Cointegration and causality relationship of Indian stock market with selected world markets

1. Introduction

Global stock market connections have been studied extensively. However, there has not been a great deal of academic interest in examining the interdependence of Emerging stock markets. An economic spillier occurs when one event sets off another event in a similar way, having an impact on economies both within and outside a country. In 2008, when Lehman Brothers collapsed in the U. S., the domino effect hit the economies worldwide including India (Aloui et al., 2016). Financial markets today are closely interconnected and driven by trust. Therefore, the developed and emerging markets have been a riveting field for the research of behavioural finance due to interlinked stock markets across the world. Lai et al. (2016) examined during the crisis, investors make errors of judgment as long as a group of investors takes irrational decisions that lead to worsening the situation of the stock market.

COVID-19 also delivered a shock to the economies of most countries, because of the nature of the interconnected global market (Karkowska and Urjasz, 2021). The Indian stock market has been broadly resilient amidst the COVID-19 crisis so far, despite the devastating waves of the pandemic (Kapoor et al., 2020). However, the Indian economy has witnessed some impact from the global crash. Seth and Panda (2020) discussed that it is hard to pinpoint exactly the impact of any financial crisis on the Indian stock market, but it seems that the COVID-19 crisis has spilled over into some sectors. Numerous studies (Shaikh, 2021; Dhall and Singh, 2020; Singh and Neog, 2020) have argued on insignificant causal linkage of the stock markets across the world. Some authors such as Zhang and Hamori (2021), have also focused on the possible factors and impacts of the global crisis on the Indian market. Hoque et al. (2007) investigated the co-movement of the Bangladesh market with those of Japan, the United States, and India and discovered evidence of a shared stochastic trend. In his paper, it was clear that shocks in the US affected Bangladesh, which is an emerging country. Rajwani and Mukherjee (2013) examined the interconnectedness of the Indian stock market with other Asian stock markets and discovered that the Indian stock market is not interconnected with any of the Asian stock markets, demonstrating the insensitivity of the Indian stock markets to other markets. Several studies have identified both short-term and long-term cointegration and interconnected financial markets between different economies of the world (Stawiarski, 2021;Yarovaya and Lau, 2016). The global financial markets are closely interconnected and driven by the emotions of the investors (Huang et al., 2020). Hence, this manuscript focuses a causal linkage and cointegration between the global crisis and the Indian stock. In previous studies such as Mukherjee and Bose (2008) and Rajwani and Mukherjee (2013), Asian economies have been integrated with the economies of developed nations such as Japan and the United States.

In this study, we contribute to the literature on strategic financial decision-making for investors. Using vector auto regressive correlation (VAR) and vector error correction method (VECM) to assess the cointegration (Yarovaya and Lau, 2016; Kanjilal and Ghosh, 2017; Aggarwal and Raja, 2019), have documented the multivariate cointegration-vector auto-regression method and their results indicate that the Indian stock market return depends on the world market returns. This study’s main objective is to comprehend how the volatility index of the Indian stock market might be impacted by the volatility index of some other countries. The Indian Capital Market has been examined by various academics at various times for its efficiency and co-integration. Utilizing the Engle-Granger test of co-integration, this study examines the co-integration characteristics of the Indian Capital Market with global markets in the post-liberalization period. Since there are so many markets and so much trade, no amount of research can adequately explain the behaviour. Indian capital markets and other capital markets around the world are investigated in this study.

Accordingly, the article is organized as follows: Section 2 summarizes existing studies that have used cointegration tests on the stock market. Section 3 describes the technique used in the article. Section 4 goes over the data, including possible structural breaks. Section 5 displays the cointegration test findings. Section 6 explores the ramifications of the findings, and Section 6 concludes.

