# Stacked search for time shifted high energy neutrinos from gamma ray bursts with the Antares neutrino telescope

- 949 Downloads
- 2 Citations

## Abstract

A search for high-energy neutrino emission correlated with gamma-ray bursts outside the electromagnetic prompt-emission time window is presented. Using a stacking approach of the time delays between reported gamma-ray burst alerts and spatially coincident muon-neutrino signatures, data from the Antares neutrino telescope recorded between 2007 and 2012 are analysed. One year of public data from the IceCube detector between 2008 and 2009 have been also investigated. The respective timing profiles are scanned for statistically significant accumulations within 40 days of the Gamma Ray Burst, as expected from Lorentz Invariance Violation effects and some astrophysical models. No significant excess over the expected accidental coincidence rate could be found in either of the two data sets. The average strength of the neutrino signal is found to be fainter than one detectable neutrino signal per hundred gamma-ray bursts in the Antares data at 90% confidence level.

## Keywords

Search Window Neutrino Data Neutrino Telescope Neutrino Emission Accidental Coincidence## 1 Introduction

Gamma-ray bursts (GRBs) are among the most powerful sources in the universe, which makes them suitable candidates for the acceleration of the highest-energy cosmic rays. Unambiguous evidence for the acceleration of hadrons in astrophysical environments can be provided by the detection of neutrinos that would be coincidently produced when accelerated protons interact with the ambient photon field (see, e.g. [1, 2, 3] and references therein). Searches for the emission of neutrinos from GRBs have been performed by a variety of experiments, for instance Super-Kamiokande [4], AMANDA [5], Baikal [6], RICE [7], ANITA [8], IceCube [9, 10] and Antares [11, 12]. While covering a wide range of neutrino energies these studies have so far focussed mainly on the time window coincident with the electromagnetic signal of GRBs. Up to now no neutrino signal could be identified by any neutrino detector during the prompt emission phases, and analytical models from [13] based on [2] have already been excluded by the IceCube collaboration [10]. There has also been some effort to successively extend the search time windows in the IceCube data from [−1 h, \(+\)3 h] up to \({\pm } 1\) day [9, 10], and up to \({\pm } 15\) days [14], to account for prolonged neutrino emission. However none of these searches could bring compelling evidence for a GRB signal, since all detected events have been identified with cosmic-ray induced air showers or were of low significance because of the large time windows.

While the search for a signal of neutrinos coincident with the emission of high-energy photons is the most common ansatz, there are many models that predict time-shifted neutrino signals, such as neutrino precursors [15], afterglows (e.g. [16]), or different Lorentz Invariance Violation (LIV) effects for photons and neutrinos on their way to Earth [17, 18]. For instance, the possibility that three low significance neutrino-like events found in the IceCube data [10] could have been produced by GRBs but arrived before the photon signal due to LIV effects is discussed in [19]. Probing such scenarios requires a new approach to the search for correlated emission. Moreover, in all aforementioned scenarios, the neutrino signal is simply shifted in time with respect to the electromagnetic signal, and none of these models predict any considerably prolonged neutrino emission. Hence the approach used in this paper and described in Sect. 3 aims at identifying a presumably faint neutrino signal that is shifted with respect to the electromagnetic GRB emission by an unknown time offset, while making no assumption about the origin of such an offset.

## 2 Neutrino candidates and GRB sample

Neutrino telescopes are arrays of photomultipliers deployed in a very large volume of transparent medium like Antarctic ice or deep-sea water. They detect the Cherenkov light generated by the products of the interaction of a high-energy neutrino in the vicinity of the detector. The direction of the impinging neutrino is reconstructed using the timing of signals from photomultipliers, while the detected amount of light gives an estimate of the neutrino energy. The Antares telescope [20] is located at a depth of \(2475~{\mathrm {m}}\) in the French Mediterranean Sea off the coast of Toulon, at \(42^{\circ }48'\)N, \(6^{\circ }10'\)E. It comprises 885 optical modules housing \(10''\) photomultipliers in \(17''\) glass spheres installed on 12 strings, representing an instrumented volume of \(0.02~\hbox {km}^3\).

The following analysis focuses on the detection of muon trajectories from below the horizon, which are produced by muon-neutrino charged-current interactions. This channel provides significantly better directional reconstruction than neutral-current interactions and charged current interactions from the other neutrino flavors. In this channel, Antares is the most sensitive detector for sources in a large part of the southern sky up to a few 100 TeV [21].

The sample of Antares events used in this analysis consists of 5516 neutrino candidates selected from data collected between March 2007 and the end of 2012 [22]. From Monte Carlo simulations the angular resolution, defined as the median of the space angle \(\delta _\mathrm{err}\) between the true and reconstructed direction of neutrinos for an \(E^{-2}\) differential spectrum, is \(0.38^{\circ } \), with a contamination from atmospheric muons of \(10\%\). The right-ascension distribution of the neutrino candidates is shown in Fig. 1.

