'Every number is guilty unless proven innocent.
(Rao, 1997: 152)
Event studies are oftentimes the first step in a sequence of analyses that aims at identifying the determinants of stock market responses to distinct event types. Event studies yield as an outcome abnormal returns (ARs), which are cumulated over time to cumulative abnormal returns (CARs) and then 'averaged'  in the case of so called sample studies  over several observations of identical events to AARs and CAARs  where the second 'A' stands for 'average'. These event study results are then oftentimes used as dependent variables in regression analyses.
\begin{equation}H_0: μ = 0 \end{equation}
\begin{equation}H_1: μ \neq 0 \end{equation}
Event studies may imply a hierarchy of calculations, with ARs being compounded to CARs, which can again be 'averaged' to CAAR in crosssectional studies (sometimes also called 'sample studies'). In longrun Event Studies instead of CAR the BuyandHold abnormal return (BHAR) is widely use. BHAR can alos be 'averaged' to ABHAR in crosssectional studies. There is a need for significance testing at each of these levels. μ in the above mentioned equations may thus represent ARs, CARs, BHARs, AARs, CAARs, and ABHARs. Let's shortly revisit these six different forms of abnormal return calculations, as presented in the introduction and longrun eventstudies:
\begin{equation}AR_{i,t}=R_{i,t}E[R_{i,t}\Omega_{i,t}] \end{equation}
\begin{equation}AAR_{t}= \frac{1}{N} \sum\limits_{i=1}^{N}AR_{i,t} \end{equation}
\begin{equation}CAR_{i}=\sum\limits_{t=T_1 + 1}^{T_2} AR_{i,t} \end{equation}
\begin{equation}BHAR_{i}=\prod\limits_{t=T_1 + 1}^{T_2} (1 + R_{i,t})  \prod\limits_{t=T_1 + 1}^{T_2} (1 + E[R_{i,t}\Omega_{i,t}])\end{equation}
\begin{equation}CAAR=\frac{1}{N}\sum\limits_{i=1}^{N}CAR_i\end{equation}
\begin{equation}ABHAR=\frac{1}{N}\sum\limits_{i=1}^{N}BHAR_{i}\end{equation}
For grouped observations, both along the firm or event dimension, we provide a precisionweighted CAAR, which offers a similar standardization as the Patell Test:
\begin{equation}PWCAAR=\sum\limits_{i=1}^{N}\sum\limits_{t=T_1 + 1}^{T_2}\omega_i AR_{i, t}\end{equation}
where $$\omega_i = \frac{\left(\sum\limits_{t=T_1 + 1}^{T_2} S^2_{AR_{i,t}}\right)^{0.5}}{ \sum\limits_{1=1}^{N}\left(\sum\limits_{t=T_1 + 1}^{T2}S^2_{AR_{i,t}}\right)^{0.5}}$$
and $S^2_{AR_{i,t}}$ is the forecasterror corrected standard deviation defined in EQ $\ref{EQ:FESD}$.
The literature on event study test statistics is very rich, as is the range of significance tests. Generally, significance tests can be grouped in parametric and nonparametric tests (NPTs). Parametric tests assume that individual firm's abnormal returns are normally distributed, whereas nonparametric tests do not rely on any such assumptions. In research, scholars commonly complement a parametric test with a nonparametric tests to verify that the research findings are not due to eg. an outlier (see Schipper and Smith (1983) for an example). Table 1 provides an overview and links to the formulas of the different test statistics.
Null hypothesis tested  Parametric tests  Nonparametric tests  Test level 

$H_0: AR = 0$  AR Test  Individual Event  
$H_0: AAR = 0$  CrossSectional Test, TimeSeries Standard Deviation Test, Patell Test, Adjusted Patell Test, Standardized CrossSectional Test, Adjusted Standardized CrossSectional Test, and Skewness Corrected Test  Generalized Sign Test, Generalized Rank T Test, and Generalized Rank Z Test  Sample of Events 
$H_0: CAR = 0$  Individual Event  
$H_0: CAAR = 0$ 
CrossSectional Test, TimeSeries Standard Deviation Test, Patell Test, Adjusted Patell Test, Standardized CrossSectional Test, Adjusted Standardized CrossSectional Test, and Skewness Corrected Test 
Generalized Sign Test, Generalized Rank T Test, and Generalized Rank Z Test 
Sample of Events