2. Literature review

A series of recent studies (Choudhary and Singhal, 2020; Kumar et al., 2021; Sahoo and Kumar, 2021; Kartal et al., 2022) has investigated the cointegration relationship of the stock market amid crisis. Some studies (He et al., 2020; Stawiarski, 2021) have explained the causal linkage of Indian stock market with Asian countries while in some other studies, a number of authors have recognized the comprehensive analysis by applying Generalized Autoregressive Conditional Heteroskedasticity Model (Narasimha and Mushinada, 2020) and found very high volatility index of Indian stock market in comparison to developed countries during the COVID-19 crisis. While recent advances in the field of behavioural finance have highlighted the volatility clustering in the Indian stock market through the use of time series data analysis and predictive analytics. According to Khaing et al. (2020), stock trend extraction results matched genuine price movement. These patterns were retrieved with the news effect curve during the global recession 2008-2009. These criteria include timestamp conversion, identifying the necessary verb, stock reference, and identifying advanced trends. Chen (2021) created the new neural network model to develop the prediction model’s concepts. Belciug et al. (2021) evaluated the efficacy of a statistical learning framework using an algorithm based on a competitive/collaborative method for generating a reliable real-time forecast of the next stock market transaction price for a share during upswing of the market. Biswas et al. (2021) reviewed numerous models and approaches used in stock market prediction and focused on their advantages and disadvantages during the crisis. Numerous studies have argued that there is insignificant (Goudarzi and Ramanarayanan, 2011) and significant (Aggarwal and Raja, 2019) causal linkage among the stock markets across the world. Some scholars, such as Jain and Biswal (2016), have also focused on the possible drivers of rupee value decline and the influence of the 2014-2015 global crisis on the Indian stock market. It is well established that the global financial markets are closely interconnected Muthukumaran et al. (2011) and are driven by the emotions of investors. Several studies have identified interconnected financial markets between different economies of the world during1996-1997 crisis Yang et al. (2003) by applying VAR (vector auto-regression). There is a strong co-movement between developing and mature markets, and studies have found a larger correlation among well-established equities markets (Bekaert and Harvey, 2003; Carrieri et al., 2007). On the other hand, some early literature implies the existence of diversification benefits by investing in both developed and developing economies due to relatively lower correlations between stock markets of such economies (Bekaert and Harvey, 1995; Foerster and Karolyi, 1999). Different experts have come to different conclusions about how stock markets around the world are related to each other. In addition, the relationship between global stock markets is temporally variable; national and global events can alter the nature and intensity of a relationship over time. Depending on its intensity, the phenomenon could last a short time or last for a very long time. Globalization has changed the relationship between various financial markets worldwide (Can Inci et al., 2011). Ahmad et al. (2005) have investigated only short term linkage whilst no significant linkage was found among the Indian Stock Market (NSE), Japanese (Nikkei) and US equity market (Dow Jones) amid crisis by using Granger-causality test. Menon et al. (2009) found that the Indian stock market did not have any causal linkage with the US and Japanese stock markets during the 2008 crisis period by hypothesizing Engle Granger test of co-integration. Siddiqui (2009) concluded that the Indian stock market is integrated with the global market. Some others studies such as Rajwani and Mukherjee (2013) have argued the Indian stock market is not interconnected with the Asian markets. Narayan et al. (2014) have investigated highly positive time varying bilateral correlations by analysing GARCH-dynamic conditional correlations.

Yarovaya and Lau (2016) have concluded the asymmetric causality linkage; their results indicating the coupling and decoupling of the Chinese stock market with the UK stock market. Nayak et al. (2016) applied machine learning algorithms and identified that the historical prices of the stocks are combined with sentiments of the investors. Nandy and Chattopadhyay (2019) have explained the unidirectional action from the world’s stock exchange indices over Indian stock market indices by carrying multivariate vector auto regression (VAR) analysis and Granger causality test. Aggarwal and Raja (2019) explored a long-run cointegration equation of the Asian and the Indian market by applying the Johansen cointegration model. Some other studies have also confirmed the bidirectional causality of Bombay Stock exchange indices with the US stock market indices by carrying Granger causality test (Choudhary and Singhal, 2020). Seth and Panda (2020) have revealed the strong dynamic linkage between the global economies and Indian economy by analysing the Autoregressive (AR1), Generalized Auto Regressive Conditional Heteroskedasticity (GARCH 1,1) Model and Asymmetric Dynamic Conditional Correlation (ADCC) model to determine the coupling and decoupling. Apart from analysing only the degree of cointegration and contagion among the world market, several studies have hypothesized the global contagion on the volatility of Indian stock’s prices. Li et al. (2011) have confirmed that the GARCH model cannot completely account for all nonlinearity in simulated market amid global crisis. Goudarzi and Ramanarayanan (2011) have revealed the bilateral causality between the Bombay Stock Exchange and foreign institutional investors. Garg and Gulati (2013) examined the rationality of the Indian investors in the face of economic crisis and validated the use of rational pricing models. Ding et al. (2014) have indicated returns depend on the direction of the movement of buying and selling pattern and stock distinctiveness of individual holdings and on arbitrage constraint. Guyon (2014) suggested the models of path-dependent volatility provide excellent alternatives to the duopoly of local volatility and stochastic volatility that has dominated option pricing for the past twenty years.

