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Comovement in cryptocurrency markets: evidences from wavelet analysis
Financial Innovation volume 5, Article number: 33 (2019)
Abstract
We study the time varying comovement patterns of the cryptocurrency prices with the help of waveletbased methods; employing daily bilateral exchange rate of four major cryptocurrencies namely Bitcoin, Ethereum, Lite and Dashcoin. First, we identify Bitcoin as potential market leader using Wavelet multiple correlation and Cross correlation. Further, Wavelet Local Multiple Correlation for the given cryptocurrency prices are estimated across different timescales. From the results, it is found that that the correlation follows an aperiodic cyclical nature, and the cryptocurrency prices are driven by Bitcoin price movements. Based on the results obtained, we suggest that constructing a portfolio based on cryptocurrencies may be risky at this point of time as the other cryptocurrency prices are mainly driven by Bitcoin prices, and any shocks in the latter is immediately transformed to the former.
Introduction
Cryptocurrencies are the latest addition to the financial instruments, and the ones garnering increased attention during the recent times (Urquhart 2018). The first asset of this class was Bitcoin, launched in 2009 immediately after the 2008 financial crisis. In the initial days, people seemed skeptic about this new product. However, in the last couple of years, there has been an exponential increase in the demand of Bitcoin, and the market has witnessed a huge growth in terms of both market capitalization and introduction of new cryptocurrency assets. The number of cryptocurrencies has increased from 500 in 2014 (White 2015) to 1560 currencies as on 8 April 2018. The increased market capitalization as well as introduction of new asset points resulted in market becoming more liquid and investors being active. However, irrespective of this upward momentum, there are serious concerns raised about various dimensions of cryptocurrency markets.
The high volatility exhibited by the cryptocurrency market is a pressing concern. Compared to traditional financial markets, cryptocurrency markets are shallow (Bohme et al. 2015); in such a market, any shocks or fluctuation in the market leader may easily transfer and trigger a market collapse. Further, the cryptocurrency market, unlike traditional financial markets, has possible unequal distribution of assets. The firstgeneration miners and investors had relative ease to mine and purchase cryptoassets (Smith and Kumar 2018). With this, there is possibility of engineering price movements. Gandal et al. (2018) shows evidence towards such a suspicious trading activity in Mt. Gox exchange in 2013.
The other dimension being the use of cryptocurrencies. Apart from gambling, online gaming, possible money laundering (Moser et.al. 2013) and crossborder transactions, speculation is one of the important motivations associated with cryptocurrencies (Smith and Kumar 2018). Glaser et al. (2014) argues that utility for crypto assets stems from their appeal as an asset class. Similar argument is put forward by Baur et al. (2018) based on their analysis of transaction value and frequency in Blockchain.
With cryptocurrencies being integrated with the traditional financial assets (see, Tony et al. 2018; Khaled et al. 2018 and Henriques and Sadorsky 2018), there is bound to be more investor attention and the possibility of market being more liquid. In such a scenario, exploring the potential for diversification in cryptocurrency markets is of paramount importance. However, the existing research on this phenomenon is sparse. Our paper addresses this issue.
Remainder of this article is structured as follows: Section 2 provides a brief review of literature, section 3 discusses data and methodology employed. Section 4 shows the estimation results and its explanation while section 5 provides the concluding remarks.
Literature review
The majority of research in cryptocurrency markets can be categorized into: a) price determination and value formation (Urquhart 2017; Van Alstyne 2014; Yermack 2013; Ali et al. 2014; Glaser et al. 2014; Kristoufek 2015; Baek and Elbeck 2015; Ciaian et al. 2016; Bouoiyour et al. 2016; Blau 2017; Zhu et al. 2017), b) volatility (Katsiampa 2017; Jiang et al. 2017; Dwyer 2015; Bouoiyour and Selmi 2016; Dyhrberg 2016), c) speculative bubbles (Cheah and Fry 2015; Cheung et al. 2015; Godsiff 2015; Fry and Cheah 2016; Urquhart 2016; Nadarajah and Chu 2017) and d) forecasting and prediction of cryptocurrencies using different models (HotzBehofsits et al. 2018; Catania et al. 2019).
