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Development of a modified envelope correlation method based on maximum-likelihood method and application to detecting and locating deep tectonic tremors in western Japan


We develop a modified envelope correlation method for locating deep tectonic tremors and apply it to construct a tremor catalog for western Japan. We redefine the envelope cross-correlation method as a maximum-likelihood method by using the cross-correlation functions as objective functions and then weighting components of the data by the inverse of the error variances. This method is also capable of detecting multiple sources that occur almost simultaneously because they appear as local maxima in our analysis. We employ a nonlinear function, the average of the weighted cross-correlation functions (ACC), to locate the deep tectonic tremor hypocenters. Our optimization method is performed in two steps. We first fix the source depth and use a grid search to find the local ACC maxima, which are the potential event locations. We then use each potential event location as an initial value and apply the gradient method to determine its hypocentral location. Several source locations are sometimes determined in a 5-min time window. We also perform a numerical test using synthetic waveforms to validate our tremor hypocenter estimations. We apply our proposed method to continuous seismograms in western Japan for 12.5-year period, with our new approach detecting 35% more tremors than the envelope correlation method with the outlier control owing to the detection of multiple tremors in a single time window and to the improved tremor hypocenter accuracy yielded by the appropriate weighting scheme. We estimate the spatial resolution, which is defined as the epicentral distance between sources that can be distinguished by the location method, to be ~ 100 km.


Since the first discovery of deep tectonic tremors in the Nankai Subduction Zone (Obara 2002), tremors and similar slow slip phenomena have been observed in many subduction zones, such as Cascadia (Rogers and Dragert 2003), Mexico (Payero et al. 2008), Alaska (Peterson and Christensen 2009), and Costa Rica (Brown et al. 2009). Shelly et al. (2007) showed that tremors consist of many low-frequency earthquakes (LFEs), which are tiny shear slips on the deep extension of the plate boundary where megathrust earthquakes occur repeatedly. Tremors are considered the short-period component of broadband slow earthquakes, spanning from LFEs, which are observed above 1 Hz, to slow slip events, with durations of several days to several months, as recently discovered in the shallower section of the plate interface in the Nankai Subduction Zone (Ide et al. 2007; Kaneko et al. 2018). Tremors may therefore be useful for accurately monitoring the slow deformation behind them. The proximity of the source regions of slow and megathrust earthquakes suggests some interaction between these slow and fast processes (e.g., Obara and Kato 2016). The accurate and complete monitoring of tremors is therefore an essential component in investigating the potential interactions between these slow and ordinary earthquake phenomena.

Ordinary location methods using phase arrivals and S–P lag times are not applicable for locating tremors because tectonic tremor waveforms lack clear P- and S-wave phases. Various tremor location methods have been developed to address this issue. The method used in the first discovery of tremors in the subduction zone of western Japan was the envelope correlation method (Obara 2002). The envelope correlation method analyzes the similarity of the envelope waveforms between seismic stations and locates a tremor source to explain the observed travel time differences of the tremor signals measured by maximizing the cross-correlations of envelope waveforms, with the travel times being calculated using ray theory. A number of improvements to the envelope correlation method have since been proposed. The method of Wech and Creager (2007, 2008) determined tremor locations by directly maximizing the cross-correlations of the envelope waveforms. Maeda and Obara (2009) incorporated signal amplitude information into the envelope correlation method. Ide (2010) determined an event with a finite duration in the time window to demonstrate the effectiveness of outlier-control schemes.

The matched-filter method (e.g., Gibbons and Ringdal 2006) is another popular approach for tremor signal detection. Shelly et al. (2007) detected a number of tremors using the highest quality LFEs as template events in the matched-filter method and showed that tremors occur as a swarm of LFEs. Brown et al. (2008) developed an autocorrelation method for tremor detection. Bostock et al. (2012) extended these methods by preparing template waveforms consisting of stacking many LFEs detected by short-period autocorrelations and used them as template events. Although these methods generally provide more accurate and complete tremor detection and location, they generally have tremendous computational requirements and are not always suitable for large datasets that consist of many stations over a large area and long observation period.