The fractal structure has been studied by Mahalingam and Selvam (2014) with long term returns on the market. An adaptive multiplicative error model (MEM) with time-varying parameters was proposed by Härdle et al. (2015). A multiplicative error model (MEM) parameters are adaptively estimated through sequential testing. Bir et al. (2015) have investigated the highest volatility for open ended stocks in the Indian stock market. Kumari and Mahakud (2016) have explored the unidirectional causality between sentiment and stock market volatility. This study indicated that the market reacts more strongly to the impact or shock of negative or bearish mood than to positive or bullish sentiment. Bouri et al. (2017) have examined significant hypothesis about the existence of cointegration linkage and nonlinear volatilities of oil and gold in Indian stock market during the crisis. Abuzayed et al. (2018) demonstrated that the skewed Student-t FIGARCH (Fractionally integrated generalized autoregressive conditional Heteroscedasticity) model generates the most precise VAR forecast for a single day. Other studies have demonstrated the ripple effects of United States of America uncertainty on other developed markets, such as L. Fang et al. (2018). Boako and Alagidede (2018) have confirmed the correlation amongst African stock markets, regional and global markets by carrying a comprehensive analysis. Chuliá et al. (2018) have demonstrated that some crises have had a weak negative correlation with market synchrony. Wang et al. (2019) have confirmed that significant shocks have a substantial link with stock prices and assert that volatility is more susceptible to the asymmetric effect than extreme volatility. According to Xing and Yang (2019), firms that attract more individual investors provide higher returns with lower future stock price crash risk. It is widely accepted that a greater degree of correlation among stocks provides an early warning of the probability of crashes. It has been conclusively shown that herding is strongly evident during the fluctuations of market (Shantha, 2019).

Some studies such as Fang et al. (2020); Wong et al. (2005); Daly (2003) also identified that the long-term volatility of the stock market depends upon many macroeconomic variables. While Lyócsa and Molnár (2020) discovered that the autoregressive coefficient was negative during COVID-19 (November 2019 to May 2020), they also discovered that uncertainty in the stock market and fear of viruses significantly influenced the breath of the autoregressive coefficient during the COVID-19 crisis. Narasimha and Mushinada (2020) point out that investors are concerned about cognitive biases and therefore adapt to changing market dynamics. (Vo, 2020) studied the significant positive link between foreign investors and crash risk due to the asymmetry of information in the emerging market. Among BRICS (Brazil, Russia, India, China, and South Africa) a diverse responses to the stock market volatility reported including negative and positive shocks (Salisu and Gupta, 2020). Cui and Zhang (2020) have suggested that negative information creates fear among the investor which leads to a larger stock price crash risk. According to Nikkinen and Peltomäki (2020), investors’ crash worries are examined by using published newspaper articles and web search volumes. They examine how information supply and demand relate to investor anxiety and their effects on stock market returns, implying that media contribute to the efficiency of information transmission. He et al. (2020) have examined the futures markets ability to price discover by margin trading on the stock market. Kumar and Misra (2020) have found widespread evidence of long-term similarity among the NIFTY 50 index and the global market. Naik et al. (2020) used GARCH (Generalized Auto-Regressive Conditional Heteroskedasticity) to calculate stock return error distribution. When time series data are heteroskedastic and volatile, the GARCH model is best. GARCH effectively predicted stock market crises (1995-2019) using State Bank of India and Infosys datasets. Elyasiani et al. (2021) analysed market greed by including the skewness index, which measures investor enthusiasm as opposed to investor fear. Previous studies have mainly exclusively explored the integration of Asian economies with other developed nations such as the United States and Japan during the period from 3^rd January 2011 to 29^th December 2017 in the midst of a global financial crisis. According to the literature, during the COVID-19 crisis, domino effects had both short-term and long-term negative consequences on economies all around the world (Salisu and Gupta, 2020).

