ORIGINAL RESEARCH article
Sec. Marine Ecosystem Ecology
Seasonal Distribution of Tuna and Non-tuna Species Associated With Drifting Fish Aggregating Devices (DFADs) in the Western Indian Ocean Using Fishery-Independent Data
- 1Marine Research Unit, AZTI, Pasaia, Spain
- 2Centro Oceanográfico de Vigo, Instituto Español de Oceanografía, Vigo, Spain
- 3Inter-American Tropical Tuna Commission, San Diego, CA, United States
- 4International Seafood Sustainability Foundation, Washington, DC, United States
- 5Marine Research Unit, AZTI, Sukarrieta, Spain
- 6Centro Oceanográfico de Madrid, Instituto Español de Oceanografía, Madrid, Spain
Man-made floating objects in the surface of tropical oceans, also called drifting fish aggregating devices (DFADs), attract tens of marine species, including tunas and non-tuna species. In the Indian Ocean, around 80% of the sets currently made by the EU purse-seine fleet are on DFADs. Due to the importance and value of this fishery, understanding the habitat characteristics and dynamics of pelagic species aggregated under DFADs is key to improve fishery management and fishing practices. This study implements Bayesian hierarchical spatial models to investigate tuna and non-tuna species seasonal distribution based on fisheries-independent data derived from fishers’ echo-sounder buoys, environmental information (Sea Surface Temperature, Chlorophyll, Salinity, Eddie Kinetic Energy, Oxygen concentration, Sea Surface Height, Velocity and Heading) and DFAD variables (DFAD identification, days at sea). Results highlighted group-specific spatial distributions and habitat preferences, finding higher probability of tuna presence in warmer waters, with higher sea surface height and low eddy kinetic energy values. In contrast, highest probabilities of non-tuna species were found in colder and productive waters. Days at sea were relevant for both groups, with higher probabilities at objects with higher soak time. Our results also showed species-specific temporal distributions, suggesting that both tuna and non-tuna species may have different habitat preferences depending on the monsoon period. The new findings provided by this study will contribute to the understanding of the ecology and behavior of target and non-target species and their sustainable management.
Pelagic ecosystems are highly dynamic environments in time and space (Kaplan et al., 2010; Dueri and Maury, 2013), accounting for 99% of the biosphere volume (Angel, 1993) and supplying more than 80% of the fish consumed by humans (Pauly et al., 2002). Due to the limited knowledge of pelagic ecosystem functioning and diversity (Kaplan et al., 2014), there is an increasing need to obtain reliable spatial information on pelagic species distributions (Costello and Kaffine, 2010). Indeed, it is necessary to understand how marine populations are distributed across the environment, and the drivers of their movement and dynamics, for a correct assessment of fish populations and ecosystem functioning, and, hence, fisheries management and conservation of exploited species (Paradinas, 2017).
The industrial tropical tuna purse seine fishery is one of the most important fisheries in the world, accounting for 64% of tuna catches worldwide (ISSF, 2019). In the Indian Ocean, more than 80% of the total sets of purse seiners in recent years have been on man-made drifting fish aggregating devices (DFADs) (Báez et al., 2018). The remainder of the purse seine fishery catch comes from sets on unassociated tuna schools, also known as free-swimming schools. In the past, the majority of floating objects used by fishers were natural floating objects (e.g., driftwood, logs or coconuts) encountered by chance, traditionally called “logs.” Over time, the objects were modified by fishers and, thus, an operational definition was adopted for them (i.e., man-made DFADs) to separate them from natural floating objects. Because of the aggregative behavior of certain tropical pelagic species, DFADs attract a large variety of marine species (Castro et al., 2002; Lezama-Ochoa et al., 2015), including tuna and non-tuna species. The average species composition of the tuna DFAD catches in the Indian Ocean by Spanish purse seiners during recent years (2014–2017) has been dominated by skipjack (60%), followed by yellowfin (33%), and bigeye (7%) (Báez et al., 2018). The use of DFADs has widely increased in all oceans since the early 1990s (Dempster and Taquet, 2004; Fonteneau et al., 2013). It is estimated that around 100,000 DFADs are deployed globally each year (Scott and Lopez, 2014; Gershman et al., 2015). In particular for the Indian Ocean, it was estimated that the number of DFADs deployed increased by a factor of 4.2 over the period 2007–2013 (Maufroy et al., 2016). The figures above indicate the importance and value of the DFAD fishery at both global and regional scales and, therefore, it is necessary to improve the knowledge of the DFAD fishery dynamics as well as the spatio-temporal distribution of tuna and non-tuna species associated to those DFADs. This understanding will contribute to enhance stock assessments and the scientific advice for tropical tunas in tuna regional fisheries management organizations (t-RFMOs). Yet, studies on detailed distribution patterns of pelagic species are scarce in the Indian Ocean. Those studies have been carried out using fishery-dependent data, such as catch logbooks (Chen et al., 2005; Lee et al., 2005; Rajapaksha et al., 2013; Potier et al., 2014; Arrizabalaga et al., 2015; Druon et al., 2017) or observers data onboard commercial vessels (Sequeira et al., 2012; Lezama-Ochoa et al., 2016; Coelho et al., 2017) and have not necessarily been focused on purse seine information.