Several other techniques have also been implemented for tremor detection and location. The source scanning algorithm of Kao and Shan (2004) estimates the tremor location and origin time that maximizes the brightness, which is the sum of the absolute amplitudes shifted by the theoretical travel times. La Rocca et al. (2010) showed that the cross-correlation between the vertical and horizontal seismogram components recorded by dense seismic arrays could be utilized to determine the S–P times of the tremor signals, with this information improving the accuracy of the tremor source location. Rubin and Armbruster (2013) showed that the tremor waveforms at two stations separated by 10–20 km were sometimes quite similar and could be used to measure the relative arrival time via cross-correlation. Their algorithm, the cross-station method, utilizes this similarity and locates tremors accurately using seismograms from only three stations.

The applicability of tremor location methods depends on the properties of seismic data, such as the extent of the target region, the observation period, and the number of stations. Here, we develop a method suitable for either a large data volume from many stations covering a long duration or daily monitoring. We review the methodology of current envelope correlation methods (Obara 2002; Wech and Creager 2008) from a statistical viewpoint and develop a location algorithm that is sufficiently fast, accurate, and applicable to a huge data volume. We apply this method to the seismogram records from 313 seismic stations in western Japan to construct a tremor catalog in the Nankai Subduction Zone for the period April 2004 to September 2016.


Maximum-likelihood-based location method

Our proposed method is essentially equivalent to that proposed by Wech and Creager (2007, 2008), but with the key modification of employing slightly different mathematical expressions that are introduced from a theoretical perspective based on the maximum-likelihood method.

Suppose that we analyze a set of continuous envelope waveforms from ground velocity seismograms sampled at time interval ΔT and search for tremors within a fixed time window with a width Tw = NtΔT, where Nt is the number of time samples. We define the normalized envelope waveform wi(t) in this time window as

$$w_{i} \left( t \right) = \frac{{w_{i}^{\prime } \left( t \right) - \overline{{w_{i}^{\prime } }} }}{{\sqrt {\mathop \sum \nolimits_{k = 1}^{{N_{t} }} \left( {w_{i}^{\prime } \left( {t_{k} } \right) - \overline{{w_{i}^{\prime } }} } \right)^{2} } }},$$

where the subscript i indicates the i-th component, \(w_{i}^{\prime } \left( t \right)\) is the original envelope waveform, \(\overline{{w_{i}^{\prime } }}\) is its temporal mean, and tk is the k-th time step in the window.

We assume that the envelope shape is common for all components at all stations. This means that each observation (normalized envelope waveform) wi(t) is represented by the summation of a common template waveform w(t) that is time-shifted because of seismic wave propagation from the source and Gaussian error ei(t) with a distribution \(N\left( {0,\sigma_{i}^{2} } \right)\). This relationship is described as

$$w_{i} \left( {t + \Delta t_{i} \left( \varvec{x} \right)} \right) = w\left( t \right) + e_{i} \left( {t + \Delta t_{i} \left( \varvec{x} \right)} \right),$$

where Δti(x) is the travel time from a potential source position x to the station recording the i-th component. The likelihood of obtaining the observed envelopes L(w, x) for a given combination of w(t) and x is written as

$$L\left( {w,\varvec{x}} \right) = \mathop \prod \limits_{i = 1}^{N} \mathop \prod \limits_{k = 1}^{{N_{t} }} \left\{ {\frac{1}{{\sqrt {2\pi \sigma_{i}^{2} } }}\exp \left( { - \frac{{\left( {w_{i} \left( {t_{k} + \Delta t_{i} \left( \varvec{x} \right)} \right) - w\left( {t_{k} } \right)} \right)^{2} }}{{2\sigma_{i}^{2} }}} \right)} \right\},$$

where N is the number of envelope components at all available stations. The log-likelihood is

$$\log L\left( {w,\varvec{x}} \right) = \mathop \sum \limits_{i = 1}^{N} \mathop \sum \limits_{k = 1}^{{N_{t} }} \left\{ {\log \frac{1}{{\sqrt {2\pi \sigma_{i}^{2} } }} - \frac{{\left( {w_{i} \left( {t_{k} + \Delta t_{i} \left( \varvec{x} \right)} \right) - w\left( {t_{k} } \right)} \right)^{2} }}{{2\sigma_{i}^{2} }}} \right\}.$$

