time interval [0, Λ(T_{0}, T)] appears to be a stationary Poisson process (uniformly distributed occurrence times) with unit intensity (occurrence rate), but it deviates upward or downward otherwise.
Let \(\tau_{0}\) = Λ(T_{0}), and N(\(\tau_{0}\), τ) be the number of events in the interval (\(\tau_{0}\), τ) in the transformed time axis. If no change occurs in aftershock activity, the extrapolated RPP is 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 \(N(0,\Delta \tau )\), 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 \(N\left( {0,\Delta \tau + (\Delta \tau )^{2} /N(\sigma ,\tau_{0} )} \right)\), derivation evaluation of which can be seen in Ogata (1992). Hereafter, we define the significance of deviations 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 integral over a fixed period of the conditional intensity function gives the expected number of earthquakes. On this basis, we focus on instances in which the number of earthquakes in an area is significantly less or larger than the extension of the fitted ETAS model, which we call “relative quiescence” and “relative activation”, respectively.
Nonstationary ETAS models
The stationary ETAS model in (2) is temporally extended to the nonstationary ETAS model (Kumazawa and Ogata 2013; Kumazawa et al. 2017a, b) in the following form:
The functions μ(t) and K_{0}(t) of time are represented by a broken line connecting the respective sequences \(\left( {t_{i} ,\mu (t_{i} )\,} \right)\) and \(\left( {t_{i} ,K_{0} (t_{i} )\,} \right)\) for earthquakes i, and obtained under the optimal smoothness constraints in piecewise slopes (see Additional file 1: S4 and S5 for more details). Namely, such piecewise functions \(\mu \,(t)\) and \(K_{0} (t)\) are characterized by a set of twice many number of coefficient values than those of the earthquakes, which cause unstable solutions in maximizing the loglikelihood function with respect to the coefficients of the piecewise functions. To avoid such illposed solutions, we consider the penalized loglikelihood (Good and Gaskins 1971):
where \(\theta = \left\{ {\mu (t_{i} ),\,K_{0} (t_{i} )} \right\}\) and
with regard to hyperparameters \(\tau = (w_{\mu } ,w_{{K_{0} }} ,c,\alpha ,p).\)
The objective before obtaining the inversion solution of \(\theta\) is to obtain the best selection of hyperparameter \(\hat{\tau }\,\), which will be listed in Additional file 1: Table S2. Here, the best weights of the penalty for tuning of hyperparameter values is objectively carried out by the empirical Bayesian procedure using the Akaike Bayesian information criterion (ABIC; Akaike 1980),
where
is the probability density of θ. Here, we need some major technical cares that are undertaken in a similar manner in Ogata et al. (2003) and Ogata (2011).
We also couple this smoothing procedure with a changepoint, which allows a target parameter to have a sharp change or a discontinuous jump at a particular infinitesimal time span, while keeping the variation smoother for the rest of the period. For example, suppose that a large earthquake that occurred at a time t_{j} is suspected to be a changepoint of a discontinuity. Then, we add a precursory time point t_{j}near t_{j} to divide the interval (t_{j–1}, t_{j}) into two subintervals (t_{j–1}, t_{j}−) and (t_{j}−, t_{j}), therefore correspondingly dividing the original segment into two segments. The weights for the penalty functions in the precursory interval are set to be the same as those for following intervals, but the weight for the second small interval is a very small value for allowing steep slope of the line, representing a jump. For example, we obtain the values in Additional file 1: Tables S2, S4 and Figs. 3, 5 when we set a sufficiently small constant, 10^{−5}, in our applications. See Additional file 1: S4 and S5 for more details.
Model comparisons
We need to compare the goodnessoffits between the abovementioned models applied to the same dataset in the entire target interval. We consider the stationary ETAS model (2) as the reference model that is applied to the same dataset in the entire target interval.
First, the twostage ETAS model is compared based on the increments
Secondly, for the nonstationary ETAS model, we cannot simply compare their resulting ABIC values because of unknown different constants mainly due to the approximations adopted for calculation of (12). Therefore, we use the difference of ABIC values relative to the corresponding to the reference models
where ABIC_{0} is the amount of ABIC value in the case where the varying coefficients of nonstationary ETAS model are a very heavily penalized, such as w_{μ} = w_{K0} = 10^{5}. Specifically, \(\mu\)(t) and K_{0}(t) become the same as the constant values \(\mu\) and K_{0} in of the reference ETAS model, respectively. Such ABIC_{0} is equivalent to the AIC_{0} of the reference ETAS model.