Drifting fish aggregating devices are monitored and tracked with satellite linked buoys (Moreno et al., 2016a) and have undergone numerous technological improvements in the 2000s, such as the introduction of an echo-sounder in the buoy to remotely inform fishers on potential fish presence and biomass underneath the object. The first echo-sounder buoys appeared on the market in 2000, but fishers did not start to use them regularly until the mid-2000’s (Lopez et al., 2014), and, nowadays, they are used in most tropical tuna purse seine fleets around the world (Moreno et al., 2016b). DFADs automatically collect huge amounts of acoustic information over several months, covering thousands of kilometers across the ocean. Because these devices collect fishery-independent information about the pelagic ecosystem in a cost-effective manner (Moreno et al., 2016a), recent studies have noted the potential this data can have in the research of several issues of scientific relevance (Dagorn et al., 2006; Santiago et al., 2015; Lopez et al., 2016; Moreno et al., 2016a), including the investigation of the ecology and behavior of DFAD-associated species and the development of alternative abundance indices (Santiago et al., 2017, 2019), among others. Unlike fishery-dependent data, echo-sounder buoys provide acoustic data that is less affected by fisheries-related dynamics such as fleet behavior, effort, and spatio-temporal constraints. However, despite these obvious advantages, this type of data has barely been used to model species distribution and environmental preferences of tunas and non-tuna species (Lopez et al., 2017b).
Species distribution models (SDMs) have been broadly used in biogeography and ecology studies to answer several environmental questions, including fisheries impacts (Varela et al., 2011). In general, SDMs link occurrence or abundance data of one or more species with a multivariate set of environmental information, which allows the prediction of their distribution in unsampled areas or periods of time (Anderson et al., 2003; Phillips et al., 2006; Zimmermann et al., 2010; Martínez-Minaya et al., 2018). These models therefore assess whether or not an area is suitable for a particular species by taking into account the relevant environmental variable (Costa et al., 2017). In order to estimate and predict the distribution of species, a large number of modeling algorithms have been used [e.g., BIOCLIM, general additive models (GAMs), MaxEnt, and boosted regression trees (BRT), APECOSM, SEAPODYM, among others] (Hastie and Tibshirani, 1990; Guisan and Zimmermann, 2000; Lehodey et al., 2008; Maury, 2010; Guisan et al., 2013; Young and Carr, 2015; Hazen et al., 2017). However, these models do not account for uncertainty in the parameters or the spatial-autocorrelation of data which is necessary to provide a more clear and detailed distribution of the species (Costa et al., 2017). Bayesian statistical methods offer the possibility to use both the model parameters and the observed data as random variables (Banerjee et al., 2014), which provides a more realistic and precise estimation of uncertainty (Haining et al., 2007). Using Bayes’ theorem, posterior probability distributions for all unknown quantities of interest (i.e., parameters) are built combining the uncertainty in the data (expressed by the likelihood) with additional information (expressed by prior distributions) (Kinas and Andrade, 2017). Moreover, the Bayesian approach allows the addition of the spatial component as a random-effect term, considering spatial autocorrelation of the data, and reducing its influence on the estimates of the effects of geographical variables (Gelfand et al., 2006). Because of these advantages, Bayesian methods are increasingly used in fisheries studies in recent years (Muñoz et al., 2013; Pennino et al., 2014; Paradinas et al., 2015).
Within this context, this study aims to investigate tuna and non-tuna species distribution dynamics in the Indian Ocean implementing Bayesian Hierarchical spatial models (hereafter B-HSMs). For this purpose, we use presence/absence data derived from fishers’ echo-sounder buoys, a set of environmental information, and DFAD-inherent variables such as the soak time and object identification. In addition, the Indian Ocean is characterized by strong fluctuations in the environment linked with monsoon regimes, which affect ocean circulation and biological production. Because of this, the spatio-temporal distribution differences have also been analyzed for each monsoon season. Understanding the habitat preferences of tuna and non-tuna species and their dynamics may contribute to specific spatial management and conservation measures toward sustainable fisheries management in this area.
Materials and Methods
Our study area is bounded by longitude 30°E to 80°E and latitude 15°N to 30°S in the Western Indian Ocean, within the Indian Ocean Tuna Commission (IOTC) convention area. DFADs are not uniformly distributed, and surface currents and winds affect their trajectory (Davies et al., 2014b). The marked monsoon system strongly influences the ocean circulation in the Indian Ocean, which could have a significant impact on oceanography and productivity in the area (Schott and McCreary, 2001; Wiggert et al., 2006; Schott et al., 2009). The Intertropical Convergence Zone (ITCZ) location changes through the year inducing regime fluctuations, creating southwestern trade winds during summer in the northern hemisphere and northeastern trade winds during winter period in the northern hemisphere (Wyrtki, 1973). The summer monsoon lasts from June to September and the winter monsoon lasts from December to March, with two inter-monsoon periods in April-May and October-November. The drastic changes in circulation of the surface currents induced by the monsoon affects biophysical factors (i.e., chlorophyll, temperature, salinity, dissolved oxygen) (Tomczak and Godfrey, 2013) and thus, may affect the presence and the relative composition of species in an area (Jury et al., 2010).
The acoustic information was obtained by Satlink buoys (SATLINK, Madrid, Spain1), which were linked to DFADs and deployed at sea by a Spanish purse seine fishing company Echebastar. The buoys are equipped with a Simrad ES12 echo-sounder which transmits to the user the potential amount of biomass (in tons, t) aggregated underneath DFADs using a depth layer echo-integration procedure (Simmonds and MacLennan, 2005), with an internal detection threshold of 1 ton. The Simrad ES12 operates at a frequency of 190.5 kHz with a power of 140 W (beam angle at –3 dB: 20°) and is programmed to operate for 40 s every time it samples. Thirty two pings are sent from the transducer during this period and an average acoustic response is measured and stored in the buoy (hereafter called “acoustic sample”). The observation depth range is composed of ten homogeneous layers, each with a resolution of 11.2 m, and it extends from 3 to 115 m, with a blanking zone between 0 and 3 (see Lopez et al., 2016; Orue et al., 2019a for further technical details on the buoy and the protocol used to process the acoustic information). A virtual vertical depth limit of 25 m was established as a possible boundary between tuna and non-tuna species based on scientific evidence from tagging and acoustic surveys in the Indian Ocean around DFADs (Dagorn et al., 2007; Moreno et al., 2007b; Taquet et al., 2007; Govinden et al., 2010; Filmalter et al., 2011; Forget et al., 2015). Though there may be temporary overlaps in the depth range used by the species at DFADs, evidence suggests that tuna spend most of the time below 25 m and non-tuna species remain in shallower waters in the Indian Ocean (Forget et al., 2015). Signals corresponding to depths shallower than 25 m (i.e., the sum of the first two layers) were thus assumed to be non-tuna species, and those deeper than 25 m (i.e., the sum of the third to the tenth layer) were presumed to be tuna. Similar depth limits were used by other studies in the field using the same buoy (Robert et al., 2013; Lopez et al., 2017a, b). As highlighted by Phillips et al. (2019), some tuna individuals are likely to be present in the area above 25 m. However, considering the data above 25 m as tuna introduces considerable uncertainty. The 25 m cut-off was kept constant throughout the experiment.