$H_0: BHAR = 0$  BHAR Test  Individual Event  
$H_0: ABHAR = 0$  ABHAR Test and Skewness Corrected Test  Sample of Events 
N.B.: Most test statistics are calculated by our free abnormal return calculators
Parametric test statistics ground on the classic ttest. Yet, scholars have further developed the test to correct for the ttest's prediction error. The most widely used of these 'scaled' tests are those developed by Patell (1976) and Boehmer, Musumeci and Poulsen (1991). Among the nonparametric tests, the ranktest of Corrado (1989), and the signbased of Cowan (1992) are very popular. EST provides these test statistics (soon) in its analysis results reports.
Why different test statistics are needed
The choice of test statistic should be informed by the research setting and the statistical issues the analyzed data holds. Specifically, eventdate clustering poses a problem leading to (1) crosssectional correlation of abnormal returns, and (2) distortions from eventinduced volatility changes. Crosssectional correlation arises when sample studies focus on (an) event(s) which happened for multiple firms at the same day(s). Eventinduced volatility changes, instead, is a phenomenon common to many event types (e.g., M&A transactions) that becomes problematic when events are clustered. As consequence, both issues introduce a downward bias in the standard deviation and thus overstate the tstatistic, leading to an overrejection of the null hypothesis.
Comparison of test statistics
There have been several attempts to address these statistical issues. Patell (1976, 1979), for example, tried to overcome the ttest's proneness to eventinduced volatility by standardizing the event window's ARs. He used the dispersion of the estimation interval's ARs to limit the impact of stocks with high return standard deviations. Yet, the test too often rejects the true null hypothesis, particularly when samples are characterized by nonnormal returns, low prices or little liquidity. Also, the test has been found to be still affected by eventinduced volatility changes (Campbell and Wasley, 1993; Cowan and Sergeant, 1996; Maynes and Rumsey, 1993, Kolari and Pynnonen, 2010). Boehmer, Musumeci and Poulsen (1991) resolved this latter issue and developed a test statistic robust against volatilitychanging events. Furthermore, the simulation study of Kolari and Pynnonen (2010) indicates an overrejection of the null hypothesis for both the Patell and the BMP test, if crosssectional correlation is ignored. Kolari and Pynnonen (2010) developed an adjusted version for both test statistics that accounts for crosssectional correlation.
The nonparametric rank test of Corrado and Zivney (1992) (RANK) applies restandardized event window returns and has proven robust against induced volatility and crosscorrelation. Sign tests are another category of tests. One advantage the tests’ authors stress over the common ttest is that they are apt to also identify small levels of abnormal returns. Moreover, scholars have recommend the used of nonparametric sign and rank tests for applications that require robustness against nonnormally distributed data. Past research (e.g. Fama, 1976) has argued that daily return distributions are more fattailed (exhibit very large skewness or kurtosis) than normal distributions, what suggests the use of nonparametric tests.
Several authors have further advanced the sign and ranked tests pioneered by Cowan (1992) and Corrado and Zivney (1992). Campbell and Wasley (1993), for example, improved the RANK test by introducing an incremental bias into the standard error for longer CARs, creating the CampbellWasley test statistic (CUMRANK). Another NPT is the generalized rank test (GRANK) test with a Student tdistribution with T2 degrees of freedom (T is the number of observations). It seems that GRANK is one of the most powerful instruments for both shorter and longer CARwindows.
The Cowan (1992) sign test (SIGN) is also used for testing CARs by comparing the share of positive ARs close to an event to the proportion from a normal period. SIGN's null hypothesis includes the possibility of asymmetric return distribution. Because this test considers only the sign of the difference between abnormal returns, associated volatility does not influence in any way its rejection rates. Thus, in the presence of induced volatility scholars recommend the use of BMP, GRANK, SIGN.
Most studies have shown that if the focus is only on single day ARs, the means of all tests stick close to zero. In the case of longer event windows, however, the mean values deviate from zero. Compared to their nonparametric counterparts, the Patell and the BMPtests produce means that deviate quite fast from zero, whereas the standard deviations of all tests gravitate towards zero. For longer event windows, academics recommend nonparametric over parametric tests.
Therefore, the main idea is that in case of longer eventwindows, the conclusions on the tests power should be very carefully drawn because of the many over or underrejections of the null hypothesis. Overall, comparing the different test statistics yields the following insights (see Table 2 for further details):
 Parametric tests based on scaled abnormal returns perform better than those based on nonstandardized returns
 Generally, nonparametric tests tend to be more powerful than parametric tests
 The generalized rank test (GRANK) is one of the most powerful test for both shorter CARwindows and longer periods
#  Name [synonym] 
Key Reference  ABBREVIATION in API RESULTS  Strengths  Weaknesses 