There exist a number of studies that discuss the comovement of Bitcoin and other financial instruments. Evidences supporting cointegration of Bitcoin exchange rates with conventional exchange rates is found in Chu et al. 2015. Pieters and Vivanco (2017) study cointegration among various Bitcoin exchange prices and finds that Bitcoin doesn’t follow the law of one price. In a similar study, Dirican and Canoz (2017) find evidences that support long run comovements between Bitcoin and major stock indices. Salman and Razzaq (2018) study the cointegration between Bitcoin prices and its determining factors using Johansen’s cointegration method and find supportive evidence towards cointegration. In a recent study, Ciaian and Rajcaniova (2018) implemented ARDL (Auto Regressive distributed lag model) m ethodology and found that Bitcoin price movement and other cryptocurrency price movements are independent of each other.
From the literature it is evident that barring a few studies (Bohme et al. 2015; Narayanan et al. 2016; Smith and Kumar 2018) there is lack of a comprehensive research that addresses the dynamics of cryptocurrency market in its isolation. With cryptocurrency market evolving as independent market segment, a study of cryptocurrency market dynamics in its isolation will be of immense use to both researcher and investors. Our work aims to fill this gap and attempts to address this issue in a detailed manner. We study the comovement of four major cryptocurrencies during the last 3 years, during which the cryptocurrency market started becoming more liquid. Considering the fact that cryptocurrency markets might be populated by investors with different time horizons (DelfinVidal and RomeroMeléndez 2016); we forego the traditional time series methods and adapt a comprehensive waveletbased methodology. Wavelets are preferred due to their ability to extract information from time series at various without losing its timescale dimension. Rationale behind choosing wavelet based analysis is provided in the methodology section.
First, we identify the potential market leader using wavelet multiple correlation and wavelet multiple crosscorrelation. After this, we estimate evolution of local dynamics by estimating wavelet local multiple correlation for the four cryptocurrencies under study and see if the dynamics of multiple correlation structure can be explained by the price movement of the potential market leader.
Data and methodology
We use daily prices (in US Dollar) of four major cryptocurrencies namely Bitcoin, Ethereum, Lite and Dashcoin from 7 August, 2015 to 24 March, 2018 for our analytical purpose. We select these four majors cryptocurrencies as they represent a fair share of the market in terms of market capitalization. Further, we select six random crypto currencies namely Reddcoin, DigixDao, Luckycoin, Bitmark, Edgecoin and Unobatanium for comparison purposes. The data is collected from coinmarketcap.com, a cryptocurrency data aggregation website. There were no missing values.
Here, a waveletbased methodology is applied to study the timevarying nature of comovements in the cryptocurrency markets across different scales. We are only looking at the short to medium term dynamics, as the cryptocurrency market is still its nascent stage.
While the standard time series/frequency domain tests can provide information about the possible presence of comovement among a multivariate time series, these tests have some serious limitations. First, while they can identify the presence of long run comovement and shortterm adjustment, these tests fail to provide a statistic that could quantify the extent of comovement. Considering the fact that there are agents with different trading time horizons operating in financial markets (DelfinVidal and RomeroMeléndez 2016), it is possible that the nature of relationship between these markets vary across different timescales. The traditional time series measures can provide measures only at the given frequency. Wavelet methods are employed to extract information across various frequencies without losing the time dimension.
Wavelet Multiple Correlation (WMC henceforth) measure, proposed by Macho (2012) can overcome these two shortcomings. The Wavelet multiple correlation coefficient measure could provide the strength of comovement among a multivariate time series across different timescales, so that one could distinguish between the short run, medium run and long run relationship. Similarly, Macho proposes Wavelet Multiple Cross Correlation (WMCC henceforth) in the same article. WMCC provides a measure to identify a potential leader among the group, that could influence the other variables present in the group.
These measures are better compared to the traditional wavelet correlation and cross correlation measures in terms of parsimony. If we have 5 markets, then we would have to calculate nX(n1)/2 = 10 wavelet correlation plots and J (order of wavelet decomposition) times wavelet cross correlation plots, resulting in a cumbersome process. If we employ WMC and WMCC methods, we need to only plot J correlation plots and J crosscorrelation plots.
Further in a multivariate context, a pairwise correlation coefficient could be spurious due to possible relationship of one variable with other variables. WMC and WMCC estimates overall correlations within the multivariate framework across different time scales making interpretation of the results easier.