The acoustic dataset contains information about the owner vessel, buoy ID (unique alphanumeric code provided by the manufacturer), location (latitude and longitude), date and GMT hour, and biomass estimates from 962 buoys spanning January 2012 to May 2015 in the Indian Ocean. The buoys used in this study were linked to newly deployed DFADs (i.e., objects with no aggregation associated when deployed), with a maximum monitoring time of 60 days at sea. This time constraint is based on a preliminary data analysis showing that after 60 days only 50% of the objects were available. A single daily acoustic signal was selected per day for each of the 962 buoys. The database was pre-processed following a protocol proposed by Orue et al. (2019a). Presence/absence data are modeled in this paper to avoid loss of information and maximize the available data. If the echo-sounder buoy emitted a signal other than zero between 3 and 25 m it was considered to record the presence of non-tuna species, regardless of the time of day, while if the echo-sounder emitted a signal other than zero between 25 and 115 m it was considered to record the presence of tuna species. The final number of acoustic samples available for this study after data cleaning was 42,322 (Figure 1).
For additional validation of the model, the logbooks of the DFADs were collected for the time periods considered in the study. These logbooks have been developed by Spanish national authorities to monitor the fishing activity of the fleet (De Molina et al., 2013).
Autocorrelation (ACF) and Partial Autocorrelation Functions (PACF) were performed to identify annual, seasonal (i.e., monsoonal) and daily non-random temporal patterns in the data using the stats package of the R software (R Development Core Team, 2017). No correlation was found at year level. Non-random distributions of acoustic records were detected for different monsoon seasons and at the daily scale. For this reason, data was aggregated in four different groups following the monsoon pattern of the area: (i) Winter Monsoon (December–March), (ii) Spring Intermonsoon (April–May), (iii) Summer Monsoon (June–September) and (iv) Autumn Intermonsoon (October–November). Day-scale patterns in acoustic records between the 7th and 53rd days did not show autocorrelation and were therefore deemed appropriate for inclusion in the models. Data from the first and last weeks of the time series were removed.
The environmental variables were obtained from the EU Copernicus Marine Environment Monitoring Service (CMEMS).2 Eight abiotic and biotic variables were extracted for each position and date of the acoustic dataset: sea surface temperature (SST), velocity (VEL), and heading (HEADING) of the current, salinity (SAL), eddie kinetic energy (EKE), sea surface height (SSH), chlorophyll concentration (CHL), and oxygen concentration (O2) (Table 1).
Table 1. Predictor variables used for modeling tuna and non-tuna occurrence with DFAD data in the Indian Ocean.
Before their use in the models, all environmental variables were tested for outliers, missing values and correlation. In addition, collinearity was assessed using the variance inflation factor analysis (VIF) with the function “corvif” in the AED R-package and a cut-off value of 5 (Zuur et al., 2009). Based on these preliminary analyses, velocity was eliminated for the posterior modeling as it was highly correlated with eddie kinetic energy (Pearson correlation, r > 0.9; p-value < 0.001). In order to facilitate interpretation and enable comparison of relative weights between variables (Kinas and Andrade, 2017), these were standardized using the function “decostand” in the vegan R-package (Oksanen et al., 2013). Moreover, days at sea (i.e., time spent in the water since initial deployment) was also included in the models as explanatory variable.
Bayesian Hierarchical Spatial Models (B-HSMs)
B-HSMs (Muñoz et al., 2013) were used to investigate the relationship of tuna and non-tuna species with the selected environmental variables and to obtain the predicted spatio-temporal probability of presence of these groups. In addition to the environmental variables and days at sea, buoy ID was included in the models as a random effect to verify its relevance and account of possible sampling structure autocorrelation. A buoy’s individual behavior due to random factors or non-observed characteristics may have caused some variability in the data. Ignoring such non-independence may result in an invalid statistical inference (Sainani, 2010). Thus, the buoy ID was included in the models to remove any buoy-specific bias (Lopez et al., 2017b).
In the B-HSM framework we used, Yi represents the species group (i.e., tuna and non-tuna) occurrence (1 being presence; 0 being absence) for each location i, and then the occurrence was modeled as:
where πi is the probability of presence of a species for a specific location i, Xiβ is the matrix of the fixed effects of the linear predictor, Zi is the buoy random effect and Wi represents the spatially structured random effect at location i. In particular Wi, account for the spatial correlation among observations at nearby locations. As required by the Bayesian approach prior distributions were assigned to every parameter of the model. For Wi we assumed a prior Gaussian distribution with a zero mean and a Matérn covariance function, which depends on the hyperparameters k and τ, that represents its range and variance. The range was fixed as the 20% of the diameter of the region and the variance equal to 1 (Lindgren et al., 2011).