1  T test 



2  CrossSectional Test  CSect T  
3  TimeSeries Standard Deviation Test  CDA T  
4  Patell Test  Patell (1976)  Patell Z 


5  Adjusted Patell Test  Kolari and Pynnönen (2010)  Adjusted Patell Z 


6  Boehmer, Musumeci and Poulsen (1991)  StdCSect Z 



7  Adjusted Standardized CrossSection Test 
Kolari and Pynnönen (2010)  Adjusted StdCSect Z 


8  Skewness Corrected Test  Hall (1992)  Skewness Corrected T 


9  Jackknife Test  Giaccotto and Sfiridis (1996)  Jackknife T  


10  Corrado and Zivney (1992)  Rank Z 


11  Generalized Rank Test  Kolari and Pynnönen (2011)  Generalized Rank T 
Accounts for


12  Generalized Rank Test  Kolari and Pynnönen (2011)  Generalized Rank Z  see GRANKT  
13  Sign Test  Cowan (1992)  not available in API 


14  Cowan Generalized Sign Test  Cowan (1992)  Generalized Sign Z  
15  Wilcoxon signedrank Test  Wilcoxon (1945) 

Insights about strenghts and weaknesses were compiled from Kolari and Pynnonen (2011)
Formulas, acronyms, and the decision rule applicable to all test statistics
Let $L_1 = T_1  T_0 + 1$ the estimation window length with $T_0$ as the 'earliest' day of the estimation window, and $T_1$ the 'latest' day of the estimation window relative to the event day and $L_2 = T_2  T_1$ the event window length with $T_2$ as the 'latest day' of the event window relative to the event day. Define $N$ as the sample size (i.e. number of events / observations); $S_{AR_i}$ represent the standard deviation as produced by the regression analysis over the estimation window according to the following formula
Our API provides test statistics for single firms in each time point $t$. The Null is: $H_0: AR_{i, t} = 0,$
$$t_{AR_{i,t}}=\frac{AR_{i,t}}{S_{AR_i}}, $$
where $S_{AR_i}$ is the standard deviation of the abnormal returns in the estimation window,
$$S^2_{AR_i} = \frac{1}{M_i2} \sum\limits_{t=T_0}^{T_1}(AR_{i,t})^2.$$
Second, we provide t statistics of the cumulative abnormal returns for each firm. The t statistic und the Null $H_0: CAR_{i} = 0$ is defined as
$$t_{CAR}=\frac{CAR_i}{S_{CAR}},$$
where
$$S^2_{CAR} = L_2 S^2_{AR_i}.$$
[2] CrossSectional Test (Abbr.: CSect T)
A simple test for testing $H_0: AAR = 0$ is given by
$$t_{AAR_t}=\sqrt{N}\frac{AAR_t}{S_{AAR_t}},$$
where $S_{AAR_t}$ is the standard deviation across firms at time $t$:
$$S^2_{AAR_t} =\frac{1}{N1} \sum\limits_{i=1}^{N}(AR_{i, t}  AAR_t)^2.$$
Test statistic for testing $H_0: CAAR = 0$ is given by
$$t_{CAAR}=\sqrt{N}\frac{CAAR}{S_{CAAR}},$$
where $S_{CAAR}$ is the standard deviation of the cumulative abnormal returns across the sample
$$S^2_{CAAR} =\frac{1}{N1} \sum\limits_{i=1}^{N}(CAR_{i}  CAAR)^2.$$
Brown and Warner (1985) showed that the crosssectional test is prone to eventinduced volatility. However, the test has low power then.
[3] TimeSeries Standard Deviation or Crude Dependence Test (Abbr.: CDA T)
coming soon
[4] Patell or Standardized Residual Test (Abbr.: Patell Z)
[5] Kolari and Pynnönen adjusted Patell or Standardized Residual Test (Abbr.: Adjusted Patell Z)
Kolari and Pynnönen (2010) propose a modification to the Patelltest to account for crosscorrelation of the abnormal returns. Using the standardized abnormal returns ($SAR_{i,t}$) defined as in (EQ: $\ref{eq:sar}$), and defining $\bar r$as the average of the sample crosscorrelation of the estimation period abnormal returns, the test statistic for $H_0: AAR = 0$ of the adjusted Patelltest is