*Swift*[23] and

*Fermi*satellites [24, 25], and supplemented by a table from the IceCube Collaboration

^{1}[26], with information parsed from the GRB Coordinates Network (GCN) notices. Since only the time and position information (and the measured redshift, if available) of each announced GRB was used, no further selection on e.g. the quality of the spectral measurements was required, leading to 1488 GRBs. Only GRB alerts were taken into account that occurred both below the horizon of the neutrino telescope and during the covered neutrino data collection period. The upper panel of Fig. 2 shows the distribution of the selected neutrino candidates, which are homogeneously distributed in time. The lower panel displays the accordingly selected GRBs in equatorial coordinates and their measured fluence.

## 3 Principle of the search

Neutrino signatures are searched-for in an angular cone around the direction of, and within a maximum time offset from the time of each GRB. For any such space and time coincidence, the time difference with respect to the GRB alert is recorded. In order to avoid any boundary effect such as an artificial asymmetry of neutrino candidates around a GRB alert close to the beginning or end of neutrino telescope data taking, GRBs detected during a period of half the considered maximum time offset at the beginning and end of the neutrino data sample are excluded. The collected time differences are stacked in a common timing profile. In the case of no signal, only purely accidental spatial coincidences of the neutrino candidates with the defined search cones around the GRB positions would be expected. The observed time shifts should then be distributed randomly, yielding a flat stacked distribution where all shifts are equally likely. Any neutrino emission associated with the GRBs, even if faint, can give rise to a cumulative effect in these stacked profiles, which can then be identified by its discrepancy from the background hypothesis. An optimal choice of the search cone size \(\delta _\mathrm{max}\) naturally depends on the GRB’s position accuracy and the neutrino direction reconstruction uncertainty. The size of the probed time window \(\tau _\mathrm{max}\) should be defined as the largest shift predicted by any of the models under consideration. Such a procedure had already been proposed [27], where windows of \(\pm 1\, \mathrm {h} \) around the GRB satellite triggers under study were considered. The approach presented in the following is extended to allow significantly larger time windows and different origins of the time shift. This method is intrinsically different from those previously developed by the IceCube Collaboration [10, 14], which focused on successively widening symmetric search time windows around the GRB alerts considering a flat temporal signal probability density function. In the case of a time-shifted signal, these methods suffer from reduced significance due to the accumulated background in the increasingly large time windows. In contrast, the technique presented here aims at identifying a time-shifted signal as a peak on top of flat background.

### 3.1 Potential physical delays considered

*z*of the GRB as:

*E*and its momentum

*p*is modified by an additional term proportional to an integer power of the ratio of the energy to the Planck scale:

*D*(

*z*) and the energy scale \(M_\mathrm{LIV}\):

*D*(

*z*) is the effective distance travelled by the particles taking into account the expansion of the Universe, and is defined according to [19] as:

*z*is the redshift, \(H_0\) is the Hubble constant, and \(\Omega _m\) and \(\Omega _\Lambda \) are the relative matter and dark energy densities of the Universe [29]. These effects are expected to appear in a stacked histogram that accounts for both the estimated neutrino energy \(E_\mathrm{est}\) and the distance of the source. Consequently, the variable to be probed is defined as:

The ratio \(r= n_+ / n_-\) of spatially coincident events before and after the respective GRB alert is a very simple measure to probe the distributions while making the fewest assumptions on any model. Any effect leading to different arrival times of neutrinos and gamma-rays from GRBs is expected to yield either positive or negative time shifts. This ratio is calculated if both \(n_+\) and \(n_-\) are non-zero.

Consequently, in the search for an associated neutrino signal from GRBs, three stacked time profiles for the measures \(\tau \), \(\tau _\mathrm{z}\) and \(\tau _\mathrm{LIV}\) were generated for all neutrino candidates which matched the coordinates of a reported GRB alert, and the ratio *r* for the whole sample was computed.

## 4 Implementation of the method and application to Antares 2007–2012 data

The expected number of background events \(\mu _b\) increases with the solid angle of the search cones \(\Omega (\delta _\mathrm{max})\) around each GRB’s position and with the considered maximum time delay \(\tau _\mathrm{max}\). Hence, the choice of the search cone size and the probed time window should be optimised under reasonable physical considerations.

### 4.1 Search cone

The determination of an optimally-sized search cone for spatially coincident neutrino candidates with a GRB alert was based on the maximisation of the ratio of signal to square root of background. Assuming a point-source-like signal at the GRB’s location, the reconstructed neutrino directions approximately follow a two-dimensional Gaussian profile of standard deviation \(\sigma _{\nu }\) around this position. This approach yields an optimum search cone size of \(1.58 \cdot \sigma _{\nu }\) as derived for example in [30]. Note that the neutrino telescope resolution is usually stated as the median of the reconstructed direction error \(m(\delta _\mathrm{err})\) (see for instance [31]). For angles in consideration here, the relation \(m(\delta _\mathrm{err})\sim 1.17 \sigma _{\nu }\) holds.