Parameters estimation and prediction were obtained using the Integrated Nested Laplace Approximations (INLA) approach (Rue et al., 2009) and R-INLA package.3 INLA is an alternative to Monte Carlo Markov Chain (MCMC) for fitting a large class of Bayesian models (Rue et al., 2009) and has several advantages over other Bayesian approaches. For example, it is faster (i.e., needs less computing time) since the algorithm is naturally parallelized, which makes possible to take advantage of the new generation of multicore processors (Beguin et al., 2012). The model syntax is straightforward, which permits a great compromise of automation with relatively few lines of code.
For fixed effects, no prior information on the parameters of the model was available, so we used vague prior distributions with a mean of 0 and a variance of 1000 as suggested by Held et al. (2010). Posterior distributions were obtained for each parameter of the model. Unlike traditional frequentist approaches, where the mean and the confidence interval are provided, this type of distribution enables explicit probability statements about parameters. Consequently, values included between the 0.025 and 0.975 quantiles of the posterior distribution represent that the unknown parameter is 95% likely to fall within this region (Dell’Apa et al., 2017).
Explanatory variable selection was performed beginning with all possible interaction terms but only the best combination of variables was chosen based on three different measures: (i) the Watanabe-Akaike information criterion (WAIC) (Watanabe, 2010), (ii) Deviance Information Criterion (DIC) (Spiegelhalter et al., 2002), and (iii) Log-Conditional Predictive Ordinates (LCPO) (Roos and Held, 2011). The smaller the values of these measures, the better the compromise between fit, parsimony, and predictive quality of the model. Thus, we choose the best model based on the best balance between lowest DIC, WAIC, and LCPO values, including only relevant predictors (i.e., those with 95% credibility intervals, not including the zero; Fonseca et al., 2017).
B-HSMs were validated using a cross-validation procedure (Fielding and Bell, 1997). The dataset was randomly split into two main subsets: a training dataset including 80% of the total observations, and a testing dataset with the remaining 20%. The training dataset was used to model the relationship between observed data and the explanatory variables and the testing dataset was used to evaluate the predictions’ accuracy. The validation procedure was repeated 10 times for the best model of each group of species (i.e., tuna or non-tuna species) and the results were averaged over different random subsets. In particular, to evaluate the model’s performance, we used the area under the receiver-operating characteristic curve (AUC) (Fielding and Bell, 1997) and the True Skill Statistic (TSS) (Allouche et al., 2006).
AUC measures the model’s ability to discriminate between sites where the species are present and those in which the species are absent. The values for AUC range from 0 to 1, where 0.5 indicates a performance no better than random, values between 0.6 and 0.9 indicate results of presence/absence different from random, and values > 0.9 are excellent to ensure that the results are non-random (Roos et al., 2015). TSS is a threshold-dependent measure that is not affected by the size of the validation set and corrects AUC for the dependence of prevalence on specificity (i.e., ability to correctly predict absences) and sensitivity (i.e., ability to correctly predict presence) (Allouche et al., 2006). Both statistics are used in combination when evaluating the predictive power of an SDM (Pearson et al., 2006; Brodie et al., 2015).
In addition, a second cross-validation approach was performed for tuna models using an additional fishery-dependent dataset. FAD logbooks were used to verify whether or not the B-HSM predictions matched with catches in the same spatio-temporal window. Fishing sets on DFAD were identified as presences, while visits to DFADs without fishing activity and where no fish were observed were classified as absences, providing 3603 data points for cross-validation. This cross-validation procedure provided additional and complementary AUC and TSS measures.
The probability of presence was predicted in the rest of the area of interest using Bayesian kriging, which treats the parameters as random variables in order to incorporate uncertainty in the prediction process (see Muñoz et al., 2013 for further information). To predict the relationship between species group and habitat features per season, explanatory variables were aggregated with a seasonal monsoon temporal resolution using the “raster” package (Hijmans et al., 2017).
Finally, with the intention of capturing general patterns in spatial trends, we plot the functional response between selected environmental variables and predicted values using ggplot R- package (Wickham, 2016) to apply a smoothing function. This technique uses locally weighted scatterplot smoothing (lowess), which is an outlier-resistant method to estimate a polynomial regression curve including local bootstrap methods with the percentile technique to gather the original lowess fit change.
The best fit B-HSM model included SST, SSH, EKE and days at sea as relevant predictors for tuna presence, in addition to spatial and buoy random effects. All models without these two random effects resulted in higher WAIC, DIC, and LCPO than those with them (Table 2).
Based on the final model, a high probability of tuna presence is expected in warmer surface waters (posterior mean = 0.14; 95% CI = [0.11, 0.17]), with higher values of SSH (posterior mean = 0.16; 95% CI = [0.12, 0.19]) and lower eddy kinetic energy values (posterior mean = −0.18; 95% CI = [−0.22, −0.14]). The probability of tuna presence is also explained by days at sea, indicating higher probabilities when the object stayed more days in the water (posterior mean = 0.03; 95% CI = [0.02, 0.03]) (Table 3). Figure 2 shows that the model found the highest probabilities of tuna presence in warm waters (i.e., between 26 and 30°), moderate SSH values and EKE values around 0.1 m2. s2.
Table 3. Numerical summary of the marginal posterior distribution of the fixed effects for the best tuna B-HSMs selected.
Figure 2. Functional responses of the final tuna B-HSMs (A, Sea Surface Temperature; B, Sea Surface Height; C, Kinetic Energy). The solid line represents the smooth function estimate; the shaded region represents the approximate 95% credibility interval.
Maps of predicted probability of tuna presence show different preferential habitat patterns in monsoon periods (Figure 3). In winter periods two hotspots were observed, one over 10° north and another over 5° south. The main hotspots seem to lay on the equatorial area during the spring inter-monsoon and, then, the probability pattern spreads eastward through the equator during the summer period. During autumn inter-monsoon (October–November), the highest probabilities of tuna presence were found in three well-defined lactations between 0 and 10° south.