It is useful to remember that exp{− 0.5ΔABIC} and exp{− 0.5ΔAIC} indicates relative probability of how likely the nonstationary ETAS model and twostep ETAS model is superior to the reference ETAS model, respectively (Akaike 1980). Furthermore, we compare the nonstationary ETAS model with twostage ETAS model by comparing ΔABIC and ΔAIC, via the likelihood exp{− 0.5(ΔABIC − ΔAIC)}.
Magnitude frequency analysis in the time and space domains
The Gutenberg–Richter (GR) law of magnitude frequency is the traditional standard model that has an exponential probability distribution with a completely detected cutoff magnitude, M_{c}
where the coefficient is called the bvalue. In the Hypocenter Catalog of the JMA, the magnitude value is rounded off and given in increments of 0.1. For the purpose of unbiased maximum likelihood estimates (MLEs) and locationdependent spatial estimates of bvalues, 0.05 should be subtracted from the magnitude of the lower limit (Utsu 1965); for example, we set M_{c}= 1.45 in (2) for the magnitude data M ≥ 1.5.
For obtaining the spatial variation of locationdependent bvalues, we apply the empirical Bayesian smoothing technique assuming a piecewiselinear function b(x,y), using Delaunay tessellation with the locations of earthquakes (Ogata 2011; see Additional file 1: S6). Namely, we use a piecewiselinear function defined by tessellation with triangles (Delaunay 1934; Ogata 2011), with coefficient values for the function given on earthquake locations and additional boundary points. Hence, a function value at any location in space is uniquely defined by the linear interpolation of values at the three nearest points (earthquakes) that determine a Delaunay triangle.
We also consider GR law with timedependent bvalues for all detected earthquake magnitudes, where the bvalue function of time is represented by a broken line connecting the sequence of earthquakes under smoothness constraint in piecewise slopes (Kumazawa et al. 2017a, b; see Additional file 1: S7). This method has the advantage of obtaining unbiased bvalues for time intervals immediately after large earthquakes such as main shocks and large aftershocks, where a substantial number of aftershocks were missed. For estimating such missing rates, the detection rates of earthquakes are modeled using similar broken lines as bvalues. The optimal weights of the smoothness constraints in variations of the bvalues and the detection rates are obtained by minimizing the ABIC that is defined by formally same equation as in (6).
Results
In this work, we analyze datasets obtained from the unified Hypocenter Catalog of the JMA after October 1997 (Fig. 1), in which earthquakes of M1.5 and larger are almost completely detected, except for a short interval immediately after the Iburi earthquake, as shown by magnitude frequency distributions in Additional file 1: Fig. S1.
We retrospectively investigate seismic activity during certain periods before and after the M6.7 main shock, as expressed in the hypocenter colors in Fig. 1.
Seismic activity prior to the Eastern Iburi earthquake
First, we studied the seismic activity since October 1997 in the region given in Fig. 1 with earthquakes of M1.5 and larger over the entire time period. The conspicuous earthquake that affected the seismicity in this period was the 2003 M8.0 TokachiOki earthquake (i, in Table 1) that occurred about a hundred kilometers in an eastward direction. By comparing the twostage ETAS model with the reference ETAS model, we see that the microseismicity in the focal region became quiet after the TokachiOki earthquake (i, 26Sep2003) as shown in Fig. 2 that summarized the AIC difference (ΔAIC = − 10.6) in Additional file 1: Table S2. Figure 2 also shows the earthquakes were migrated toward the shallower depths until the TokachiOki earthquake occurred.
After earthquake, 14 months before the occurrence of the M6.7 main shock, there was an aftershock cluster that was followed by the M5.1 earthquake (ii) that occurred near the focal zone of the M6.7 earthquake (iii, 6Sep2018); see the cluster of red circles in Fig. 1 and the last subperiod in Fig. 2. Therefore, we have applied the nonstationary ETAS model (9) throughout the period from the 1st October 1997 until the M6.7 earthquake (iii). Additional file 1: Table S3 shows that the nonstationary ETAS model is much better than the reference ETAS model, and the model with ΔABIC = − 46.9 indicating that the changepoint for a jump at 1Jul2017 is most significant. Figure 3 shows the changes in the background rate μ(t) and the triggering coefficient K_{0}(t) for the latter part of this period. There is a significant disconnection in smoothing at the time of the M5.1 event (ii, 1Jul2017), according to the abovementioned ABIC comparison (Additional file 1: Table S2). The background rate μ(t) and the triggering coefficient K_{0}(t) were constant until the M5.1 event (ii) occurred, at which time the background rate μ(t) jumped nearly tenfold and then decreased gradually to lower than the previous level. After this the background rate recovered slightly before the M6.7 main shock (iii). The triggering coefficient K_{0}(t) stayed almost constant throughout.