However, there is a contradiction in the argument made by Aggarwal and Raja (2019); Rajwani and Mukherjee (2013) and Menon et al. (2009). Long-term cointegration of stock markets was not discovered, but correlation analysis revealed that stock market integration was growing with time.

Even though the majority of the COVID-19 economic crisis has passed, further research is still needed on the developed and rising Asian markets. In addition, it would be interesting to know whether the effect of the crisis on the Indian stock market persists over time and, if so, for how long. Do the recent shocks to global markets alter the standard deviation of forecasting errors in the Indian stock market? Contributing to existing theory and strategic financial decision-making for investors, this paper offers valuable insights. In particular, the authors explore how the global volatility index’s shock influences the Indian volatility index, how long the impact lasts, and the degree and sign of the effect.

3. Methods

In our study, we examined data from several major indices, including the NSE in India, the NIKKEI (Japan’s Nikkei 225 Stock Average) in Japan, NASDAQ (National Association of Securities Dealers Automated Quotations), DJI (Dow Jones Industrial Average) and S&P (Standard and Poor index) in the United States, the FTSE (Financial Times Stock Exchange) in the UK, the DAX (Deutscher Aktien Index) in Germany, the FTXIN (FTSE–Xinhua China A50 Index) in China, Cotation Assistée en Continu (CAC) benchmark of France stock market and the Hang Seng in Hong Kong. The descriptive statistics for all indexes’ returns are shown in Table 3. We compiled and collected the data from different websites (including Yahoo, Investing.com and NSE India) over the long-term, encompassing a significant portion of the recession from January 1, 2008, to December 2, 2021. The time period covered by the research has been selected to provide an in-depth look at the worldwide correlations that have an effect on the Indian stock market over the long term. Although the trading hours of each stock exchange varies, the time frame is the exact same for all indexes. Therefore, in order to examine the group statistics, we have taken the common sample. We calculated the daily return by applying the [Return=log (Closing price of indices/Closing price of indices (-1))] equation over the closing price. We analysed the data using the EViews 12 (University Version) software package. The Johansen cointegration test (Menon et al., 2009)¹ is used to demonstrate a long-term link between variables. To determine short-term and long-term associations between variables, the vector error correction model was utilised followed by Ezeibekwe (2021).

4. Descriptive statistical analysis

Individual observations show large shifts during crisis times are further followed by large shifts in the return of the NSE indices and the global indices representing the wild and calm periods of volatility clustering. Figure 1 shows the clustering of the volatility for the daily return of indices, firstly noted by Mandelbrot and Taylor (1967) ‘large changes tend to be followed by large changes, of either sign, and small changes tend to be followed by small changes.’ Figure 2 represent the leptokurtic statistical distributions with kurtosis greater than three results to a greater extent of volatility because of positive or negative shocks in the stock market. While the Jerque-Bera of NSE daily return (32031.42) measures the high volatility. The shape of the curve and the value of kurtosis along with the low probability value reveal the possibility for the rejection of the null hypothesis. The skewness measures the asymmetry of a time series over a given period (normal skewness; 0, positive skewness; long right tail, negative skewness; long left tail).

Figure 1. Volatility clustering plot of daily returns to NSE, NIKKEI, NASDAQ, S&P, DJI, FTSE, FTXIN, HANG SENG, DAX AND CAC INDICES (Source: author’s calculations).

Figure 2. Time series plot of returns to NSE (Source: author’s calculations).