When the spatial effect was included, maps showed similar patterns as when only environmental variables were included. Therefore, most of the variability in the data is explained by the environmental variables included in the B-HSM (Figure 4). Hotspots on spatial effect maps are more marked than on maps of the posterior mean of tuna occurrence probability, which may indicate that there are other ecological processes that are not being considered in this study.
The occurrence probability for this group was explained by the SST, the CHL and the days at sea. The final B-HSM for non-tuna species also included spatial and buoy random effects as relevant predictors. As for the tuna B-HSM, all models without these random effects resulted in higher WAIC, DIC and LCPO scores (Table 4).
Higher probabilities of non-tuna species were found in colder (posterior mean = −0.08; 95% CI = [−0.13, −0.03]) and productive waters (posterior mean = 0.11; 95% CI = [0.04, 0.17]). Days at sea was positively related with probability of presence (posterior mean = 0.01; 95% CI = [0.01, 0.02]) although its effect is smaller than in the tuna model, based on the posterior mean values (Table 5). In particular, as shown in Figure 5, the probability of non-tuna presence decreased with temperature continuously from 20°C, while the chlorophyll showed an increasing pattern, with the highest probabilities of non-tuna presence found in waters with chlorophyll concentrations higher than 0.8 mg/m3.
Table 5. Numerical summary of the marginal posterior distribution of the fixed effects for the best non-tuna B-HSM selected.
Figure 5. Functional responses of the final non-tuna B-HSMs (A, Sea Surface Temperature; B, Chlorophyll). The solid line represents the smooth function estimate; the shaded region represents the approximate 95% credibility interval.
Maps of the predicted probability of non-tuna species presence identified more marked hotspots during the winter and spring periods, versus scattered hotspots during summer monsoon and autumn inter-monsoon (Figure 6). Throughout the year, intermediate probabilities are found off the coast of Somalia between 0 and 10° north. During the winter period another hotspot in the SE of Seychelles is detected, also for tuna, but less marked.
Spatial effect maps for non-tuna species showed patterns similar to the posterior mean maps (i.e., although with different scales), which suggests that most of the variability is explained by the variables included in the model (Figure 7).
Model prediction performance scores showed AUC values greater than 0.65 (i.e., 0.75 ± 0.07 for tuna models and 0.68 ± 0.06 for non-tuna models), which indicates a good degree of discrimination between locations where tuna and non-tuna groups were present and those where they were absent (Table 2). Likewise, TSS values ranged between 0.20 and 0.39, which represents good model ability to predict true negative and true positive predictions (Brodie et al., 2015). The values of AUC and TSS for the tuna model using the fishery-dependent dataset (i.e., catch and DFADs activities information from fishing and FAD logbooks respectively) achieved lower values than the ones obtained from the echo-sounder estimated presence by B-HSMs (Table 6). However, AUC and TSS values were reasonable, 0.60 ± 0.06 and 0.18 ± 0.08, respectively, indicating good prediction performance for the models.
Table 6. Average and standard deviation AUC and TSS values for the final models selected in each case for tuna and non-tuna species using two different datasets (fisheries-independent and fisheries-dependent) for the cross-validation.
This study represents the first investigation of the spatial and temporal distribution of tropical tuna and non-tuna species aggregated under DFADs in the Indian Ocean using fishery-independent data collected by fishers’ echo-sounder buoys. The results showed species-specific distribution patterns based on relevant environmental preferences and provide new insights on species habitat when associated with DFADs. Despite tuna and tuna-like species being the most important resources exploited by a variety of fleets operating in the Indian Ocean, detailed studies of their habitat and ecological preferences are limited. Previous knowledge of the distribution dynamics and environmental preferences of tropical tuna in the Indian Ocean have primarily been obtained from fishery-dependent data of purse seiners and longlines fisheries (Chen et al., 2005; Lee et al., 2005; Fonteneau et al., 2008; Song et al., 2008, 2009; Tew-Kai and Marsac, 2009; Lan et al., 2013; Lumban-Gaol et al., 2015), but not fisheries-independent data. Furthermore, only a few studies have considered tuna and other species associated with DFADs. Therefore, the relationship of DFAD-associated species and their local environment is still unclear (Fraile et al., 2010). To our knowledge, only one other study has used acoustic data collected by fishers’ echo-sounder buoys to relate the biomass gathered under the objects to environmental factors, but it was focused on the Atlantic Ocean (Lopez et al., 2017b).
Differing species-specific environmental preferences are suggested by existing literature, likely reflecting differences in the target data (e.g., body size) and the spatio-temporal bounds of the varied methodologies. For example, Mohri and Nishida (2000) and Song et al. (2008), used fishery data that commonly target adult individuals of yellowfin tuna (Thunnus albacares) to suggest a depth range of 100–180 m for this species. In contrast, Cayré and Marsac (1993) and Dagorn et al. (2006) suggested a depth range of 40–110 m for the same species using electronic tagging for juveniles. Temperature has been used as an explanatory variable for tuna habitat in many studies. Mohri and Nishida (2000) and Song et al. (2008) suggested 15–17°C as an optimal temperature range for yellowfin tuna, while Romena (2001) found 17–20°C using qualitative methods. Romena (2001) also suggested an optimal salinity range of 34.2 to 35 PSU for adults of yellowfin tuna in the Indian Ocean. Dissolved oxygen is another important factor commonly used in these studies. Romena (2001) suggested a range of 2.6–5 mg ⋅ L−1 of dissolved oxygen for yellowfin tuna, while Song et al. (2008) of 2–3 mg ⋅ L−1. Song et al. (2009) suggested an optimum of chlorophyll-a of 0.090–0.099 mg L–1 for yellowfin tuna, different from Lee et al. (1999) which used monthly means of sea surface color in the analysis. Similarly, inter-species environmental preference data is varied. For the habitat preference of bigeye tuna, (Thunnus obesus) in the Indian Ocean, Song et al. (2009) showed an optimal range of 240–280 m of depth, 12–14°C of temperature, and 2–3 mg ⋅ L−1 of dissolved oxygen, whereas for skipjack (Katsuwonus pelamis) sea surface temperature varied between 15 and 30°C (Barkley et al., 1978) and a preferred range from 23 to 28°C (Arrizabalaga et al., 2015). Aggregating these complimentary datasets provides greater overall insight on the tuna environmental preference in the Indian Ocean.