Wavelet Local Multiple Correlation (WMLC henceforth), proposed by FernándezMacho (2018) is an extension Macho (2012). While WMC and WMCC provided an overall measure of correlation across in a multivariate context, WLMC provides a local measure of the same so that one could study the evolution of wavelet multiple correlation values over time. First, we will briefly explain the WMC and WMCC estimation. In the next step, a detailed explanation of WLMC estimation will be given.
The wavelet Multiple correlation is explained as follows:
Let {X_{t}} be a multivariate stochastic process and let {W_{jt}} be the respective j^{th} level wavelet coefficients obtained by the application of maximal overlap discrete wavelet transform (MODWT). The wavelet multiple correlation (WMC) ∅x (λ _{j}) can be defined as one single set of multi scale correlations calculated from X_{t} as follows.
At each wavelet scale λ _{j} we calculate the square root of the regression coefficient of determination in that linear combination of variables w_{ijt} , i=1,2,…n, for which the coefficient of determination is a maximum. The coefficient of determination corresponding to the regression of a variable Z_{i} on a set of regressors {Z_{k},k ≠ i}, could be obtained as R_{i}^{2}=11/ρ^{ii}, where ρ^{ii} is the i^{th} diagonal element of the inverse of the complete correlation matrix P.
The WMC, ∅x (λ _{j)}) is obtained as
Where P is the N×N correlation matrix of W_{jt}, and the max diag(.) operator selects the largest element in the diagonal of the argument. Since the R^{2}_{i} coefficient can be shown equal to the square of the correlation between the observed values of z_{i} and the fitted values z_{i} obtained from such a regression (see Appendix), ∅x (λj) can also be expressed as:
Where the wavelet variances and covariance are defined as follows:
Where w_{ij} on a set of regressors {w_{kj},k ≠ i},leads to the maximization of the coefficient of determination, \( {\hat{w}}_{ij} \) represents the fitted values. The number of wavelet coefficients affected by boundary associated with a wavelet filter of length L and scale λ_{j} is calculated as
L_{j} = (2^{j}1)(L1)+1. Then the number of wavelet coefficients unaffected by the boundary conditions is obtained as \( {\overset{\sim }{T}}_j=T{L}_j1 \).
Allowing a lag τ between observed and fitted values of the variables selected as the criterion variable at each scale λ_{j}, we may define the wavelet multiple cross correlation (WMCC henceforth) as
For n=2 the WMC and WMCC are the same as the standard wavelet correlation and cross correlation.
However, as the WMC and WMCC could not explain the evolution of potential local nonlinear dynamics, Macho (2018) proposed WMLC (Wavelet Multiple Local Correlation) as an extension as the WMC method. The method is described as follows.
Let X be the multivariate time series under consideration and let W_{jt} = (w_{1jt}, w_{2jt} … … . w_{nt}) be the λ_{j} wavelet coefficients obtained by applying an MODWT on all x ∈ X. Following Macho (2012),at each wavelet scale λ _{j} we calculate the square root of the regression coefficient of determination in that linear combination of variables w_{ijt} , i=1,2,…n, for which the coefficient of determination is a maximum. The coefficient of determination corresponding to the regression of a variable Z_{i} on a set of regressors {Z_{k},k ≠ i}, could be obtained as R_{i}^{2}=11/ρ^{ii}, where ρ^{ii} is the i^{th} diagonal element of the inverse of the complete correlation matrix P. Φ_{XS} (λ _{j)}) is obtained as
Where P_{j, s} is the n X n weighted correlation matrix of W_{jt}, with weights θ(t − s) and the max diag(.) operator selects the largest element in the diagonal of the argument. Since the R^{2}_{i} coefficient can be shown equal to the square of the correlation between the observed values of Z_{i} and the fitted values Z_{i} obtained from such a regression, Φ_{X, s} (λj) can also be expressed as:
Where the w_{ij} is chosen to maximize ϕ_{X, s}(λ_{j}). Applying MODWT to the given multivariate timeseries X for an order J, we can obtain J number of T length MODWT coefficients,
\( \overset{\sim }{W_J}=\Big\{\overset{\sim }{W_{J0}},\overset{\sim }{W_{J1}} \),………\( \overset{\sim }{W} \)_{J,T1}}. From Eq. (1), the WLMC of scale λ_{j} is a nonlinear function of all the n(n1)/2 weighted correlations of W_{jt}. Alternatively, it could be explained in terms of all the weighted variances and covariances of W_{jt}, as shown in Eq. (2). Hence, a consistent estimator of WLMC based on MODWT could be derived as:
Where the weighted wavelet variances and covariances can be estimated as:
\( \tilde{w}_{i}j \) is selected such that regressing \( \tilde{w}_{i}j \) on a set of regressors {\( \tilde{w}_{k}j \),k ≠ i} leads to the maximization of the coefficient of determination, \( {\hat{\overset{\sim }{w}}}_{ij} \)represents the fitted values. The number of wavelet coefficients affected by boundary associated with a wavelet filter of length L and scale λ_{j} is calculated as L_{j} = (2^{j}1)(L1) + 1. Then the number of wavelet coefficients unaffected by the boundary conditions is obtained as \( {\overset{\sim }{T}}_j=T{L}_j1 \).