For a fixed source location, Eq. (4) shows that we can determine the w(tk) that maximizes the log-likelihood at each discrete time tk independently, which is equivalent to minimizing

$$\mathop \sum \limits_{i = 1}^{N} \frac{{\left( {w_{i} \left( {t_{k} + t_{i} \left( \varvec{x} \right)} \right) - w\left( {t_{k} } \right)} \right)^{2} }}{{2\sigma_{i}^{2} }}.$$

for w(tk). We can determine the maximum-likelihood estimate wMLE(tk, x) by taking the derivative of Eq. (5) with respect to w(tk), which is considered the best template waveform and is written as

$$w^{\text{MLE}} \left( {t_{k} ,\varvec{x}} \right) = \frac{{\mathop \sum \nolimits_{i = 1}^{N} \frac{{w_{i} \left( {t_{k} + \Delta t_{i} \left( \varvec{x} \right)} \right)}}{{\sigma_{i}^{2} }}}}{{\mathop \sum \nolimits_{i = 1}^{N} \frac{1}{{\sigma_{i}^{2} }}}}.$$

The maximum log-likelihood is then rewritten as

$$\log L\left( {w,\varvec{x}} \right) = \mathop \sum \limits_{i = 1}^{N} \mathop \sum \limits_{k = 1}^{{N_{t} }} \left\{ {\left( {\log \frac{1}{{\sqrt {2\pi \sigma_{i}^{2} } }} - \frac{{w_{i}^{2} \left( {t_{k} + \Delta t_{i} \left( \varvec{x} \right)} \right)}}{{2\sigma_{i}^{2} }}} \right) + \frac{{2w_{i} \left( {t_{k} + \Delta t_{i} \left( \varvec{x} \right)} \right)w^{\text{MLE}} \left( {t_{k} ,\varvec{x}} \right) - w^{{{\text{MLE}^2}}} \left( {t_{k} ,\varvec{x}} \right)}}{{2\sigma_{i}^{2} }}} \right\}.$$

Assuming that the data possess a periodicity, where wi(t) = wi(t + Tw), the summation of the first term for k is independent of x. Therefore, we can essentially maximize the likelihood with x by simply maximizing the second term, which is rewritten as

$$\mathop \sum \limits_{k = 1}^{{N_{t} }} w^{\text{MLE}} \left( {t_{k} ,\varvec{x}} \right)\mathop \sum \limits_{i = 1}^{N} \frac{{2w_{i} \left( {t_{k} + \Delta t_{i} \left( \varvec{x} \right)} \right) - w^{\text{MLE}} \left( {t_{k} ,\varvec{x}} \right)}}{{2\sigma_{i}^{2} }}.$$

We then substitute Eq. (6) into the above formula to obtain

$$\mathop \sum \limits_{k = 1}^{{N_{t} }} \frac{{\mathop \sum \nolimits_{i = 1}^{N} \frac{{w_{i} \left( {t_{k} + \Delta t_{i} \left( \varvec{x} \right)} \right)}}{{\sigma_{i}^{2} }}}}{{\mathop \sum \nolimits_{i = 1}^{N} \frac{1}{{\sigma_{i}^{2} }}}}\left( {\mathop \sum \limits_{i = 1}^{N} \frac{{w_{i} \left( {t_{k} + \Delta t_{i} \left( \varvec{x} \right)} \right)}}{{\sigma_{i}^{2} }} - \frac{{\mathop \sum \nolimits_{i = 1}^{N} \frac{{w_{i} \left( {t_{k} + \Delta t_{i} \left( \varvec{x} \right)} \right)}}{{\sigma_{i}^{2} }}}}{{\mathop \sum \nolimits_{i = 1}^{N} \frac{1}{{\sigma_{i}^{2} }}}}\mathop \sum \limits_{i = 1}^{N} \frac{1}{{2\sigma_{i}^{2} }}} \right).$$

By combining the x-dependent terms, we find the maximum of Eq. (9) is obtained by maximizing

$$\mathop \sum \limits_{k = 1}^{{N_{t} }} \left( {\mathop \sum \limits_{i = 1}^{N} \frac{{w_{i} \left( {t_{k} + \Delta t_{i} \left( \varvec{x} \right)} \right)}}{{\sigma_{i}^{2} }}} \right)^{2} .$$

This can be rewritten as

$$\mathop \sum \limits_{i = 1}^{N} \mathop \sum \limits_{j = 1}^{N} \mathop \sum \limits_{k = 1}^{{N_{t} }} \frac{{w_{i} \left( {t_{k} + \Delta t_{i} \left( \varvec{x} \right)} \right)w_{j} \left( {t_{k} + \Delta t_{j} \left( \varvec{x} \right)} \right)}}{{\sigma_{i}^{2} \sigma_{j}^{2} }},$$

which is a summation of the cross-correlations weighted by the inverse of the error variances. The best tremor location in the analyzed time window is therefore determined by calculating the Δti(x) value (and therefore x) that maximizes Eq. (11). This function is identical to the maximized function in Wech and Creager (2007, 2008), except the weighting factors for cross-correlations. Note that the variance \(\sigma_{i}^{2}\) is fixed to estimate the likelihood function because it is determined from other information, which is discussed below.