The species-specific temporal distributions found in this study suggest that both tuna and non-tuna species associated with DFADs may have different habitat preferences depending on the monsoon period. These results are consistent with previous studies in which regular seasonal variability in catch has been observed (Kaplan et al., 2014) as well as different spatial patterns in fishing effort in fleet behavior during the monsoon period in the Indian Ocean (Davies et al., 2014a). We note that the temporal scale (e.g., daily, monthly, seasonal or monsoon aggregation) could be case-dependent. Here, we selected the monsoon aggregation on the basis of the ACF and PACF analysis after testing daily and monthly aggregations in B-HSMs and achieving worse predictions and fits (in terms of WAIC, and LCPO). However, others temporal scales (e.g., quarterly) could provide different results, therefore comparative studies are needed to assess the appropriate temporal aggregations (Pennino et al., 2019).
A major difference in this study with respect to fisheries-dependent studies (e.g., Davies et al., 2014a) is that we did not find high probability of presence in the Mozambique Channel throughout the year. However, it is known that the purse seine fisheries have recorded consistent annual catches in this area since 1985 and large quantities of tunas associated to floating objects within this local fishery yearly in March (end of the winter monsoon) and in April–May (inter-monsoon). Model bias likely explains the absence of probability of presence for this area and timeframe. First, this model has a lower prediction power in areas with few or no observations. Second, B-HSMs implicitly assume that correlation is only dependent on the distance between observations, and therefore does not account for the presence of physical barriers– in this case, the island of Madagascar. Efforts to account for spatial disruptions within current model algorithms are in development (Martínez-Minaya et al., 2019). Moreover, there are some differences between our presence probability maps and fishery catch distribution maps. This could be because the probability of occurrence may show different spatio-temporal trends than biomass abundance or catch. For example, for some species, measures of occurrence and measures of abundance respond differently to environmental variables (Heinänen et al., 2008) depending on the life habits, age-size, and trophic niche.
Understanding the habitat characteristics and dynamics of pelagic species aggregated under DFADs contributes to the management and design of conservation measures for these valuable fishery resources, for example, by providing a baseline for the design of area closures, which is especially important in a changing ocean. Currently, the vast majority of spatial management measures for marine species, such as Marine Protected Areas (MPA), set fixed boundaries around mobile species (Hyrenbach et al., 2000; Norse et al., 2005; Crowder and Norse, 2008), which may be rendered inadequate by the dynamism of the ocean. In recent years, the concept of dynamic ocean management has been defined as “management that changes in space and time in response to the shifting nature of the ocean and its users based on the integration of new biological, oceanographic, social and/or economic data in near real-time” (Maxwell et al., 2015). This concept requires more precise data and faster collection, processing, and analysis to enable near real-time responses (Wilson et al., 2018). The approach used in this study could be the first steps toward designing, in the near future, spatio-temporal conservation management measures (e.g., area closures) for both target and non-target species, using near real-time habitat predictions based on acoustic data provided by fishers’ echo-sounders and remote sensing systems.
Environmental Predictors of Species Distribution
This study showed that the spatio-temporal distribution and relevant environmental factors were different for tuna and non-tuna species aggregated at DFADs, suggesting that tuna and non-tuna species may have different habitat preferences.
B-HSM results highlighted the importance of SST, SSH, EKE and days at sea for tuna presence. In particular, these results suggest that areas with higher SST and SSH and lower EKE yielded higher probability of tuna presence.
The negative effect with eddy kinetic energy may be due to the energetic cost of being associated with fast-DFADs. This relationship can be observed during summer and in autumn inter-monsoon, when the North Equatorial Current reverses its directions toward the east and combines with the eastward-flowing Equatorial Countercurrent, such that its broad eastward flow dominates the northern Indian Ocean (Benny, 2002). The probability of tuna presence is close to zero during this period above 0°N probably due to the high speed of the buoys that flow with this current eastwards at high speeds (Schott and McCreary, 2001; Tomczak and Godfrey, 2013). This result is consistent with the study of Lopez et al. (2017b), in which tuna predilection to associate with DFADs at speeds between 0.5 and 1 kn or lower was shown. Additionally, in a study by Moreno et al. (2007a) to better understand tuna behavior at DFADs in Indian Ocean, fishers who were interviewed believe that fish leave DFADs when a significant change in the DFAD speed or change in the direction of the trajectory occurs.
Sea surface height was also relevant for the tuna model, presenting a positive relationship with tuna occurrence. This finding is consistent with previous studies that showed a similar relationship in the three oceans (Druon et al., 2017; Lan et al., 2017). Areas of positive SSH values are usually associated with deeper mixed layer depths (MLDs) (Gaube et al., 2013; Dufois et al., 2014, 2017) and mesoscale features (López-Calderón et al., 2006; Benitez-Nelson et al., 2007; Lopez et al., 2017b), suggesting that tuna may prefer deep and well mixed waters in the center or the edge of productivity structures (e.g., eddies). Higher probabilities of tuna presence were also found in areas with high SST. Tuna’s preference for warm surface waters has been observed in previous investigations, where warm waters have been linked to both higher catch rates of large tunas (Zagaglia et al., 2004; Lan et al., 2011, 2017) and acoustic biomass data (Lopez et al., 2017b). Overall, B-HSM results are in accordance with previous studies in the field, which suggest that tropical tunas usually prefer warmer environments that display near null or positive SSH values (Arrizabalaga et al., 2015; Lan et al., 2017; Lopez et al., 2017b).