$$z_{Patell, t}=z_{Patell, t} \sqrt{\frac{1}{1 + (N  1) \overline r}},$$
where $z_{patell, t}$ is the Patell test statistic. It is easily seen that if the correlation $\overline r$ is zero, the adjusted test statistic reduces to the original Patell test statistic. Assuming the squareroot rule holds for the standard deviation of different return periods, this test can be used when considering Cumulated Abnormal Returns ($H_0: CAAR = 0$):
$$z_{Patell}=z_{Patell} \sqrt{\frac{1}{1 + (N  1) \overline r}}.$$
[6] Standardized CrossSectional or BMP Test (Abbr.: StdCSect Z)
Similarly, Boehmer, Musumeci and Poulsen (1991) proposed a standardized crosssectional method which is robust to the variance induced by the event. Test statistics on day $t$ ($H_0: AAR = 0$) in the event window is given by
$$z_{BMP, t}= \frac{ASAR_t}{\sqrt{N}S_{ASAR_t}},$$
with $ASAR_t$ defined as for Patelltest [2] and with standard deviation
$$S^2_{ASAR_t} = \frac{1}{N1}\sum\limits_{i=1}^{N}\left(SAR_{i, t}  \frac{1}{N} \sum\limits_{l=1}^N SAR_{l, t} \right)^2.$$
Furthermore, EST API provides the test statistic for testing $H_0: CAAR = 0$ given by
$$z_{BMP}=\sqrt{N}\frac{\overline{SCAR}}{S_{\overline{SCAR}}},$$
where $\overline{SCAR}$ is the averaged standardized cumulated abnormal returns across the $N$ firms, with standard deviation
$$S^2_{\overline{SCAR}} = \frac{1}{N1} \sum\limits_{i=1}^{N} \left(SCAR_i  \overline{SCAR}\right)^2,$$
$$\overline{SCAR} = \frac{1}{N}\sum\limits_{i=1}^{N}SCAR_i$$
and $SCAR_i = \frac{CAR_i}{S_{CAR_i}}$. $S_{CAR_i}$ is the forecast error corrected standard deviation from Mikkelson and Partch (1988). The Mikkelson and Partch correction adjusts for each firm the test statistic for serial correlation in the returns. The correction terms are
 Market Model:
$$S_{CAR_i} = S_{AR_i}^2\left(L_i + \frac{L^2_i}{M_i} + \frac{\left(\sum\limits_{t=T_1+1}^{T_2}(R_{m,t}\bar{R}_{m})\right)^2} {\sum\limits_{t=T_0}^{T_1}(R_{m,t}\bar{R}_{m})^2}\right)$$
 Comparison Period Mean Adjusted Model:
$$S_{CAR_i} = S_{AR_i}^2\left(L_i + \frac{L^2_i}{M_i}\right)$$
 Market Adjusted Model:
$$S_{CAR_i} = S_{AR_i}^2L_i,$$
where $L_i$ is the count of nonmissing return values in the event window and $M_i$ is the count of nonmissing return values in the estimation window for firm $i$. $\bar{R}_{m}$ is the mean of the market returns in the estimation window, see e.g. Patell Test.
[7] Kolari and Pynnönen Adjusted Standardized CrossSectional or BMP Test (Abbr.: Adjusted StdCSect Z)
Kolari and Pynnönen (2010) propose a modification to the BMPtest to account for crosscorrelation of the abnormal returns. Using the standardized abnormal returns ($SAR_{i,t}$) defined as in the previous section, and defining $\bar r$as the average of the sample crosscorrelation of the estimation period abnormal returns, the test statistic for $H_0: AAR = 0$ of the adjusted BMPtest is
$$z_{BMP, t}=z_{BMP, t} \sqrt{\frac{1 \overline r}{1 + (N  1) \overline r}},$$
where $z_{bmp, t}$ is the BMP test statistic. It is easily seen that if the correlation $\overline r$ is zero, the adjusted test statistic reduces to the original BMP test statistic. Assuming the squareroot rule holds for the standard deviation of different return periods, this test can be used when considering Cumulated Abnormal Returns ($H_0: CAAR = 0$):
$$z_{BMP}=z_{BMP} \sqrt{\frac{1 \overline r}{1 + (N  1) \overline r}}.$$
[8] Skewness Corrected Test (Abbr.: Skewness Corrected T)