Table 1 indicates that the left-hand tail of the German Blue chip stock market (DAX) is smaller than the right-hand tail. In other indices, a negative skewness (the left-hand tail is larger than the right-hand tail) indicates a scenario of small wins and few large losses for investors. Table 1 provides descriptive statistics on daily returns, highlighting Jarque-Bera standard deviation using the same sample for all indices. The NSE returns over the entire period sample shows a negatively skewed distribution of the sample (Jaque-Bera 33817.66, standard deviation 0.013768, Kurtosis 20.31397). In Japan, the statistical moments of the NIKKEI were Jarque-Bera 5525.19, standard deviation 0.0151, and Kurtosis 10.171). Jarque-Bera values for US Market (NASDAQ; 10447.74, standard deviation 0.014376, and Kurtosis 17.26778), (S&P; 23085.57, standard deviation 0.013164), and (DJI; 33669.34, standard deviation 0.012713, and Kurtosis 20.25097). These all show a similar leptokurtic distribution with negative skewness.

It is evident from the descriptive statistics that the significant value probabilities and the Jerque-Bera calculation indicate that the residual distribution of daily returns, like other indices (FTSE) Jarque-Bera 13203.88, standard deviation 0.012250 with Kurtosis value 13.81124), Germany (DAX) Jarque-Bera 9850.239, standard deviation 0.014335 with Kurtosis value 12.34726), Hong Kong (HANG SENG) Jarque-Bera 11642.69, standard deviation 0.0126 and Kurtosis 19.89 and France (CAC) Jarque-Bera 8553.046. The values of skewness’ and kurtosis observed the volatility clustering and specify the distribution of all indices (variables) is leptokurtic. Only Germany (DAX) is positively skewed, which specify that the huge gain covers the small losses of investors. The Indian stock market exhibits a positive correlation with the world market, as seen in Table 2; however, the correlation of all variables is not strong enough to explain the cointegration.

Table 2 examines the correlation trends between the Indian market and a few selected global markets, indicating that there is a relationship between the Indian stock market and other markets; nevertheless, Figure 3 illustrates that this connection is sometimes parallel to the global economy.

Figure 3. Movement of indices.

It is said that the “flap of a butterfly’s wings in Brazil could set off a tornado in Texas” (Lorenz, 2000) that is not true in the Indian context. The Indian stock market is still linked to the world market because the NSE has a positive correlation with all global indexes, despite the fact that this correlation has been reducing significantly.

5. Results

Johansen’s cointegration test results

Table 5 shows the statistical values of Johansen’s cointegration test. In addition, it provides information about the maximum Eigen-value. Statistics for all variables dependent (NSE) and independent (World’s indices) demonstrate a perfect correlation of cointegration. Since the calculated value of statistics and maximum Eigen-value are greater than the critical value (at 5% level) of (MacKinnon et al., 1999), the null hypothesis of no cointegration is rejected in favour of the alternative hypothesis of cointegration. Therefore, the Indian stock market and the global stock market have ten cointegration equations.

Table 5. Johansen’s cointegration test.

Lags interval (in first differences): 1 to 3
Unrestricted cointegration rank test (Trace)
Hypothesized No. of CE(s)	Eigen-value	Trace statistic	0.05 Critical value	Prob.**
None *	0.334300	3261.797	239.2354	0.0000
At most 1 *	0.285750	2753.151	197.3709	0.0000
At most 2 *	0.268835	2332.498	159.5297	0.0000
At most 3 *	0.231890	1941.102	125.6154	0.0000
At most 4 *	0.222216	1611.324	95.75366	0.0000
At most 5 *	0.212214	1297.192	69.81889	0.0000
At most 6 *	0.206747	999.0299	47.85613	0.0000
At most 7 *	0.190017	709.5135	29.79707	0.0000
At most 8 *	0.170580	446.0860	15.49471	0.0000
At most 9 *	0.156201	212.3006	3.841465	0.0000
Trace test indicates 10 cointegrating eqn (s) at the 0.05 level.