The practical application of our proposed method requires that we use only those pairs of envelope waveforms whose cross-correlation maximum is larger than a threshold Clim. This criterion removes station pairs that may violate the assumption in Eq. (2) that the normalized envelope waveforms are the sum of the template waveform and small random errors, and also accelerates the computation. The resultant objective function to maximize in the numerical calculation is

$$\mathop \sum \limits_{{\{ \left( {i,j} \right)|{\mathrm{max}} {\text{CC}}_{i,j} > C_{\lim } \} }} \mathop \sum \limits_{k = 1}^{{N_{t} }} \frac{{w_{i} \left( {t_{k} + \Delta t_{i} \left( \varvec{x} \right)} \right)w_{j} \left( {t_{k} + \Delta t_{j} \left( \varvec{x} \right)} \right)}}{{\sigma_{i}^{2} \sigma_{j}^{2} }}.$$

We introduce the average of the weighted cross-correlations (ACC) as the final function to maximize for x as

$${\text{ACC}}\left( \varvec{x} \right) = \frac{{\mathop \sum \nolimits_{{\left( {i,j} \right)}} \mathop \sum \nolimits_{k = 1}^{{N_{t} }} \frac{{w_{i} \left( {t_{k} + \Delta t_{i} \left( \varvec{x} \right)} \right)w_{j} \left( {t_{k} + \Delta t_{j} \left( \varvec{x} \right)} \right)}}{{\sigma_{i}^{2} \sigma_{j}^{2} }}}}{{\mathop \sum \nolimits_{{\left( {i,j} \right)}} \frac{1}{{\sigma_{i}^{2} \sigma_{j}^{2} }}}},$$

where the criterion for Clim is omitted. This approach also allows us to compare the objective functions for different weight settings. Equation (13) is equivalent to Eq. (12) when the variances are fixed. Figure 1 shows a schematic diagram of our proposed location method.

Fig. 1
figure 1

Schematic diagram of our location method. The observed envelopes at many stations are shown by the red curves in the upper boxes. The light blue curves in the upper boxes are the time-shifted template waveform, which is also shown as the black curve in the lower box. Our method searches for the source location that will maximize ACC, which is the weighted sum of the cross-correlations. The weight is determined based on the similarity between the observed and template waveforms. In this case, the weight of station i is smaller than those at stations 1–3, as the difference between the observed and template waveforms is large

Our ACC evaluation requires numerous evaluations of the cross-correlation functions. We calculate the cross-correlations for each pair with travel time differences in the frequency domain via the fast Fourier transform method, as time differences are multiples of the sampling interval, and then store the cross-correlations in a table to reduce the computational requirements and costs of the method. We optimize our proposed method by calculating the cross-correlations as spline interpolations of values in our calculated table. By referring to this table, we can reduce the number of the evaluations of the cross-correlation functions between station pairs as much as the original envelope correlation method.

ACC optimization

We search for the maximum ACC using a combination of a grid search and a gradient method. The grid search, assuming a fixed tremor depth, picks several local ACC maxima as potential tremor epicenter locations. The variances of the normalized envelope waveform error \(\sigma_{i}^{2}\) are assumed to be proportional to the square of the hypocentral distance during this first step of the optimization. Note that we consider local maxima instead of the global maximum. This is because multiple tremors may occur at different locations in the same time window, such that the local maxima may reflect the occurrence of multiple tremors in a single time window.

We then maximize ACC using a gradient method, the conservative convex separable approximation (CCSA) algorithm (Svanberg 2002), with each potential tremor epicenter being used as an initial value, to determine the best hypocentral location of each tremor. When the hypocentral solutions from some potential locations are very close to each other, we unite these solutions.