The skewnessadjusted ttest, introduced by Hall 1992, corrects the crosssectional ttest for skewed abnormal return distribution. This test is applyable for averaged abnormal return ($H_0: AAR = 0$), the cumulative averaged abnormal return ($H_0: CAAR = 0$), and the averaged buyandhold abnormal return ($H_0: ABHAR = 0$). In the following, we limit us on the situation of cumulative averaged abnormal returns. First, reviside the crosssectional standard deviation (unbiased by sample size):
$$S^2_{CAAR} = \frac{1}{N1} \sum\limits_{i=1}^{N}(CAR_i  CAAR)^2.$$
The skewness estimation (unbiased by sample size) is given by:
$$\gamma = \frac{N}{(N2)(N1)} \sum\limits_{i=1}^{N}(CAR_i  CAAR)^3S^{3}_{CAAR} .$$
Furthermore, let
$$S = \frac{CAAR}{S_{CAAR}},$$
then the skewness adjusted test statistic for CAAR is given by
$$t_{skew} = \sqrt{N}\left(S + \frac{1}{3}\gamma S^2 + \frac{1}{27}\gamma^2S^3 + \frac{1}{6N}\gamma\right),$$
which is asymptotically standard normal distributed. For a further discussion on skewness transformation we refer to Hall (1992) and for further discussion on unbiased estimation of the second and third moment we refer to Cramer (1961) or Rimoldini (2013).
[9] Jackknife Test (Abbr.: Jackknife T)
coming soon.
[10] Corrado Rank Test (Abbr.: Rank Z)
In a first step, the Corrado's (1989) rank test transforms abnormal returns into ranks. Ranking is done for all abnormal returns of both the event and the estimation period. If ranks are tied, the midrank is used. For adjusting on missing values Corrado and Zyvney (1992) suggested a standardization of the ranks by the number of nonmissing values $M_i$ plus 1
$$K_{i, t}=\frac{rank(AR_{i, t})}{1 + M_i + L_i} $$,
where $L_i$ refers to the number of nonmissing (i.e., matched) returns in event window. The rank statistic for testing on a single day ($H_0: AAR = 0$) is then given by
$$t_{rank, t} = \frac{\overline{K}_t  0.5}{S_{\overline{K}}},$$
where $\overline{K}_t = \frac{1}{N_t}\sum\limits_{i=1}^{N_t}K_{i, t}$, $N_t$ is the number of nonmissing returns across firms, and
$$S^2_{\overline{K}} = \frac{1}{L_1 + L_2} \sum\limits_{t=T_0}^{T_2} \frac{N_t}{N}\left(\overline{K}_t  0.5 \right)^2$$.
When analyzing a multiday event period, Campell and Wasley (1993) define the RANKtest considering the sum of the mean excess rank for the event window as follows ($H_0: CAAR = 0$):
$$t_{rank} =\sqrt{L_2} \left(\frac{\overline{K}_{T_1, T_2}  0.5}{S_{\overline{K}}}\right),$$
where $\overline{K}_{T_1, T_2} = \frac{1}{L_2} \sum\limits_{t=T_1 + 1}^{T_2}\overline{K}_t$ is the mean rank across firms and time in event window. By adjusting the last day in the event window $T_2$, one can get a series of test statistics as definded by Campell and Wasley (1993).
Note 1: The adjustment for event induced variance as done by Campell and Wasley (1993) is omitted here and may be implemented in a future version. In such a case, we recommend the GRANKT or GRANKZ test.
[11] Generalized Rank T Test (Abbr.: Generalized Rank T)
In following steps we assume for sake of simplicity that there are no missing values is estimation and event window for each firm. In order to account for possible eventinduced volatility, the GRANK test squeezes the whole event window into one observation, the socalled 'cumulative event day'. First, define the standardized cumulative abnormal returns of firm $i$ in the event window
$$SCAR_{i}=\frac{CAR_{i}}{S_{CAR_{i}}},$$
where $S_{CAR_{i}}$ is the standard deviation of the prediction errors in the cumulative abnormal returns of firm $i$, namely