The effects of uncertainty in GRB location \(\mathrm {\Delta _\mathrm{err}}\) (sub-arc second for *Swift*/UVOT or ground based telescopes, up to several degrees for *Fermi*/GBM) is accounted for by extending the search window whenever \(\mathrm {\Delta _\mathrm{err}} > \sigma _{\nu }\). As the contribution of random coincidences scales quadratically with \(\Delta _\mathrm{err}\), the background in the cumulative profile might be dominated considerably by a few bursts with very large satellite error boxes. Consequently, a reasonable trade-off should be found. On the one hand, the statistics should not be reduced too much by excluding a large number of badly-localised bursts. On the other hand, the stacked timing profiles should not be dominated by one burst with a large error box, which naturally leads to many accidental spatial coincidences. In order to limit this effect without significantly reducing the data sample, a maximum search-cone size was chosen – based on the distribution of \(\mathrm {\Delta _\mathrm{err}^\mathrm{max}}\) shown in Fig. 3 – such that no GRB contributed more than an order of magnitude more of uncorrelated background than any other.

### 4.2 Maximum time delay

The approach presented in this paper aims at being as model independent as possible. The maximum time shift anticipated from the astrophysical processes mentioned in Sect. 3.1 is used to set the time coincidence window. Intrinsic shifts in the emission times of neutrinos were predicted in [15] with neutrinos \({\sim } 100 \, \mathrm {s} \) before the electromagnetic GRB signal. A precursor neutrino signal that might be emitted even tens of years before the actual GRB is derived in [32]. Since the latter time scale exceeds the operational times of the current neutrino telescopes, we will omit this scenario. Early afterglow emission of neutrinos \({\sim } 10\, \mathrm {s} \) after the burst are predicted in [16, 33] and extended neutrino fluxes up to 1 day after the prompt emission are derived in [34]. These intrinsic time shifts between neutrino and photon signals are still well within the time scopes that have already been probed, for example in [10, 14] – without positive result.

Differences in arrival times induced by LIV effects would depend not only on \(M_{LIV}\), but also on the energy of the particles and the distance of the source. However, a maximum expected time shift of neutrinos and photons can be inferred from Eq. 3 using the existing limit on the LIV energy scale. The most stringent limit within the theoretical framework used here has been set to \(M_{\mathrm{LIV}} = 7.6 \cdot M_\mathrm{Planck}\) based on the *Fermi*/LAT data [35]. Using the distance *D*(*z*) at a redshift of \(z=8.5\), which is the highest measured redshift in the selected GRB catalog, and a maximum energy of \({\sim } E_\mathrm{max}=10^9\, \mathrm {GeV} \) accounting for the energy range at which a signal might be observed, a maximum time shift of \(\tau _\mathrm{max} = 40\) days was derived. Even though the upper bound was derived from quantum space-time models, the search itself remains model independent.

A discretisation of the cumulative timing profiles into 150 bins was chosen, which allows time scales down to 13 h to be probed. Given the low number of expected coincidences within the allowed time window (see Sect. 4.5), this choice ensures that there will be much less coincidences than bins, leading to a quasi-unbinned approach [28].

### 4.3 Final GRB sample

Having chosen the maximal search time window and the largest angular search cone that should be taken into account, the final samples associated with the neutrino telescope data set were determined. The initially selected GRB catalog comprised 1488 bursts that had occurred between 2007 to 2012, which gives a detection rate of 0.68 bursts per day. Out of these, 563 have been selected for the search of associated neutrinos in the Antares data using the criteria outlined above, of which 150 have a measured redshift *z*.

### 4.4 Statistical tests

From the stacked histograms of \(\tau \), \(\tau _z\) and \(\tau _\mathrm{LIV}\), test statistics are calculated that distinguish a systematically time-shifted neutrino signal associated with GRBs from the background-only hypothesis of purely accidental coincidences. A large number of background realisations preserving the telescope’s acceptance are generated from the existing data sets by scrambling the time from the corresponding distribution of Fig. 1 and randomising the right ascension of detected neutrino candidate events in accordance with the flatness of the data distribution. The significance, of an excess in the data is then given by the *p*-value which is the probability to measure the test statistic in question (or more extreme values) from the background-only distribution.