Aftershock activity following the M6.7 main shock
On September 6, 2018, a M6.7 earthquake (iii, 6Sep2018) occurred at a depth of 37 km; subsequently, on February 21, 2019, the M5.8 largest aftershock (iv, 21Feb2019) occurred at a depth of about 35 km in the northern part of the primary aftershock zone of the M6.7 main shock (see Table 1 and Fig. 1).
Seismicity characteristics of the entire aftershock volume
The aftershocks of the M6.7 earthquake up to the end of the period (March 16, 2019), with the cutoff magnitude M_{c} = 1.5, were analyzed by fitting to the stationary ETAS model in (2). Since the aftershocks immediately after the main shock are incompletely detected, we set the first 0.1day interval is precursory period in (4); and we get the MLEs from the rest as the target period, where the background rate of the aftershock activity is fixed (μ = 0.228 event per day) that is the MLE of the ETAS μ in the preceding interval before the M6.7 earthquake (iii, 6Sep2018). Also, the background rate μ = 0.228 is within the error bounds of the background rate of the preceding nonstationary ETAS model (Fig. 3).
Additional file 1: Table S4 (whole period) shows that the occurrence time of (iv, 21Feb2019), the M5.8 largest aftershock, is a clear changepoint with ΔAIC = − 47.9, which means that the ETAS model of the primary aftershock activity following the main shock has different parameters from those of the secondary aftershock activity that followed the M5.8 event (iv). In particular, the ETAS triggering coefficient K_{0} of the M5.8 event (iv) is significantly lower than that of the M6.7 main shock (iii).
There is another changepoint in the period before the occurrence time of the M5.8 event (iv) (see the top half rows of Additional file 1: Table S4). We first analyzed the aftershock period between the events (iii) and (iv), and found a significant changepoint with ΔAIC = − 21.2 on the 24th day (1Oct2018) after the main shock (iii). Figure 4 shows that cumulative curve of the seismicity obeys that of the stationary ETAS model (red curve) until the time of the changepoint, but then it deviates upwards for several days, and the RPP cumulative curve deviates outside the 2sigma parabola; in other words, it becomes relatively active compared to the ETAS prediction. It then recovers later. Furthermore, the RPP plot of blue circles in Fig. 4 shows seeming migration of aftershocks’ depth distribution, which is related to the increase in percentage of shallow aftershocks greater than about 25 km depth relative to the decaying trend of the aftershock activity in the deeper part.
We further applied the nonstationary ETAS model (9) throughout the period from the M6.7 main shock (iii) until the end of the period (16Mar2019), with the same precursory period of 0.1 days after the M6.7 event (iii) as the previous twostage ETAS model, in consideration of lower detection rate. Note there is little discrepancy in μ(t) before and after the M6.7 event (iii) according to the last column of Additional file 1: Tables S3, S5 and Figs. 3 and 5; namely, the estimated value of μ(t) = 0.215 with 95% credible interval (0.175–0.255) for the former, and 0.233 with (0.198, 0.268) for the latter).
Figure 5 shows the changes in the background rate μ(t) and the triggering coefficient K_{0}(t). There is a significant disconnection in smoothing at the time of the changepoint (1Oct2018) with, whereas no discontinuity at the time of the M5.8 largest aftershock (iv, 21Feb2019), according to the ABIC comparison (Additional file 1: Table S5). At the changepoint, the background rate μ(t) increased nearly tenfold, and then decreased gradually until it was lower than the level before the changepoint. Thereafter the rate recovered slightly before the M5.8 event (iv), whereas the triggering coefficient K_{0}(t) remained almost constant. It can be seen from Fig. 1 that the seismic activity for 4 days after the changepoint (pinkcolored band in Fig. 5) is spatially concentrated at southern end of the aftershock volume in purple color disks, where we suspect that might be the swarms caused by water intrusion as discussed later.
On the other hand, Fig. 6 summarizes the analyzed results in Additional file 1: Table S6 for the aftershock activity with magnitude thresholds of M_{c} = 3.0 and 4.0, where the changepoint hypothesis is supported by the ΔAIC value − 6.9 and − 2.2, respectively; and significant quiescence is seen from their RPP cumulative curves deviating outside the 2sigma parabola. These are larger thresholds than the previous cases with a microseismicity of M_{c} 1.5. Even with these moderatesized aftershocks, significant relative quiescence is found from 6 days after the M6.7 main shock (iii), and it lasts until the M5.8 largest aftershock (iv) by the ETAS model.