\begin{equation}S^2_{CAR_{i}} = S^2_{AR_i} \left(L+\frac{L_2}{L_1}+\frac{\sum\limits_{t=T_1+1}^{T_2}(R_{m,t}\bar{R}_{m})^2} {\sum\limits_{t=T_0}^{T_1}(R_{m,t}\bar{R}_{m})^2}\right).\end{equation}
The standardized CAR value $SCAR_{i}$ has an expectation of zero and approximately unit variance. To account for eventinduced volatility $S_{CAR_{i}}$ is restandardized by the crosssectional standard deviation
$$SCAR^*_{i}=\frac{SCAR_{i}}{S_{SCAR}},$$
where
$$S^2_{SCAR}=\frac{1}{N1} \sum\limits_{i=1}^N \left(SCAR_{i}  \overline{SCAR} \right) \quad \text{ and } \quad \overline{SCAR} = \frac{1}{N} \sum\limits_{i=1}^N SCAR_{i}.$$
By construction $SCAR^*_{i}$ has again an expectation of zero with unit variance. Now, let's define the generalized standardized abnormal returns ($GSAR$):
$$GSAR_{i, t} = \left\{ \eqalign{ SCAR^*_i &\text{ for t in event window} \\ SAR_{i ,t} &\text{ for t in estimation window}} \right.$$
The CAR window is also considered as one time point, the other time points are considered GSAR is equal to the standardized abnormal returns. Define on this $L_1 + 1$ points the standardized ranks:
$$K_{i, t}=\frac{rank(GSAR_{i, t})}{L_1 + 2}0.5$$
Then the generalized rank tstatistic for testing $H_0: CAAR = 0$ is defined as:
$$t_{grank}=Z\left(\frac{L_1  1}{L_1  Z^2}\right)^{1/2}$$
with
$$Z=\frac{\overline{K_{0}}}{S_{\overline{K}}},$$
$t=0$ indicates the cumulative event day, and
$$S^2_{\overline{K}}=\frac{1}{L_1 + 1}\sum\limits_{t \in CW}\frac{N_t}{N}\overline{K}_t^2$$
with CW representing the combined window consisting of estimation window and the cumulative event day, and
$$\overline{K}_t=\frac{1}{N_t}\sum\limits_{i=1}^{N_t}K_{i, t}.$$
$t_{grank}$ is tdistributed with $L_1  1$ degrees of freedom.
Formulas testing on a single day ($H_0: AAR = 0$) are straightforward from the above ones.
[12] Generalized Rank Z Test (Generalized Rank Z)
Using some facts about statistics on ranks, we get the standard deviation of $\overline{K_{0}}$
$$S^2_{\overline{K_{0}}} =\frac{L_1}{12N(L_1 + 2)}.$$
By this calculation following test statistic can be defined
$$z_{grank} = \frac{ \overline{K_{0}} }{ S_{\overline{ K_{0} } } } = \sqrt{ \frac{12N(L_1+ 2)}{L_1}} \overline{K_{0}},$$
which converges under null hypothesis fast to the standard normal distribution as the firms $N$ increase.
[13] Sign Test (Abbr.: not available in our API)
This sign test has been proposed by Cowan (1991) and builds on the ratio of positive cumulative abnormal returns $\hat{p}$ present in the event window. Under the null hypothesis, this ratio should not significantly differ from 0.5.
$$t_{sign}= \sqrt{N}\left(\frac{\hat{p}0.5}{\sqrt{0.5(10.5)}}\right)$$
[14] Cowan Generalized Sign Test (Abbr.: Generalized Sign Z)
Under the Null Hypothesis of no abnormal returns, the number of stocks with positive abnormal cumulative returns ($CAR$) is expected to be in line with the fraction $\hat{p}$ of positive $CAR$ from the estimation period. When the number of positive $CAR$ is significantly higher than the number expected from the estimated fraction, it is suggested to reject the Null Hypothesis.
The fraction $\hat{p}$ is estimated as
$$\hat{p}=\frac{1}{N}\sum\limits_{i=1}^{N}\frac{1}{L_1}\sum\limits_{t=T_0}^{T_1}\varphi_{i, t},$$
where $\varphi_{i,t}$ is $1$ if the sign is positive and $0$ otherwise. The Generalized sign test statistic ($H_0: CAAR = 0$) is
$$z_{gsign}=\frac{(wN\hat{p})}{\sqrt{N\hat{p}(1\hat{p})}},$$