*r*will be the variable itself. For the stacked histograms, the Bayesian observable \(\psi \) to estimate the compatibility of a given stacked (and binned) time profile with the expectations from background has been proposed in [27, 28]. This test statistic is proportional to the logarithm of the probability

*p*of an observation

*D*under an hypothesis

*H*defined by a set of information

*I*(here that the stacked profile bins are filled following a multinomial law of known probabilities):

*n*events in the histogram in total, distributed in \(k \in [1 \dots m]\) bins. The probability to fall within bin

*k*is \(p_k\); for a uniform background distribution (i.e. in the case of the \(\tau \) profile), \(p_k = 1/m\) is simply given by the total number of bins

*m*. For the non-uniform profiles \(\tau _\mathrm{z}\) and \(\tau _\mathrm{LIV}\), these probabilities have to be determined by a large number of pseudo-experiments simulating the background, of the order of \(10^{7}\) to estimate the significance of a potential excess up to the \(5\sigma \) level. The value of \(\psi \) is calculated for each of the \(\tau \), \(\tau _z\) and \(\tau _\mathrm{LIV}\) profiles, correspondingly denoted \(\psi \), \(\psi _\mathrm{z}\) and \(\psi _\mathrm{LIV}\).

### 4.5 Sensitivity

Around \(1.4\times 10^{7}\) pseudo experiments yielding sky-maps of uncorrelated neutrino events were generated to simulate the case of purely accidental coincidences (background-only) between the Antares neutrino data and the GRB catalogue. On average, 3.9 of the neutrino candidates are expected to match the bursts’ search windows in time and space, with 0.7 of them coinciding accidentally with the bursts with measured redshift.

To illustrate the performance of the proposed technique to identify hypothetical neutrinos from GRBs, a test signal was generated by associating neutrino candidates artificially with a fraction of the GRBs at a hypothetical intrinsic time shift of \(t_\mathrm{in}\) with \(t_\mathrm{in}=1,~5,~10~\mathrm{or~}20\) days. That is, taking into account the cosmological redshift *z*, a simulated signal delayed by \(t_\nu = t_\mathrm{GRB} + t_\mathrm{in} \cdot (1+z)\). Its strength was quantified by the probability \(f \in [0,1]\) that a GRB produced a signal in the neutrino telescope. The signal was consequently only simulated for those bursts for which the redshift could be determined, and the variable which has the best sensitivity to it will be \(\tau _\mathrm{z}\) since signal will accumulate in one bin.

*r*, \(\psi \), \(\psi _\mathrm{z}\) or \(\psi _\mathrm{LIV}\)) above a threshold corresponding to a p-value at the \(n\sigma \) level on the background-only realisations. It represents the efficiency of the analysis and the specific test statistic to identify a signal being associated with a fraction of GRBs. The detection efficiency of the \(\psi _\mathrm{z}\) test statistic is independent of the time shift of signal for delays up to 10 days, as can be seen in Fig. 4. The evolution of the efficiencies for an example signal at an intrinsic time shift of 5 days as a function of the signal strength

*f*is shown in Fig. 5, and is hence representative of shifts from 0 to 10 days. Signal strength corresponding to discovery probabilities are summarized in Table 1, for the whole sample and for GRBs with measured redshift. For instance, using the \(\psi \) test statistics, if only \(f=1.3\%\) of the GRBs would give rise to an associated signal neutrino, it would produce an excess of \(3\sigma \) significance with \(50\%\) probability, whereas a stronger signal in \(2.4\%\) of the bursts would be identified at the \(5\sigma \) level. For the sample of GRBs with measured redshift, the \(\psi _\mathrm{z}\) test statistic only needs a fraction \(f_z=4.5\%\) which is half of the signal fraction necessary with the \(\psi \) test statistic for the same detection efficiency.

Sensitivities at 90% and 99% confidence level and detection probabilities at \(3\sigma \) and \(5\sigma \) with 50% statistical power for a signal delayed by 5 days at the source (see text) for the different test statistics expressed in terms of the fraction \(f_\mathrm{all}\) of the GRB sample with detectable signal and the fraction \(f_z\) of the GRB sample with measured redshift \(f_z\)

Test statistic | Sensitivity at 90% CL | Sensitivity at 99% CL | \(\mathcal {MDP}\) \(3\sigma \) | \(\mathcal {MDP}\) \(5\sigma \) | ||||
---|---|---|---|---|---|---|---|---|

\(f_\mathrm{all}\) (%) | \(f_z\) (%) | \(f_\mathrm{all}\) (%) | \(f_z\) (%) | \(f_\mathrm{all}\) (%) | \(f_z\) (%) | \(f_\mathrm{all}\) (%) | \(f_z\) (%) | |

| 0.8 | 3.0 | 1.5 | 5.5 | 2.4 | 9.0 | 4.5 | 17 |

\(\psi \) | 0.6 | 2.2 | 1.3 | 5.0 | 1.3 | 5.0 | 2.4 | 9.0 |

\(\psi _\mathrm{z}\) | 0.3 | 1.1 | 0.8 | 3.0 | 0.6 | 2.3 | 1.2 | 4.5 |

\(\psi _\mathrm{LIV}\) | 0.3 | 1.1 | 0.8 | 3.0 | 1.5 | 5.5 | 3.0 | 12.5 |

The introduced time-stacking technique is consequently capable of robustly finding at the \(3\sigma \) level an intrinsically delayed neutrino emission from GRBs as long as it is associated with at least 3 of the 563 bursts.