Hypothesized No. of CE(s)	Eigen value	Max-Eigen Statistic	0.05 Critical value	Prob.**
None *	0.334300	508.6457	64.50472	0.0000
At most 1 *	0.285750	420.6532	58.43354	0.0000
At most 2 *	0.268835	391.3954	52.36261	0.0000
At most 3 *	0.231890	329.7780	46.23142	0.0000
At most 4 *	0.222216	314.1328	40.07757	0.0000
At most 5 *	0.212214	298.1618	33.87687	0.0000
At most 6 *	0.206747	289.5164	27.58434	0.0000
At most 7 *	0.190017	263.4275	21.13162	0.0000
At most 8 *	0.170580	233.7855	14.26460	0.0000
At most 9 *	0.156201	212.3006	3.841465	0.0000

* Denotes rejection of the hypothesis at the 0.05 level.

** MacKinnon et al. (1999) p-values.

We employ VECM to evaluate the short-run characteristics of the cointegrated variables in order to ascertain whether they remain stationary over time (Table 6). If cointegration has been found between series, we are aware that there is a long-term equilibrium link between them.

Table 6. Vector error correction estimates.

Cointegrating Eq:	CointEq1	CointEq2	CointEq3
NSE (-1)	1.000000	0.000000	0.000000
NIKKEI (-1)	0.000000	1.000000	0.000000
NASDAQ (-1)	0.000000	0.000000	1.000000
SP (-1)	-5.908983	0.686667	-7.595660
	(0.99997) [-5.90918]	(3.23212) [ 0.21245]	(0.39953) [-19.0114]
DJI (-1)	0.189825	-1.192373	0.215697
	(0.11843) [ 1.60291]	(0.38278) [-3.11505]	(0.04732) [ 4.55862]
DAX (-1)	0.632029	-2.710561	-0.179478
	(0.16343) [ 3.86730]	(0.52824) [-5.13131]	(0.06530) [-2.74863]
CAC (-1)	-0.460907	10.90881	2.086912
	(0.38206) [-1.20637]	(1.23490) [ 8.83374]	(0.15265) [ 13.6712]
FTSE (-1)	-1.492381	-5.607010	-0.224850
	(0.35493) [-4.20473]	(1.14721) [-4.88751]	(0.14181) [-1.58557]
XIN (-1)	-0.053049	-0.524904	0.053855
	(0.09164) [-0.57891]	(0.29619) [-1.77219]	(0.03661) [ 1.47092]
HNGSNG (-1)	0.023054	0.574167	-0.058868
	(0.05353) [ 0.43068]	(0.17302) [ 3.31852]	(0.02139) [-2.75245]
C	6557.587	12741.45	2171.077

The effectiveness of market connectivity is measured by residual diagnostics for heteroscedasticity, which aid in identifying heteroscedasticity (Table 7). One can determine whether the model can be trusted based on this. Probability scores over 0.05 indicate that the model should work for the Indian stock market.

Table 7. VEC residual heteroskedasticity tests (levels and squares) joint test.

Chi-sq	df	Prob.
8093.609	1430	0.2731

The Jarque-Bera test in statistics determines if sample data have skewness and kurtosis that are consistent with a normal distribution. The result of Table 8 shows that the regression residual is normally distributed since the p value is greater than 0.05.

Table 8. VEC residual normality tests: null hypothesis: residuals are multivariate normal.

Component	Skewness	Chi-sq	df	Prob.*
1	-0.030822	0.234808	1	0.6280
2	0.341632	28.84747	1	0.2776
3	0.627158	97.21750	1	0.1832
4	-0.117999	3.441499	1	0.8308
5	0.381231	35.92239	1	0.6795
6	-0.287373	20.41181	1	0.5404
7	1.312546	425.8131	1	0.2081
8	-0.070094	1.214358	1	0.2705
9	-0.003174	0.002490	1	0.9602
10	-0.355615	31.25722	1	0.0000
Joint		644.3626	10	0.2271