Further seismicity characteristics for divided zones of the Eastern Iburi aftershocks
Because the aftershocks of the M6.7 main shock (iii, 6Sep2018) with the low cutoff magnitude (M_{c} = 1.5) are abundant, we studied the whole aftershock sequence in more detail by dividing the entire aftershock area into four spatial zones as follows. We first divided shallow and deep zone by visually consulting the clustering of earthquakes at the depth of 23 km by looking at the distributions of gray disks in Fig. 1b and c, Fig. 9a and b, and also the different activity patterns seen in RPP depths against transformed times in Fig. 4; we further subdivided the deep zone into northern, middle, and southern zones, as shown in Fig. 7a. Here, for the calculation of the MLE and AIC, we include the M6.7 main shock (iii) occurrence data in the loglikelihood function (3) for every zone because the main shock magnitude is too large for such a narrow region to ignore the triggering effect.
The deep middle zone that actually includes the main shock obeys the stationary ETAS model as seen in Fig. 7c based on the results in Additional file 1: Table S7 (center). However, the northern and southern zone shows opposite anomaly of relative quiescence and activation, according to Fig. 7b and d whose ΔAIC value is − 12.5 and − 11.6 in Additional file 1: Table S7 (North) and (South), respectively. Their cumulative curves deviate outside the 2sigma parabolas. It is noteworthy that both changepoints are the same.
For the activity in the shallow zone, none of the stationary and twostage ETAS models appears to provide satisfactory fits according to Fig. 8a and b, respectively. Therefore, we applied the nonstationary ETAS model (4), which shows a significantly better fit, according to the ΔABIC in Additional file 1: Table S8 and thick gray cumulative curve in Fig. 8a. The estimated background rate μ(t) and triggering coefficient K_{0}(t) with the cumulative function for shallow activity are given in Fig. 8c in comparison with those of the stationary ETAS model.
Characteristic changes in bvalues of the GR magnitude distribution
The time change of the bvalues (black curve in Fig. 9c) of the aftershocks, taking account of the time dependence of earthquake detection rates (Additional file 1: S7), was obtained using all the detected data throughout the period from the main shock (iii, 6Sep2018) up to the end of the period (16Mar2019). Some undulation can be observed in the bvalues with respect to the lapse time plotted in logarithmic scale, but a gentle increasing trend is recognizable in the black curves.
However, the twodimensional spatial distribution projected onto the tomographic plane of bvalues have clear locationdependent variation (see Additional file 1: S6), especially where the shallow bvalues are larger than 0.85, whereas deeper bvalues show patchy patterns but much smaller than 0.85 (Fig. 10). These patterns were objectively obtained according to the optimal solution of the ABIC procedure (Additional file 1: Table S10). The patchiness in the deeper area resulted from the far denser earthquakes. For smoothing the bvalue, we use a piecewiselinear function defined on the Delaunay tessellated region. The vertices of each Delaunay triangle comprise the hypocenter coordinates of the three nearest earthquakes, hence the resolution is finer with more hypocenters.
Therefore, we divided the aftershock zone into shallow and deep sections; according to the solution of the ABIC analysis in Additional file 1: Table S10, the bvalue time changes for the shallow part are chosen to be a constant due to the very high weight w1. However, the bvalue for the deep section shows a smaller increasing trend than that for the aftershocks in general (Fig. 9c).
The ratio of the numbers of the deep aftershocks relative to the shallow aftershocks in Fig. 9e appears to relate the undulation of the bvalues of the entire aftershocks. See also Fig. 4 for the migration and relative increase of shallow aftershocks relative to the deep ones. Consequently, we imply that the increasing trend and undulation of bvalues of the entire aftershocks in Fig. 8c is due to the ratio of the occurrence of shallow aftershocks relative to the deep ones (Fig. 9e).
Discussion and conclusions
Seismic activity in and surrounding the area of the aftershock zone of the 2018 M6.7 Eastern Iburi earthquake (iii, 6Sep2018) was analyzed using the ETAS model, the nonstationary ETAS model (4) and the model of the magnitude frequency including seismic detection rate.
The triggering effects of the M8.0 TokachiOki earthquake (i, 26Sep2003) (see the source model in Fig. 1, Geographical Survey Institute 2003) on the seismicity in the focal region are complex. Firstly, occurrences of the 2018 M6.7 Eastern Iburi earthquake (iii) and the preceding neighboring moderate M5.1 earthquake (ii, 1Jul2017) seems to be promoted by the Coulomb failure stress increases of about + 1.4 bars and + 0.3 bars, respectively; here we used the receiver fault mechanisms listed in Table 1 and source fault parameters given by the Geographical Survey Institute (2018) and the Fnet catalog of National Research Institute for Earth Science and Disaster Resilience (2019). On the other hand, the microseismicity in the focal region became quiet after the TokachiOki earthquake (i) as seen in Fig. 2. This might suggest that the entire region is covered by stress shadow as discussed by Ogata (2006a, b, 2007, 2011).