Probabilities *P* to yield values of the test statistic \(Q \in [\psi , \psi _\mathrm{z}, \psi _\mathrm{LIV} ]\) above the measurement \(Q_\mathrm{meas}\) and above the median value *m*(*Q*) as expected from pure background realisations for different fractions \(f_\mathrm{all}\) (\(f_z\)) of all GRBs (with measured redshift *z*) with one associated signal neutrino intrinsically shifter by 5 days at the source

\(f_\mathrm{all}\) (%) | \(P({>}\psi _\mathrm{meas})\) | \(P({>}m(\psi ))\) | \(f_z\) | \(P({>} \psi _\mathrm{z, meas})\) | \(P({>}m(\psi _\mathrm{z}))\) | \(P({>}\psi _\mathrm{LIV, meas})\) | \(P({>}m(\psi _\mathrm{LIV}))\) |
---|---|---|---|---|---|---|---|

\(\psi _\mathrm{meas} =0\) (%) | \(m(\psi )=73.3\) (%) | (all | \(\psi _\mathrm{z, meas} =0\) (%) | \(m(\psi _\mathrm{z})=0\) (%) | \(\psi _\mathrm{LIV, meas} =0\) (%) | \(m(\psi _\mathrm{LIV})=0\) (%) | |

0.0 | 98 | 50 | 0.0 | 48.5 | 48.5 | 48.2 | 48.2 |

0.04 | 99 | 54 | 0.15 | 59 | 59 | 59 | 59 |

0.29 | 99 | 75 | 1.1 | 90 | 90 | 90 | 90 |

0.60 | 100 | 90 | 2.3 | 98 | 98 | 98 | 98 |

0.69 | 100 | 93 | 2.6 | 99 | 99 | 99 | 99 |

1.07 | 100 | 98 | 4.0 | 100 | 100 | 100 | 100 |

1.33 | 100 | 99 | 5.0 | 100 | 100 | 100 | 100 |

2.10 | 100 | 100 | 8.0 | 100 | 100 | 100 | 100 |

## 5 Results and discussion

The data collected by the Antares telescope from the years 2007 to 2012 were analysed to search for neutrinos within the predefined angular and timing search windows associated with the GRB catalogue. None of the neutrino candidates in the data matched these search windows, where 3.9 would have been expected from background (0.7 coincidences were expected for the GRBs with measured redshift *z*). The measured values of the test statistics are thus zero, and the ratio \(r=n_+/n_-\) is undefined. The probability to observe no events coinciding with all GRBs is relatively small, with \(P(0 | 3.9)=1.2\%\) (and \(51.4\%\) for GRBs with measured *z*).

We verified the under-fluctuation to be of statistical origin instead of intrinsic systematic effects in the search methodology or the software. In particular, we derived the number of coincidences when increasing independently \(\tau _{max}\) and \(\delta _{max}\). Using these enlarged coincidence windows, the number of coincident data events is close to the expected number of coincidences from randomized data.

*P*to measure test statistics above the measurements and the expected values from the median background realisations are given. This results in \(99\%\) CL limits of \(f_{all}=0.04\%\) and \(f_z=2.6\%\), and a \(90\%\) CL upper limit on \(f_z\) of \(1.1\%\). With the aforementioned under-fluctuation, the setting of a \(90\%\) CL limit on \(f_\mathrm{all}\) defined according to Sect. 4.5 is not possible. A conservative option would be to set the limit equal to the sensitivity as in [36]. Since this method does not make use of the information contained in the actual nonobservation, the resulting \(90\%\) CL of \(f_{all}=0.6\%\) is weaker than the standard \(99\%\) CL of \(0.04\%\), so the value of \(0.04\%\) should be used for both \(90\%\) and \(99\%\) CL.

Total live-time of the considered neutrino telescope data sets \(\tau _\mathrm{tot}\), respective number of neutrino candidate events \(N_\mathrm{events}\) and respective median angular resolution \(m(\delta )\). Samples of \(N_\mathrm{GRB}\) GRBs are identified (out of which \(N_{\mathrm{GRB} ,z} \) have measured redshifts) for the search of correlations. Assuming totally uncorrelated neutrino data, the mean numbers of coincident events that would be expected within the GRB’s search windows \(n_\mathrm{coinc}\) are also given

\(\nu \) Data sample | \(\tau _\mathrm{tot}\) | \(N_\mathrm{events}\) | \(m(\delta )\) | \(\delta _\mathrm{max} \) | \(\tau _\mathrm{max}\) | \(N_\mathrm{GRB}\) | \(N_{\mathrm{GRB},z} \) | (Uncorrelated) | |
---|---|---|---|---|---|---|---|---|---|

[d] | [\(^{\circ }\) ] | [\(^{\circ }\) ] | [d] | \(n_\mathrm{coinc}\) | \(n_{\mathrm{coinc}, z}\) | ||||