where $w$ is the number of stocks with positive cumulative abnormal returns during the event period. For the test statistic, a normal approximation of the binomial distribution with the parameters $\hat{p}$ and $N$, is used.
Note 1: This test is based on the paper of Cowan, A. R. (1992).
Note 2: EST provides GSIGN test statistics also for single days ($H_0: AAR = 0$) in the event time period.
Note 3: The GSIGN test is based on the traditional SIGN test where the null hypothesis assumes a binomial distribution with parameter $p=0.5$ for the sign of the $N$ cumulative abnormal returns.
Note 4: If $N$ is small, the normal approximation is inaccurate for calculating the pvalue, in such case we recommend to use the binomial distribution for calculating the pvalue.
[15] Wilcoxon Test (Abbr.: Wilcoxon Z)
coming soon.
References and further readings
Boehmer, E., Musumeci, J. and Poulsen, A. B. 1991. 'Eventstudy methodology under conditions of eventinduced variance'. Journal of Financial Economics, 30(2): 253272.
Campbell, C. J. and Wasley, C. E. 1993. 'Measuring security performance using daily NASDAQ returns'. Journal of Financial Economics, 33(1): 7392.
Campbell, J., Lo, A., MacKinlay, A.C. 1997. 'The econometrics of financial markets'. Princeton: Princeton University Press.
Corrado, C. J. and Zivney, T. L. 1992. 'The specification and power of the sign test in event study hypothesis test using daily stock returns'. Journal of Financial and Quantitative Analysis, 27(3): 465478.
Cowan, A. R. (1992). 'Nonparametric event study tests'. Review of Quantitative Finance and Accounting, 2: 343358.
Cowan, A. R. and Sergeant, A. M. A. 1996. 'Trading frequency and event study test specification'. Journal of Banking and Finance, 20(10): 17311757.
Cramer H., 1961, Mathematical Methods of Statistics, Princeton University Press
Fama, E. F. 1976. Foundations of Finance. New York: Basic Books.
Giaccotto C. and Sfiridis J. M. 'Hypothesis testing in event studies: The case of variance changes'. Journal of Econometrics and Business, 48(4): 349370.
Hall, P., 1992, 'On the Removal of Skewness by Transformation'. Journal of the Royal Statistical Society. Series B (Methodological) Vol. 54, No. 1, pp. 221228
Kolari, J. W. and Pynnonen, S. 2010. 'Event study testing with crosssectional correlation of abnormal returns'. Review of Financial Studies, 23(11): 39964025.
Kolari, J. W. and Pynnonen, S. 2011. 'Nonparametric rank tests for event studies'. Journal of Empirical Finance, 18(5): 953971.
Wayne H. Mikkelson and M. Megan Partch, 1988. 'Withdrawn Security Offerings'. The Journal of Financial and Quantitative Analysis Vol. 23, No. 2 (Jun., 1988), pp. 119133; Errata: Vol. 24, No. 4, p. 487
Maynes, E. and Rumsey, J. 1993. 'Conducting event studies with thinly traded stocks'. Journal of Banking and Finance, 17(1): 145157.
Patell, J. A. 1976. 'Corporate forecasts of earnings per share and stock price behavior: Empirical test'. Journal of Accounting Research, 14(2): 246276.
Rao, R. 1997. 'Statistic and truth. Putting chance to work'. World Scientific Publishing Co Ltd: Singapore.
Rimoldini, L. 'Weighted skewness and kurtosis unbiased by sample size'. Draft 28 April 2013
Schipper, K. and Smith, A. 1983. 'Effects of recontracting on shareholder wealth: The case of voluntary spinoffs.' Journal of Financial Economics, 12(4): 437467.
Wilcoxon, F. (1945). 'Individual comparison by ranking methods'. Biometrics Bulletin, 1(6): 8083.