Macho (2012) constructs the confidence intervals using the Fisher’s transform. Fisher’s transformation is defined as arctanh(r); where arctanh(.) is the inverse hyperbolic tangent function, and r is the sample correlation value. and it is used to construct confidence interval for a population correlation is based on the fact that if (X, Y) follows a bivariate normal distribution with ρ = Corr(X, Y), then the transformed sample correlation coefficient calculated from T independent pairs of observations can be shown to be approximately normally distributed with mean arctanh(r) and variance (T − 3)^{−1}. (Fisher 1922). Here, confidence intervals are estimated applying this method to the sample wavelet local multiple correlation coefficient \( {\overset{\sim }{\phi}}_{X,s}\left({\lambda}_j\right) \) as follows:
Let {X_{t}} be a realization of multivariate Gaussian stochastic process and let
\( {\overset{\sim }{W}}_j=\left({\overset{\sim }{W}}_{j0}\dots {\overset{\sim }{W}}_{j,T1}\right)=\left\{\left({\overset{\sim }{w}}_{1j0}\dots \tilde{w}_{n}j0\right),\left({\overset{\sim }{w}}_{1j,T/{2}^j1}\right)\right\} \), j = 1, 2…….J, be vectors of wavelet coefficients obtained by applying a MODWT of order J to each of the univariate time series (x_{i1}, x_{i2}, …. . x_{iT}) for i = 1, 2…n. If \( {\overset{\sim }{\phi}}_{X,j}\left({\lambda}_j\right) \) is the sample wavelet multiple local correlation obtained from Eq (1), then \( \tilde{z}_{j}\sim FN\Big({z}_j,{\left(T/{2}^j3\right)}^{1} \)), Where z_{j} = arctan h(∅_{Xs}(λ_{j})), \( \tilde{z}_{j}=\arctan h\left({\overset{\sim }{\phi}}_{X,s}\left({\lambda}_j\right)\right) \) and FN stands for Folded Normal Distribution.
The 100(1 − α)%confidence interval for the true value of ϕ_{X, τ}(λ_{j}) is then obtained as \( {CI}_{1\alpha}\left({\phi}_{X,\tau}\left({\lambda}_j\right)\right)=\tanh \Big(\tilde{z}_{j}{c}_2/\sqrt{T/{2}^j3} \) ;\( \tilde{z}_{j}+{c}_1/\sqrt{T/{2}^j3} \)) where c_{1} and c_{2} are folded normal critical values.
We select a Gaussian window with length M= N/2^4, as suggested by FernándezMacho (2018).
Results and discussion
Before we start the wavelet analysis, we want to see if there exist any long run cointegration among the variables of interest. Towards this, we apply Johansen (1992) cointegration test on the four cryptocurrency prices. Result of the same is provided in Table 1. From the results, it can be seen that there is a cointegrating relationship between the cryptocurrencies under analysis and we proceed towards the wavelet analysis (Fig. 1).
First, we want to see if we can establish Bitcoin as a potential market leader. Towards this, we employ Wavelet Multiple Correlation (WMC) and Wavelet Multiple Cross Correlation (WMCC) and obtain the results for the overall period of analysis. The estimations are carried out from scales 2–4 days (intraweek scale) to 16–32 days (monthly scale). The results are shown in Figs. 2 and 3.