Antares (07-12) | 2154 | 5516 | 0.38 | 0.51–1.59 | 40 | 563 | 150 | 3.9 | 0.7 |

IC40 (08-09) | 408 | 12876 | 0.70 | 0.95–2.99 | 40 | 60 | 12 | 35.0 | 4.0 |

Mean and median values of the different test statistics used in this analysis as derived in the pseudo experiments of background and in the measurement using the neutrino candidates as selected in the Antares data from 2007 to 2012 and IceCube data from the IC40-period from April 2008 to May 2009. The number of data events coinciding spatially with the respective GRB samples \(n_\mathrm{coinc}\) are also given. The probabilities \(P({>}\mathrm{meas})\) and the *p*-value, \(P({\ge } \mathrm{meas})\) give the fraction of background-only pseudo experiments that yield test statistics above and at and above the measurement. Being 10 times the logarithm of two definite positive quantities, the \(\psi \) type test statistics are usually expressed in dB [28]. Note that since there are no coincidences in the Antares data sample, *r* is not defined

ANTARES 07-12 | IceCube IC40 08-09 | |||||||||||
---|---|---|---|---|---|---|---|---|---|---|---|---|

All GRBs | GRBs w/ | All GRBs | GRBs w/ | |||||||||

\(n_\mathrm{coinc}\) | \(\psi \) | \(n_\mathrm{coinc}\) | \(\psi _\mathrm{z}\) | \(\psi _\mathrm{LIV}\) | \(n_\mathrm{coinc}\) | | \(\psi \) | \(n_\mathrm{coinc}\) | \(\psi _\mathrm{z}\) | \(\psi _\mathrm{LIV}\) | ||

(dB) | (dB) | (dB) | (dB) | (dB) | (dB) | |||||||

Bgd mean | 4.4 | 77.4 | 0.7 | 11.9 | 4.5 | 1.1 | 35.0 | 371.3 | 4.0 | 56.6 | 10.4 | |

Bgd median | 4 | 73.3 | 0 | 0 | 0 | 35 | 1.0 | 371.8 | 4 | 56.3 | 7.9 | |

Measurement | 0 | 0 | 0 | 0 | 0 | 42 | 0.4 | 416.0 | 8 | 1.1 | 93.9 | 8.8 |

\(P({>}\mathrm{meas.})\) | 98.8% | 98.8% | 48% | 48.6% | 48.6% | 10.4% | 0.4 | 14.0% | 2.1% | 6.1% | 45.1% | |

\(P({\ge } \mathrm{meas.})\) | 100% | 100% | 100% | 100% | 100% | 13.5% | 14.0% | 5.1% | 6.1% | 45.1% |

We can state a sensitivity of \(m(f_\mathrm{all}^{90\% \mathrm{CL}})= 0.6\%\) of all GRBs (\(2.2\%\) for those with measured *z*), which is the median upper limit on the fraction of bursts that contain a signal of the form \(\tau _\mathrm{s}=5\, \mathrm {d} \cdot (1+z)\). Furthermore, we see that \(99\%\) of all realisations with a signal fraction \(f_{\mathrm{all}} = 0.04\%\) would yield higher \(\psi \) than observed, so we can exclude such a signal with \(99\%\) confidence. Regarding the sample of bursts with measured redshift *z*, the observation of zero events matched the median expectation from background, so we could exclude that \(1.1\%\) of them produced a signal neutrino with a delay shape \(\tau _\mathrm{s}=5\, \mathrm {d} \cdot (1+z)\) with \(90\%\) confidence, in accordance with the sensitivity that had previously been derived.

### 5.1 Application to the IceCube IC40 data sample

The same parameter optimisation and search has been performed with the public data sample^{2} from an analysis searching for neutrino pointlike sources [37] of the IceCube observatory in its 40-string configuration. These data cover April 2008 to May 2009 and comprise 12877 neutrino candidates. The selection procedure of neutrinos and GRBs is the same as in Sect. 4. With a resolution of \(0.7^{\circ } \) [38] it leads to 60 GRBs (respectively 12 with measured *z*) 35 of which are expected to be in coincidence with neutrinos (respectively 4). The different parameters summarising the Antares and IceCube samples, including the number of coincident events \(n_\mathrm{coinc}\) that would be expected if the neutrino data was completely uncorrelated with the chosen GRBs (i.e., the background-only hypothesis) are given in Table 3.