The microaftershock activities of the both M5.1 (ii) and M6.7 (iii) earthquakes, with M1.5 and larger, show transient increases in background rates, as seen in Figs. 3 and 5. These suggest that swarm activities may have been induced by fluids weakening local faults. Such behavior was observed during swarms in Vogtland/NW Bohemia, central Europe (Hainzl and Ogata 2005), during several unusual earthquake events triggered by the 2011 TohokuOki earthquake of M9.0 in northern Japan (Terakawa et al. 2013; Kumazawa and Ogata 2013), in particular near the Lake Inawashiro (Kumazawa and Ogata 2013; Yoshida et al. 2017), and in Basel enhanced geothermal system, Switzerland (Terakawa 2014).
The moderate magnitude sized aftershock activity of the M6.7 event (iii) became significantly quiet relative to the occurrence rates in the ETAS model fitted for the first period after the main shock (iii). For example, applying the ETAS model to the aftershock activity with the lower limits of M_{c} = 3.0 and 4.0 suggested that the region became relatively quiet about 1 week after the main shock (iii), and then recovered during a month; but then lowered again until the occurrence of the M5.8 largest aftershock (iv, 21Feb19) (see Fig. 6).
We speculate one possible scenario as a reason for the earlier part of the quiescence (Kumazawa et al. 2018; see also Additional file 1: S8). It was suggested that the main shock dynamically weakened a part of the shallow faults in the eastern margin of the Ishikari Lowland fault zone, causing a “slow slip”, which caused the aftershock area of the Eastern Iburi earthquake to become a stress shadow. After that, the strength of the fault zone may have recovered, but the weakened stress shadow might have triggered the sequence of strong aftershocks that followed.
Furthermore, the relative quiescence that lasted until the M5.8 largest aftershock (iv) may be explained by the stress shadow by the precursory slow slip on the M5.8 fault and its extension. Although the relative quiescence cannot be seen for the entire aftershock volume with the cutoff magnitude M_{c} = 1.5 (Fig. 4), we see the relative quiescence in the northern zone of the deep part of the aftershock volume that includes the M5.8 earthquake (iv). The other three parts of the M6.8 Iburi earthquake show contrastingly different patterns to each other. Readers are also referred to Katsumata (2019) for mechanism about the three separations.
The bvalues of the entire aftershock region seemingly increased in trend with some undulation during the period after the main shock (iii), which is explained by the spatially different bvalues and different fluctuating occurrence rates of the shallow and deep aftershocks.
Availability of data and materials
The JMA hypocenter earthquake catalog can be downloaded from the JMA home page (https://www.jma.go.jp/jma/index.html). The Fnet catalog can be found in the NIED home page (http://www.bosai.go.jp/).
Abbreviations
 ABIC:

Akaike Bayesian information criterion
 AIC:

Akaike information criterion
 ETAS model:

epidemictype aftershock sequence model
 MLE:

maximumlikelihood estimate
 XETAS:

Xwindowsbased ETAS applications
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Acknowledgements
We used the PDE Hypocenter Earthquake Catalog (as of March 2019) of the JMA. We would like to thank to the JMA, the National Research Institute for Earth Science and Disaster Resilience (NIED), and the relevant universities for providing hypocenter data, and to the Meteorological Laboratory for MICAPG that calculates Coulomb failure stress. We are grateful for the support from the Japan Society for the Promotion of Science KAKENHI Grants 16K00065 and 17H00727. We also thank the support of the Tokyo Metropolitan Resilience Project.
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This research is funded from the Japan Society for the Promotion of Science KAKENHI Grants 16K00065 and 17H00727, and the Tokyo Metropolitan Resilience Project.
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TK arranged the statistical tools, modified and extended the functions used for the current study for implementing the analysis, made figures and tables, and also wrote the manuscript. YO organized the study, drafted the original manuscript, and had prepared some original statistical programs for the methods. HT had made and modified the XETAS programs for the present study. YO and HT checked the results. All authors read and approved the final manuscript.
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Kumazawa, T., Ogata, Y. & Tsuruoka, H. Characteristics of seismic activity before and after the 2018 M6.7 Hokkaido Eastern Iburi earthquake. Earth Planets Space 71, 130 (2019). https://doi.org/10.1186/s406230191102y
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Keywords
 ABIC
 AIC
 Bayesian method
 bValues
 Stationary ETAS model
 Twostage ETAS model
 Nonstationary ETAS model