Here, we see that the market is moderately correlated during the period of analysis. And at each scale, the cryptocurrency that maximizes the correlation value is against the linear combination of the other cryptoassets are shown in the plot. At all the 4 scales, bitcoin is the one that found to be maximizing WMC, indicating Bitcoin as a potential leader/follower. Next, we try to confirm this fact by estimating Wavelet Multiple Cross Correlation at a lead/lag of 36 days. The results are shown in Fig. 2.
The crosscorrelation Plot explains the potential leadlag relationship between the cryptocurrency prices. Here, the cryptocurrency that maximizes the multiple correlation value against the linear combination of the other currencies is shown at toplet corner in each scale plot for all the scales. We can see that Bitcoin maximizes WMC against the other currencies across all scales. However, as the highest value of WMCC is obtained at lag zero, we cannot conclude solely based on the test results whether Bitcoin leads ahead or lags behind other cryptocurrencies. However, with Bitcoin accounting for the largest market capitalization in the cryptocurrency market, it would be safe to assume that Bitcoin is the market leader in cryptocurrency markets. As WMCC identifies Bitcoin as potential leader/follower, our assumption is not solely based on simple observation, but backed up by statistical evidences.
The next step in the analysis will be to obtain a detailed timeline on major price fluctuations in the market leader. Details about major events in Bitcoin prices are presented in Table 2. If there is a price increase in Bitcoin after the event, we term the event positive and similarly, any event that results in an immediate price decrease is termed as negative event.
From the aforementioned events, we can obtain an outlook about the prevailing moods in the Bitcoin markets during the period of analysis. Our aim is to detect any potential patterns in the cryptocurrency comovements and see if we could relate it with Bitcoin price movements. If the WLMC values decrease with a negative news and increase with a positive news; we can confirm that the market is affected by cryptocurrency price movements. Towards this, we present the WLMC results of estimation; shown in Figs 4, 5, 6 and 7.
Observing the WLMC values across different timescales, we can see a number of common factors. First, the correlation among the markets are high across all the timescales. Second, the nature of the correlation varies in a cyclical fashion, albeit an aperiodic one. Further, the markets record the overall highest correlation values in the initial periods (January2016). It takes almost 2 years for the market to reach the same peak, and the inbetween periods are marred by frequent turbulences. As we proceed from smaller scales (high frequency) to larger scales (low frequency), the cyclical nature of the WLMC is found to be smoothening, implying that the fluctuations prevailing in the cryptocurrency comovement predominantly are of short term nature.
In the following paragraphs, we offer possible explanations behind the cyclical nature of the comovement. As we identified Bitcoin as the potential market leader with the help of wavelet correlation and crosscorrelation analysis, we try to explain the WLMC based on certain events related to Bitcoin prices.
The WLMC values shows a decreasing trend between August to September 2015. During this period, two major events took place in the Bitcoin market. First, arrest of now defunct cryptoexchange Mt. Gox. CEO and then, the announcement of Bitcoin Fork. These two events resulted in a value drop of Bitcoin, only to be picked up during the following months, possibly due to the positive events such as Bitcoin being included into the commodity list in the US, exclusion of Value Added Tax by EU and the Launch of new Cryptoexchange Gemini, offering some sort of Insurance coverage to the investor. The recovery is depicted in the increased value of WLMC across all scales.
In January 2016, major Bitcoin developer Mike Hearn quit Bitcoin, creating a panic in the cryptocurrency markets. This was reflected in the bitcoin prices, a drop of around $35. Later, the WLMC starts to pick up around April 2016, which coincides with the launch of new Bitcoin related software OpenBazzar, supposed to be a better transaction platform.
In July 2016, the blockrewards of Bitcoins were reduced, as per the bitcoin issue system. This in turn resulted in an initial price rise in Bitcoin. However, the correlation between Bitcoin and other markets drops down immediately. One reason for the said behavior could be that, with the increased difficulty in obtaining Bitcoins, a part of miners and investors would have migrated to other options, resulting in the reduced wavelet correlation values. The correlation reaches its lowest point in August 2016, when the Hong Kong based cryptocurrency exchange BitFinex was hacked.