The IceCube GRB sample shows significantly lower statistics, due to the fact that the published data spans only around one year compared to almost six years in the Antares sample. In addition, because of the location of the detectors on Earth, \(87\%\) of the sky is visible for the Antares detector with unequal coverage, whilst the IceCube experiment covers the northern sky but at all times. It is also worth noting that, due to the larger instrumented volume of the detector, the IceCube data set contains more neutrino candidates than the Antares one, while covering a smaller time period in which less GRB alerts were recorded. Both samples therefore explore different statistical regimes. In the end, 42 of the neutrino candidates fall within the search windows, with 8 for the bursts with measured *z*. This is a slight fluctuation above the expectations from background, with *p*-values of 13.5% (whole sample) and 5.1% (GRBs with measured redshift), yielding excesses of moderate 1.5\(\sigma \) and 1.9\(\sigma \) significances, respectively. The observation is compatible with no correlation of the IceCube data with the chosen GRB sample. Moreover, the timing profiles show no indication for any preferred time delay. The measured and expected values as well as the corresponding significance of the different test statistics for the two studied samples, are summarised in Table 4.

## 6 Conclusion

A powerful method has been presented to identify a neutrino signal associated with GRBs if it is shifted in time with respect to the photon signal. The signal is distinguished from randomly distributed data as a cumulative effect in stacked timing profiles of spatially coincident neutrinos in the data from the Antares and IceCube neutrino telescopes.

Estimating the behaviour of the search for a large number of simulated measurements using randomised sky maps of the neutrino events, and comparing these with the actual neutrino telescope data, significances of the observations were derived. Using data from the Antares neutrino telescope between the years 2007 and 2012, a deficit of spatially coincident neutrinos with the selected gamma-ray-burst catalogue was reported, with \(98.8\%\) of the randomised data leading to more coincidences between the neutrino data and the GRBs. The application of the method to the public IceCube data in its 40 line configuration gives results compatible with the expectation from background.

The presented approach could have identified an intrinsically time-shifted signal even if only of the order of one in a hundred GRBs would have given rise to a single associated neutrino in the Antares data. This is above the detectable neutrino signal predicted by the NeuCosmA model [39] that is on average only of the order of \({\sim } 2\times 10^{-4}\) in the Antares detector, and only the strongest individual burst yields a neutrino detection rate exceeding 0.01 [12].

In conclusion, novel analysis techniques have been developed that increase the sensitivity of existing neutrino searches from GRBs to models of delayed neutrino emission and Lorentz Invariance Violation. They allow extending the search for neutrinos from GRBs with time displacements of up to 40 days. It confirms the absence of a significant neutrino signal being associated with GRBs that has so far been measured in the simultaneous time windows.

## Footnotes

- 1.
Available on-line at http://grbweb.icecube.wisc.edu/.

- 2.
IceCube IC40 neutrino candidates are available at http://icecube.wisc.edu/science/data/ic40/.

## Notes

### Acknowledgements

The authors acknowledge the financial support of the funding agencies: Centre National de la Recherche Scientifique (CNRS), Commissariat à l’énergie atomique et aux énergies alternatives (CEA), Commission Européenne (FEDER fund and Marie Curie Program), Institut Universitaire de France (IUF), IdEx program and UnivEarthS Labex program at Sorbonne Paris Cité (ANR-10-LABX-0023 and ANR-11-IDEX-0005-02), Labex OCEVU (ANR-11-LABX-0060) and the A*MIDEX project (ANR-11-IDEX-0001-02), Région Île-de-France (DIM-ACAV), Région Alsace (contrat CPER), Région Provence-Alpes-Côte d’Azur, Département du Var and Ville de La Seyne-sur-Mer, France; Bundesministerium für Bildung und Forschung (BMBF), Germany; Istituto Nazionale di Fisica Nucleare (INFN), Italy; Stichting voor Fundamenteel Onderzoek der Materie (FOM), Nederlandse organisatie voor Wetenschappelijk Onderzoek (NWO), The Netherlands; Council of the President of the Russian Federation for young scientists and leading scientific schools supporting grants, Russia; National Authority for Scientific Research (ANCS), Romania; Ministerio de Economía y Competitividad (MINECO): Plan Estatal de Investigación (refs. FPA2015-65150-C3-1-P, -2-P and -3-P, (MINECO/FEDER)), Severo Ochoa Centre of Excellence and MultiDark Consolider (MINECO), and Prometeo and Grisolía programs (Generalitat Valenciana), Spain; Agence de l’Oriental and CNRST, Morocco. We also acknowledge the technical support of Ifremer, AIM and Foselev Marine for the sea operation and the CC-IN2P3 for the computing facilities.