We simply assume that the variances in the normalized envelope waveform errors are proportional to the square of the hypocentral distance in the grid search stage and locate potential tremor source epicenters. We then recalculate the weights assuming that the variances are proportional to the squared difference between wi and wMLE, such that

$$\sigma_{i}^{2} \propto \mathop \sum \limits_{k = 1}^{{N_{t} }} \left( {w_{i} \left( {t_{k} + \Delta t_{i} \left( \varvec{x} \right)} \right) - w^{\text{MLE}} \left( {t_{k} ,\varvec{x}} \right)} \right)^{2} .$$

A given seismic dataset may include very unusual observations that are unexpected in Gaussian statistics. We therefore employ two criteria to remove any outliers after the first tremor source estimation and repeat the procedure with the refined dataset until no outliers are identified.

The first criterion is based on the envelope cross-correlation, which requires each waveform in a pair of normalized envelope waveforms to meet a threshold cross-correlation Clim for consideration in the analysis. We originally apply the criterion about the cross-correlation to select the pairs in Eq. (12), which means that the maximum of the cross-correlation function is always larger than Clim. However, the cross-correlation value at a given time lag, which is calculated based on the potential tremor source location, is equal to or lower than the maximum and may be smaller than Clim.

The second criterion is based on the similarity between the envelope and the template waveform. We reject an envelope when the cross-correlation of the envelope and the template is below the threshold \(C_{ \lim }^{t}\). This criterion is introduced to eliminate signals that occurred at different locations. In this case, the cross-correlation of the pair may possibly be large, such that the pair meets the first criterion, whereas the second criterion is designed to reject these different seismic signals. We repeat the procedure, where we estimate σi, remove the outliers, and maximize ACC via the CCSA algorithm until no outliers are identified, to determine the best tremor hypocenter xbest.

We estimate the tremor source location error using a bootstrap method. We randomly resample the same number of correlated component pairs allowing duplication and locate the tremor source. We repeatedly examine the above process Nb times and determine the error as the standard deviation of these calculated source locations.

Source parameter estimation

We determine the hypocentral time, duration, and energy magnitude of each detected tremor as

$$\dot{E}_{\text{s}} \left( t \right) = 4\pi \rho \beta \frac{{\mathop \sum \nolimits_{{\left( {i,j} \right)}} \left( {\frac{{w_{i}^{\prime 2} \left( {t + \Delta t_{i} \left( {\varvec{x}^{\text{best}} } \right)} \right)R_{i}^{2} }}{{\sigma_{i}^{2} }} + \frac{{w_{j}^{\prime 2} \left( {t + \Delta t_{j} \left( {\varvec{x}^{\text{best}} } \right)} \right)R_{j}^{2} }}{{\sigma_{j}^{2} }}} \right)}}{{\mathop \sum \nolimits_{{\left( {i,j} \right)}} \left( {\frac{1}{{\sigma_{i}^{2} }} + \frac{1}{{\sigma_{j}^{2} }}} \right)}},$$

where \(\dot{E}_{\text{s}} \left( t \right)\) is an average of the seismic wave energy rate; Ri is the hypocentral distance to the station recording the i-th component; and ρ and β are the density and S-wave velocity at the station, which are assumed as 3,000 kg/m3 and 2.844 km/s, respectively. The hypocentral time is defined as the time when the maximum \(\dot{E}_{\text{s}} \left( t \right)\) occurs. The tremor duration is also estimated as the period when \(\dot{E}_{\text{s}} \left( t \right)\) exceeds a quarter of its maximum. The energy magnitude Me is defined as (Choy and Boatwright 1995)

$$M_{\text{e}} = \frac{{\log \left( {\int {\dot{E}_{\text{s}} \left( t \right){\text{d}}t} } \right) - 4.4}}{1.5},$$

with the integration taken over the tremor duration.

Application to observed data

Data and preprocessing

The seismic data consist of continuous velocity waveforms recorded at 313 Hi-net stations in western Japan maintained by the National Research Institute for Earth Science and Disaster Resilience. We only use the two horizontal components in our analysis because the tremor signals are dominated by S waves, and we want to suppress any unwanted P-wave signature, which is commonly visible in the vertical component at some stations. The seismic data cover the period April 2004 to September 2016, with the original records consisting of ground velocities sampled at 100 samples per second. The seismic data undergo a preprocessing procedure, which includes bandpass filtering at 2–8 Hz, squaring, low-pass filtering below 0.2 Hz, and resampling at 1 Hz, with the square root of the data considered as the envelope.