One uncommon result in this study is a low probability of tuna in the Mozambique Channel area throughout the year. Our methodology only considered DFADs deployed by a single fishing company, and having known trajectories since their deployment. Buoys deployed on natural objects were excluded, because their soak time could not be accurately determined. High abundances of natural floating objects have been observed in the Mozambique Canal (Dagorn et al., 2013), so there have always been fewer deployments of DFADs in this area than in the rest of the Indian Ocean (Davies et al., 2014b). Incorporation of data from this area would provide information complimentary to our study.
A positive relationship was also identified between tuna occurrence and the number of days that the DFAD were at sea, meaning that the longer the DFAD spends in the water, the higher its probability of aggregating tuna. This positive relationship is probably related to the colonization process of the DFADs and is in accordance with other studies (Lopez et al., 2017b; Orue et al., 2019b) showing that, in general, biomass increases with time at DFADs. DFADs may contribute to the formation of large schools of fish and shaping the optimal size of the school (Pitcher and Parrish, 1993) during the first 30–60 days at sea (Orue et al., 2019b). This study only considers DFADs that have stayed at sea 60 days. Additional studies should try to include longer time series in the analysis and test the importance this variable has in the long-term processes associated with DFADs ecology.
The echo-sounder buoys used in this study provide a single value of tuna biomass that includes the three associated species under the DFADs so, for the moment, the specific distribution of each species cannot be analyzed. This has been widely discussed in other studies, where the need for multi-frequency studies on echo-sounder buoys has been highlighted for more effective tuna species discrimination at DFADs (Moreno et al., 2019; Orue et al., 2019b). Once it is possible to effectively discriminate between the three tropical tuna species associated with DFADs, further analyses should identify differences in species behavior and environmental variables.
For non-tuna species, the probabilities of presence were, in general, lower than for the tuna group where the maps of the posterior mean probability show less marked hotspots. This may be related to the buoy detection ability. The buoy used in this study has a blanking zone (i.e., a data exclusion zone to remove transducer’s near-field effect; Simmonds and MacLennan, 2005) between 0 and 3 m, so species located at distances closer from the DFAD are not easily detected by the beam. In this case, we do not believe that the detectability limit will greatly affect outcomes, since some by-catch species are known to be strongly and tightly associated with the DFAD (intranatant/extranatant species, see Freon and Dagorn, 2000) and thus, may be more easily detected. The minimum detection threshold calculated by the buoy (i.e., 1 ton) may be important for non-tuna species, as bycatch species are usually found in DFADs in relatively low biomass (Romanov, 2002, 2008; Amandé et al., 2008; Dagorn et al., 2012; Ruiz et al., 2018). However, as has been explained in previous studies using this buoy brand (Orue et al., 2019b), due to the empirical algorithm used to convert raw acoustic backscatter into biomass, one ton of biomass determined through the skipjack-based algorithm may not necessarily represent the same quantity of non-target species, but certainly less, suggesting that the one ton threshold may not have impacted results significantly. Although we do not believe that these limitations have important implications for the final results, they may affect, to some extent, the smaller estimated probabilities of non-tuna presence.
In this case, the most relevant environmental variables were CHL and again, SST, although in this case the relationship with surface temperature was negative. The negative relationship between SST and non-tuna species presence, and the positive one with CHL, indicates that non-tuna species may show predilection to cold, high productivity waters. In the monsoon predictions, we found a relatively stable area throughout the year with the highest probability of non-tuna presence off the coast of Somalia, which is characterized by the chlorophyll-rich water (Jury et al., 2010). These results are in accordance with published research that investigated the environmental preferences of non-tuna species associated with DFADs in the Atlantic Ocean (Lopez et al., 2017b). The most marked hotspots during the spring period coincide with the Great Whirl, an anticyclonic eddy generated by the Somali current. Although the eddy is usually evident between June and September, the Great Whirl’s anticyclonic circulation reveals on average in April (Beal and Donohue, 2013). Non-tuna probability presence, as well as for tuna, is positively correlated with days at sea. This finding is consistent with a previous study that used fishery-independent data which showed increasing non-tuna biomass the longer the DFAD is at sea (Orue et al., 2019b).
Random Effects for Species Distribution
Results showed that the buoy random effect was relevant to explain part of the variability in the distribution of both tuna and non-tuna species that is not explained by the environment. These results could indicate that other processes driving the associative behavior of tuna and non-tuna species at DFADs have not been incorporated in this study. Some of these may be characteristics associated to the structure of the DFAD. In fact, fishers state that characteristics of the construction can have direct impacts on the effectiveness of the DFAD for fish attraction (Moreno et al., 2016c). For example, fishers build objects with float depth and underwater features dependent on the ocean, and evidence has been provided of a significant relationship between DFAD depth and the colonization of tuna in the Indian Ocean (Orue et al., 2019b).
The spatial effects, which explain the intrinsic spatial variability of the data without the use of explanatory variables, showed similar patterns in probability maps for both tuna as well as non-tuna species. Indeed, maps of the spatial effects highlighted the same hotspots identified in the response variables, although the patterns are more marked than for the models without spatial effects. This is especially true for non-tuna species, which may suggest that part of the variability of DFAD data is not explained by the selected variables. This suggests that other ecological processes not considered in this study may be implicated in the process of species aggregation in DFADs at different scales (e.g., social behavior of tuna at DFADs, FAD densities in the area, dispersal or the patterns of aggregative species). This is consistent with previous studies, where environmental factors were seen to have a more important role in free schools than in DFAD communities in the Indian Ocean (Lezama-Ochoa et al., 2015). Therefore, we could hypothesize that for small tuna that usually aggregate with DFADs, the importance of environmental conditions are not as relevant as for big tunas, which are usually found in free swimming schools. Marsac et al. (2000), raising the ecological trap hypothesis, suggested the possibility that tuna could be trapped in DFADs even when environmental conditions were not biologically optimal, which may affect natural migration routes of tunas and potentially their biology if habited in poor feeding conditions. Future studies should analyze the comparison of preferential/non-preferential areas and biomass aggregation/decrease around DFADs, which could inform the effect of DFADs on tuna and non-tuna species movement and habitat, and shed light on the ecological trap hypothesis.