Component	Kurtosis	Chi-sq	df	Prob.
1	20.83695	19659.44	1	0.849
2	10.34838	3336.671	1	0.186
3	12.81838	5956.751	1	0.273
4	5.912879	524.2937	1	0.251
5	6.440253	731.3253	1	0.275
6	10.60865	3577.214	1	0.220
7	89.73248	464829.3	1	0.307
8	4.173781	85.13416	1	0.401
9	4.787424	197.4173	1	0.285
10	10.62113	3588.961	1	0.849
Joint		502486.5	10	0.643

Component	Jarque-Bera	df	Prob.
1	19659.68	2	0.279
2	3365.519	2	0.252
3	6053.969	2	0.276
4	527.7352	2	0.318
5	767.2477	2	0.355
6	3597.626	2	0.403
7	465255.1	2	0.279
8	86.34852	2	0.252
9	197.4198	2	0.357
10	3620.218	2	0.348
Joint	503130.8	20	0.294

* Approximate p-values do not account for coefficient.

The null hypothesis is accepted for the sample based on the serial correlation test results, which show that the p-value is greater than 0.05 at the 5% significance level. The serial correlation verifies the accuracy and validity of the results of the cointegration test (Table 9).

Table 9. Serial correlation test.

Null hypothesis: No serial correlation at lag h
Lag	LRE* stat	df	Prob.	Rao F-stat	df	Prob.
1	1143.845	100	0.0000	12.03171	(100, 1039...	0.3803
2	1678.684	100	0.0000	18.12598	(100, 1039...	0.3741

Null hypothesis: No serial correlation at lags 1 to h
Lag	LRE* stat	df	Prob.	Rao F-stat	df	Prob.
1	1143.845	100	0.0000	12.03171	(100, 1039...	0.2775
2	2011.990	200	0.0000	10.79347	(200, 1296...	0.1831

* Edgeworth expansion corrected likelihood ratio statistic.

In Figure 4, we show impulse response functions associated with the non-factorized one standard deviation of innovations for the Indian stock market and the stock markets of some of India’s top trading partners and developed nations. It depicts the negative impulse responses of the Chinese and Japanese stock markets. Interestingly, both markets are responding similarly to a shock to the Indian stock market in their respective stock markets. Geographic proximity may be the reason for this. The established stock markets of the United States and other economies have a distinct trend. It demonstrates that these markets are in fact developed and have a robust positive impulse reaction to the Indian stock market.

Figure 4. Impulse response functions (Source: authors calculations).

6. Conclusion

The empirical findings suggest that the selected stock markets have a long-term dynamic. According to our research, the volatility of the US stock market considerably affected the Indian stock market. We performed a vector error correction model test to assess the stationary conditions of the series. This test demonstrated that the sequence is stationary. However, the variables become constant after considering the original difference. Cointegration tests show that the Indian stock market is integrated over time owing to the presence of a cointegration vector. A model of error correction demonstrates conclusively that variables are causal in the long-term. The stock market in India is impacted by those in the United States, Great Britain, Japan, and Germany. In addition, we applied the pairwise Granger causality test, which reveals the lead-lag connection across the markets, to test for short-term causative and informational linkages among diverse pairs of markets. According to our findings, the Indian stock market is neither fully connected nor completely decoupled from the global market. Nonetheless, the amount of integration implies that portfolio diversification can still result in substantial risk reduction and return maximisation in both the short-term and long-term by diversifying their portfolio during a crisis. In recent years, the returns on major US stock indices have dominated the returns for Indian stocks. Similar results show that the bank-dominated financial sectors of the ASEAN five and China are increasingly integrated (Caporale et al., 2021).

The study is prone to various limitations because it relies on secondary sources of data, which have inherent limitations, such as the total number of trading days during the study period for each country were different. So, the sample was adjusted with the help of EViews software. A quick glance at the study highlights clear-cut investment and portfolio diversification opportunities for international investors. This may help regulators formulate better policies concerning price discovery mechanisms. Moreover, it is possible to extend the present study to include global contagion issues between the sample countries. This could be done using high frequency data.

Data availability

Figshare: Cointegration and Causality Relationship, https://doi.org/10.6084/m9.figshare.20263803.v2 (Ali et al., 2022).

This project contains the following underlying data:

Data are available under the terms of the Creative Commons Attribution 4.0 International license (CC-BY 4.0).