Parameter settings

The time window for the analysis Tw is fixed at 300 s. We analyze the continuous data using half-overlapping successive time windows. Cross-correlation functions are calculated for all component pairs whose inter-station distances are less than 100 km. The detection method is applied to a given time window when the number of cross-correlations that exceed the threshold of cross-correlation, Clim, is larger than 15. The travel time is calculated using ray theory and the JMA2001 1-D velocity model (Ueno et al. 2002) as the assumed S-wave velocity structure.

The following optimization parameters are assumed. The spatial interval for the grid search is 0.2°. The search area is limited to the region covered by the observation network, with every grid point within 100 km of the nearest station. The source depth is assumed to be 30 km in the grid search, which is a typical tremor depth in this region. We pick a grid point if it is the local maximum around 1° × 1° section, which we use as the initial locations in the gradient method. We merge the solutions when the distance between two solutions from the gradient method is less than 0.2°. The thresholds for outlier rejection, Clim and \(C_{ \lim }^{t}\), are set to 0.6 and 0.4, respectively.

We control the quality of the solution in several ways. The error is estimated via the bootstrap method, with Nb = 100. We remove any tremors where the error is greater than 2 km. We also apply a clustering technique to remove any spatiotemporally isolated solutions. We reject an event if it has no neighboring event within ± 0.2° latitude and longitude and ± 1 day. This method also detects ordinary earthquakes and does not distinguish them from tremors. We therefore select events with durations previously defined of longer than 10 s as tremors because ordinary earthquake signals are shorter than tremor signals.

Tremor detection examples

We encounter numerous scenarios for identifying deep seismic tremors across the study region, including a single tremor (Fig. 2), multiple tremors (Figs. 3, 4), and closely spaced tremors (Fig. 5). Here, we provide specific examples of the common tremor scenarios during the analysis and describe how we distinguish the detected tremors in each scenario.

Fig. 2
figure 2

Single-tremor detection result. a The star shows the final location of the tremor. The tremor occurred at 02:56:05 on May 3, 2010, with a hypocentral location of 33.965°N, 133.252°E, and 23.8 km depth. The heatmap shows the ACC distribution at 30 km depth, determined using the weights calculated as the squares of the hypocentral distances. The red triangles are the seismic stations used in the analysis that met the outlier control criteria. The white triangles mark the seismic stations that were not used in the analysis owing to cross-correlations that did not meet the required threshold. b ACC distribution and bootstrap method result. The axes show the difference from the final tremor location. The heatmaps show the ACC distribution when the tremor source is located at each point. Each blue dot represents the final tremor location for a set of bootstrap samples. c Relationship between the hypocentral distance and the weight which is the inverse of the error variance. The weight is calculated for each component to determine the tremor location and visualized after normalization by the maximum value

Fig. 3
figure 3

Multiple-tremor detection result. a Two tremors are located as local maxima in the ACC distribution, occurring between 02:45 and 02:50 on November 16, 2010. The western tremor occurred at 02:48:25, with a hypocentral location of 33.919°N, 133.888°E, and 29.0 km depth. The eastern tremor occurred at 02:45:28, with a hypocentral location of 35.057°N, 137.240°E, and 30.8 km depth. b Normalized envelope waveforms, time-shifted from the western source. The horizontal axis represents time in this time window, and 0 s corresponds to 02:45. c Normalized envelope waveforms, time-shifted from the eastern source

Fig. 4
figure 4

Location results for three tremors that occurred between 00:12:30 and 00:17:30 on November 15, 2010. The three tremor epicenters are located at the local maxima of the ACC distribution. The western tremor occurred at 00:14:14, with a hypocentral location of 33.818°N, 133.138°E, and 27.4 km depth. The middle tremor occurred at 00:15:08, with a hypocentral location of 34.077°N, 135.794°E, and 34.8 km depth. The eastern tremor occurred at 00:16:22, with a hypocentral location of 35.049°N, 137.111°E, and 35.6 km depth

Fig. 5
figure 5

Location results for two tremors that occurred between 00:57:30 and 01:02:30 on December 12, 2010. The western tremor occurred at 01:02:08, with a hypocentral location of 33.350°N, 132.525°E, and 30.6 km depth. The eastern tremor occurred at 01:02:08, with a hypocentral location of 33.877°N, 133.312°E, and 31.5 km depth. The distance between the two tremor epicenters is ~ 100 km

Figure 2a shows an example of the estimated tremor location, together with the spatial ACC distribution. The first grid search successfully selects the potential epicentral location that yields the maximum ACC, which represents a tremor source location, as the peak ACC distribution is near the final location. The ACC distribution around the source is monophasic and suitable for further analysis via the gradient method (Fig. 2b). The bootstrap method results (blue dots) are concentrated in the high cross-correlation area. Figure 2c shows the relationship between the station distance and final weights, which have been adjusted during the iterative refinement. The weighting tends to decrease as the distance increases, which is consistent with the increased effect of seismic wave attenuation at greater distances. We successfully reduce the effects of distant stations using this weighting scheme, where the signal qualities are generally poor.