Dataset Features and Statistical Reliance
Large-scale habitat preference predictions, such as those carried out in this study, allow wider and more comprehensive knowledge of species distribution, although their use can result in a certain level of compromise in the analysis. Mapping of critical habitats requires a high level of accuracy, but the problem is that the amount of data available over large areas is often limited or very aggregated in certain regions. Bayesian interpolation and extrapolation are sufficiently reliable for the identification of species distribution for effective decision making in fishery management. The use of B-HSM for habitat identification is founded on a number of predictive evaluation criteria that prove a reasonable predictive performance for this approach and its benefits in terms of ecological interpretation. Fishery-dependent datasets matched, in general with various exceptions due to lack of data in those regions, the predicted presences of the fishery-independent data and Bayesian distribution models with a reasonable level of accuracy, as shown by the TSS and AUC indexes.
The use of monsoon seasons, which are not consistent with seasonal catch and catch rates of the DFAD fishery, coupled with the limited DFAD buoy information in some areas or seasons means that the model does not predict the probability of tuna occurrence in areas or seasons where fishing hotspots usually occur (i.e., Somalia area each year accounting for large amount of DFAD catches and Mozambique area where a seasonal fishery take place during March, April and May). Therefore, the present results and conclusions should be taken with caution due to the limited DFAD buoy data analyzed. Future work should be devoted to apply same approach using data covering the entire Indian Ocean consistently.
The B-HSM used in this study provides a description of the seasonal distribution of tuna and non-tuna species associated to DFADs in the Indian Ocean using large-scale, non-invasive sampling, and identifies the suitable and preferential areas of these species’ groups. However, these results and conclusions should be taken with caution due to the limited data from DFAD buoys analyzed. The vast majority of management measures for marine species set fixed boundaries around mobile species (Hyrenbach et al., 2000; Norse et al., 2005), which is not very useful for species like tuna as they are highly mobile. DFADs attached to echo sounder buoys continuously record and provide information on the DFADs trajectories as well as the biomass of fish aggregated below them, so they may represent powerful tools for the study of pelagic ecosystems in a dynamic way (Moreno et al., 2016a). The approach used in this study could be very useful to help designing spatio-temporal conservation management measures, using near real-time habitat predictions based on acoustic data provided by fishers’ echo-sounders and remote sensing systems. Nevertheless, much work remains to be done, especially related to the improvement of biomass estimation by echo-sounders buoys. Moreover, none of the echo-sounders used at this time have the ability to discriminate fish species and sizes, since these buoys operate with a single frequency. If echo-sounder buoys had the capability to directly identify this information of tunas found at DFADs, these real-time habitat predictions could provide specific management measures for certain species or sizes. Making this possible will require initiatives of data-exchange between fleets and scientific organizations, which allow, either directly or with certain delay, the transmission of echo-sounder buoy data to scientists.
Data Availability Statement
The datasets for this article are not publicly available because they reflect individual fishing strategies of a private fishing vessel company. Requests to access the datasets should be directed to the company by contacting Julen Marques from Echebastar (email@example.com).
BO, MP, HM, GM, LR, and JL designed the research. BO, MP, HM, GM, and JL performed the research. BO and MP analyzed the data. BO, MP, JL, GM, JS, LR, and HM wrote the manuscript.
This study was partly funded by a Ph.D. grant by the AZTI Foundation to BO.
Conflict of Interest
The authors declare that the research was conducted in the absence of any commercial or financial relationships that could be construed as a potential conflict of interest.
We would like to thank Spanish fishing company Echebastar who kindly agreed to provide the acoustic data from their echo-sounder buoys used in the present study. We would also like to thank the reviewers who helped us to improve the first version of the manuscript. Also, we extend our appreciation to Dr. Emma J. Harrison for helping with the written language. This manuscript is contribution No. 974 from AZTI-Tecnalia, Marine Research Division.
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Keywords: Bayesian models, bycatch species, echo-sounder, Fish Aggregating Devices, FADs, INLA, species distribution models, tuna
Citation: Orúe B, Pennino MG, Lopez J, Moreno G, Santiago J, Ramos L and Murua H (2020) Seasonal Distribution of Tuna and Non-tuna Species Associated With Drifting Fish Aggregating Devices (DFADs) in the Western Indian Ocean Using Fishery-Independent Data. Front. Mar. Sci. 7:441. doi: 10.3389/fmars.2020.00441
Received: 13 June 2019; Accepted: 19 May 2020;
Published: 17 June 2020.
Edited by:Xavier Pochon, Cawthron Institute, New Zealand
Reviewed by:Alain Henri Fonteneau, Independent Researcher, Saint Malo, France
John David Filmalter, South African Institute for Aquatic Biodiversity, South Africa
Felipe Galván-Magaña, Centro Interdisciplinario de Ciencias Marinas (IPN), Mexico
Copyright © 2020 Orúe, Pennino, Lopez, Moreno, Santiago, Ramos and Murua. This is an open-access article distributed under the terms of the Creative Commons Attribution License (CC BY). The use, distribution or reproduction in other forums is permitted, provided the original author(s) and the copyright owner(s) are credited and that the original publication in this journal is cited, in accordance with accepted academic practice. No use, distribution or reproduction is permitted which does not comply with these terms.
*Correspondence: Blanca Orúe, firstname.lastname@example.org