## References

- 1.E. Waxman, Phys. Rev. Lett.
**75**, 386 (1995)ADSCrossRefGoogle Scholar - 2.E. Waxman, J. Bahcall, Phys. Rev. Lett.
**78**, 2292 (1997)ADSCrossRefGoogle Scholar - 3.E. Waxman, Astrophys. J. Suppl.
**127**, 519 (2000)ADSCrossRefGoogle Scholar - 4.S. Fukuda et al., Astrophys. J.
**578**(1), 317 (2002)ADSCrossRefGoogle Scholar - 5.A. Achterberg et al., Astrophys. J.
**674**(1), 357 (2008)ADSCrossRefGoogle Scholar - 6.A.V. Avrorin et al., Astron. Lett.
**37**(10), 692 (2011)Google Scholar - 7.D. Besson et al., Astropart. Phys.
**26**(6), 367 (2007)ADSCrossRefGoogle Scholar - 8.A.G. Vieregg et al., Astrophys. J.
**736**(1), 50 (2011)ADSCrossRefGoogle Scholar - 9.R. Abbasi et al., Astrophys. J.
**710**, 346 (2010)ADSCrossRefGoogle Scholar - 10.R. Abbasi, Nature
**484**, 351 (2012)ADSCrossRefGoogle Scholar - 11.S. Adrián-Martínez, JCAP
**03**, 006 (2013)ADSGoogle Scholar - 12.S. Adrián-Martínez, A&A
**559**, A9 (2013)ADSCrossRefGoogle Scholar - 13.D. Guetta, Astropart. Phys.
**20**, 429 (2004)ADSCrossRefGoogle Scholar - 14.J. Casey for the IceCube Collaboration, in
*Proceedings of the 33rd ICRC*, ed. by IUPAP (2013)Google Scholar - 15.S. Razzaque, Phys. Rev. D
**68**(8), 083001 (2003)ADSCrossRefGoogle Scholar - 16.E. Waxman, J.N. Bahcall, Astrophys. J.
**541**, 707 (2000)ADSCrossRefGoogle Scholar - 17.G. Amelino-Camelia, L. Smolin, Phys. Rev. D
**80**(8), 084017 (2009)ADSCrossRefGoogle Scholar - 18.U. Jacob, T. Piran, Nat. Phys.
**3**, 87 (2007)CrossRefGoogle Scholar - 19.G. Amelino-Camelia et al., Astrophys. J.
**806**(2), 269 (2015)ADSCrossRefGoogle Scholar - 20.M. Ageron, Nucl. Instrum. Methods A
**656**, 11 (2011)ADSCrossRefGoogle Scholar - 21.S. Adrian-Martinez et al. (ANTARES and IceCube Collaborations), Astrophys. J.
**823**(1), 65 (2016)Google Scholar - 22.S. Adrian-Martinez, Astrophys. J.
**786**, L5 (2014)ADSCrossRefGoogle Scholar - 23.N. Gehrels, Astrophys. J.
**611**, 1005 (2004)ADSCrossRefGoogle Scholar - 24.W.B. Atwood, Astrophys. J.
**697**, 1071 (2009)ADSCrossRefGoogle Scholar - 25.C. Meegan, Astrophys. J.
**702**, 791 (2009)ADSCrossRefGoogle Scholar - 26.J.A. Aguilar, for the IceCube Collaboration, in
*Proceedings of the 33rd ICRC*, ed. by IUPAP (2013)Google Scholar - 27.N. van Eijndhoven, Astropart. Phys.
**28**, 540 (2008)ADSCrossRefGoogle Scholar - 28.D. Bose, Astropart. Phys.
**50**, 57 (2013)ADSCrossRefGoogle Scholar - 29.K.A. Olive et al. (Particle Data Group), Review of particle physics. Chin. Phys. C
**38**, 090001 (2014)Google Scholar - 30.D.E. Alexandreas, Nucl. Instrum. Methods A
**328**, 570 (1993)ADSCrossRefGoogle Scholar - 31.S. Adrian-Martinez et al. Astrophys. J.
**760**, 53 (2012)Google Scholar - 32.J. Granot, D. Guetta, Phys. Rev. Lett.
**90**(19), 191102 (2003)ADSCrossRefGoogle Scholar - 33.K. Murase, Phys. Rev. D
**76**(12), 123001 (2007)ADSCrossRefGoogle Scholar - 34.S. Razzaque, Phys. Rev. D
**88**(10), 103003 (2013)ADSCrossRefGoogle Scholar - 35.V. Vasileiou, Phys. Rev. D
**87**(12), 122001 (2013)ADSCrossRefGoogle Scholar - 36.M.G. Aartsen, Astrophys. J.
**779**, 132 (2013)Google Scholar - 37.R. Abbasi, Phys. Rev. D
**84**, 082001 (2011)ADSCrossRefGoogle Scholar - 38.A. Karle for the IceCube Collaboration, in
*Proceedings of the 31rst ICRC*, ed. by M. Giller, J. Szabelski (2009)Google Scholar - 39.S. Hümmer, M. Rüger, F. Spanier, W. Winter, Astrophys. J.
**721**, 630 (2010)ADSCrossRefGoogle Scholar

## Copyright information

**Open Access**This article is distributed under the terms of the Creative Commons Attribution 4.0 International License (http://creativecommons.org/licenses/by/4.0/), which permits unrestricted use, distribution, and reproduction in any medium, provided you give appropriate credit to the original author(s) and the source, provide a link to the Creative Commons license, and indicate if changes were made.

Funded by SCOAP^{3}