We can potentially locate more than one event in a single time window by analyzing the local maxima. The ACC distribution in some cases shows two or more local maxima, suggesting that several events occurred. Figure 3a shows an example analysis for a time window that captures two events. The tremor locations are denoted by the two stars, highlighting that they are well detected by these local ACC maxima. Figure 3b, c shows the time-shifted envelope waveforms calculated from each detected tremor location. The envelope waveform peaks are aligned systematically when the stations are near the epicenter. The waveform components of the distant stations are automatically removed for each local maximum as a result of the outlier control scheme. In Fig. 3c, we can see the undetected peek around 180 s. Because we do not consider the temporal separation in a single time window, we only detect the largest signal. Therefore, the resolution of the temporal separation is limited by the length of the time window, 300 s.

Figure 4 shows another multi-tremor example, with the location method detecting three events in a single time window. We note that there was persistent tremor activity near each detected location for several hours prior to this time window.

The event separation may not be as large as that shown in previous examples. Figure 5 shows an example of a difficult source location scenario, where two nearby events occurred. The signals from both events appear in the envelope waveforms recorded at some stations. Nevertheless, our proposed method is able to successfully separate these two events.

The number and distribution of detected tremors

For the period of interest, we detect 132,704 tremors using our proposed method. This includes 3132 events that would not have been detected using the global maximum instead of the local maxima. We compare our result with that of the outlier-controlled envelope correlation method (Ide 2010) by selecting tremors from the outlier-controlled result that meet the same criteria outlined in this study. We detect 67,381 of the 98,653 outlier-controlled events for an interevent distance of < 0.2° and a hypocentral time distance of < 100 s, as well as 65,323 new events. Many of the missed events that were detected by the method of Ide (2010) are rejected on account of the short estimated tremor durations.

Figure 6 shows the detected tremor hypocenters via our proposed location method. Tremors are located in the vicinity of the plate boundary, which is consistent with the previous study. Our method also detects events outside of the tremor concentrated band. These include volcanic tremors and events occurring in Tottori (Ohmi and Obara 2002), Osaka Bay (Kamaya and Katsumata 2004; Aso et al. 2011), Kyushu (Yabe and Ide 2013), and Okayama (Ide and Tanaka 2014).

Fig. 6
figure 6

Tremor locations using our proposed location method and the seismic station coverage for a western Japan and b western Shikoku. The dots show the located tremor hypocenters, with the colors indicating their depths. The red triangles show the Hi-net seismic stations. The red circles show the volcanic tremors. The blue circles show the tremors occurring outside of the tremor concentrated band, in Kyushu, Tottori, Okayama, and Osaka Bay. The inset figure in b shows a cross section of tremors located within the red rectangle


Resolution of the location method

A unique feature of our proposed method is the detection of multiple tremor events in a single time window. However, a pair of tremor events may be difficult to recognize if they occur too close to each other. Therefore, we should determine the minimum separation required to detect multiple independent events. Figure 7a shows the number of detected tremor pairs by epicentral distance. There is a marked decrease in the simultaneous detection of event pairs in a single time window when the epicentral distance is less than 100 km, suggesting that the resolution of our method is ~ 100 km.

Fig. 7
figure 7

a Histogram of the number of detected tremor pairs by epicentral distance. b Histogram of the detection rate for synthetic waveforms of two sources via the proposed location method by epicentral distance. c Histogram of the detection rate for synthetic waveforms of two sources via the location method with no weighting scheme

We randomly select tremor source pairs from the detected tremor source locations and calculate their synthetic waveforms to estimate the resolution of our proposed method. We use the discrete wavenumber method with attenuation for a 1-D layered structure (Takeo 1985) to calculate the waveforms. We assume that each tremor is a point source with a time function that is a finite sequence of random values Td that follows an exponential distribution with P(x) = ex. The duration and magnitude of Td are adjusted to the catalog value. The tremor focal mechanism is assumed to be that of the moment tensor (strike = 228°, dip = 20°, and rake = 93°) determined for stacked broadband records by Ide and Yabe (2014). We then apply the location method to these synthetic waveforms. Figure 7b shows the effectiveness of the location method in detecting two sources based on their epicentral distance, confirming that an epicentral distance of ~ 100 km is required between two tremor sources to locate them separately.

Weighting scheme

Our weighting scheme provides a major improvement. The implementation of our weighting scheme increases the number of detected tremors from 55,327 to 132,704. The weighting scheme also reduces the tremor location errors and improves the resolution of simultaneous tremor events. These improvements gained from implementing the weighting scheme can be seen by comparing the results with (Fig. 7b) and without (Fig. 7c) weighting factors. Simultaneous tremor events cannot be detected when weighting factors are not applied, highlighting the effectiveness of the weighting scheme in recognizing tremors that are spatiotemporally close to each other.

The effect of outlier controls

Outlier controls affect the number of detected tremor sources and their associated errors. Figure 8 shows the result when we ignore the second criterion. Although this approach increases the number of detected events to 236,451, the resultant tremor sources are scattered over a broader region, suggesting numerous false detections and larger location errors. Most of these events are falsely located or falsely assigned longer duration because of outlier data.

Fig. 8
figure 8

Detected event distribution without the second criterion of outlier control which rejects an envelope when the cross-correlation with the template is below the threshold, \(C_{ \lim }^{t}\), for a western Japan and b western Shikoku. The dots show the located tremor hypocenters, with the colors indicating their depths. Many of scattered hypocenters are considered as false detections. The red triangles show the Hi-net seismic stations. The inset figure in b shows a cross section of tremors located within the red rectangle


Here, we developed a new location method for deep tectonic tremors that is based on the envelope correlation method. We reviewed the relationship between the envelope correlation and maximum-likelihood methods and determined that envelope correlation weighting should be calculated as the inverse of the error variance for consistency with the maximum-likelihood estimates. Our implementation of this weighting scheme improved the number of detections by about 240% (132,704 vs. 55,327).

Tremor activity often occurs in several places in one seismic region. It is therefore possible to detect these tremors separately using some optimized station sets for each tremor location. However, this would require extensive a priori knowledge and may not be suitable for routine monitoring using many stations. Our method enables multiple tremor detections to be made in a single time window by analyzing the local maxima instead of the global maximum. The resolution of these multiple detections is approximately 100 km based on the large number of tremor pairs for such an epicentral distance and the use of synthetic waveforms to locate the two tremor sources.

Various methods have been proposed to detect and locate tremors, and each method possesses distinct pros and cons. Although our method is not as accurate as the matching-filter technique, it is computationally light and sufficiently efficient, making it suitable for automatic data processing using long, continuous seismogram records from many seismic stations. As the available data volume is continuing to increase, the proposed method presents a worthwhile approach for quickly analyzing such a dataset to determine the detectability of tremors and obtain a tremor catalog that is of acceptable quality.



the average of weighted cross-correlation functions


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Authors’ contributions

NM developed the method and analyzed the data, and SI designed the study. Both authors read and approved the final manuscript.


We thank our laboratory members for constructive discussions. Comments from Honn Kao and an anonymous reviewer helped to improve the manuscript. The implementation of our algorithm was coded using NLopt (Johnson 2014) and GNU Parallel (Tange 2018). The figures in this manuscript were produced using Matplotlib (Hunter 2007) and Basemap.

Competing interests

The authors declare that they have no competing interests.

Availability of data and materials

The data used in this paper are available from the National Research Institute for Earth Science and Disaster Resilience. The tremor catalog generated by our proposed method will be in the Slow Earthquake Database (Kano et al. 2018;

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This study was supported by JSPS KAKENHI Grant Numbers 16H02219 and 18J13918, and MEXT KAKENHI Grant Number 16H06477.

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Correspondence to Naoto Mizuno.

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Mizuno, N., Ide, S. Development of a modified envelope correlation method based on maximum-likelihood method and application to detecting and locating deep tectonic tremors in western Japan. Earth Planets Space 71, 40 (2019).

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  • Deep tectonic tremor
  • Hypocenter determination
  • Envelope correlation method
  • Maximum-likelihood method
  • Western Japan