WLMC reaches its peak again in November 2016, something that interestingly coincides with Donald Trump’s election as the president of the USA. Around this period, stockmarkets, especially that of US showed evidences of capital flight towards assets that are traditionally considered as Safe. A part of such investments has gone into cryptocurrencies (Bouoiyour and Selmi 2017), resulting in increased demand and thereby prices. However, this exuberance seems to be shortlived, as we see a sharp drop in the correlation values. It coincides with US Securities Exchange Commission’s (SEC) rejection of a project on cryptocurrency based ExchangeTradedFund (ETF), proposed by Winkelwos brothers. However, the correlation picks up after Japan announced the validity of Bitcoin as a legal tender.
However, around August 2017, we see further drop in WLMC values. The reason for the same can be attributed to uncertainty about the potential fork in Bitcoin. In August 2017, the fork resulted in a new cryptocurrency namely Bitcoin Cash. Around the same period, Chinese government had initiated a crackdown in cryptocurrency markets. As China is one of the major Hub of cryptocurrency activities, this crackdown fueled the existing uncertainty, leading to the drop in WLMC values. The market seems to have picked up after the Chinese crackdowns, as evidenced by the increased WLMC values, coinciding with the positive events such as Bitcoin being listed by Cboe Global Markets Inc. and CME Group Inc., and the proposed cancellation of the fork in Bitcoin prices.
As discussed in the introduction part, cryptocurrency markets are populated by several new asset in the last couple of years. It would be interesting to see how these assets are moving with respect to the major cryptocurrencies in the market. It is our aim to see if they move opposite to the market direction. Towards this, we estimate WLMC values for a set of 10 cryptocurrency returns. Here we include six additional cryptocurrencies namely Reddcoin, DigixDao, Luckycoin, Bitmark, Edgecoin and Unobatanium. These currencies were picked randomly with varying market capitalization. The result of WLMC estimation is given in Fig. 8.
From the results, it is seen that apart from a fluctuation around the year 2016, the correlation values are around 1. This presents an interesting picture. From the WMC and WMCC results, Bitcoin is identified as the market leader. With a correlation value of 1 persisting for the larger period, it can be said that the market, especially when we consider smaller currencies, follow the fluctuations in the Bitcoin prices always.
From these, it is possible to draw some conclusions about the investor behavior. When there is a price drop in Bitcoins, the correlation structure between Bitcoin and other currencies collapse, indicating that agents distance themselves from cryptoassets. But when Bitcoin is on the upswing, it is reflected in Other cryptoassets as well, cementing Bitcoin’s position as the market leader. The fluctuations are frequent during the period of analysis, which is to be expected as cryptocurrency markets are still in its early stage. It is difficult to comment whether the cryptocurrency markets are going to be less volatile in the near future, due to its innate decentralized structure. With cryptocurrencies being introduced at par with traditional financial assets, there is a possibility that a better trading and regulatory frame work will come into place. However, it is too early to comment on that and we do not make any assumptions as such.
Concluding remarks
We studied the time varying comovement patterns of the cryptocurrency markets with the help of waveletbased methods. Daily bilateral exchange rate of four major cryptocurrencies namely Bitcoin, Ethereum, Lite and Dashcoin from 7 August, 2015 to 24 March,2018 were used for the analysis. First, we identified Bitcoin as potential market leader using Wavelet multiple correlation and cross correlation. Next, we estimated Wavelet Local Multiple Correlation for the given cryptocurrency prices. From the results, we could observe that the correlation follows an aperiodic cyclical nature, and the cryptocurrency prices are influenced by Bitcoin price movements. The demand for crypto assets increases when Bitcoin prices are on the rise, resulting in a price rise in other cryptocurrencies. Conversely, any price drop in Bitcoin is immediately reflected in other cryptocurrency prices.
From an investor perspective, this coupling of other cryptocurrencies with Bitcoin creates a dilemma. While cryptocurrency assets can possibility act as instruments of hedge in a traditional portfolio, along with other assets such as equities and bonds, we do not suggest constructing a portfolio entirely composed of Cryptoassets. From the evidences obtained from the analysis, constructing a portfolio based on cryptocurrencies may be risky at this point of time as the altcoin prices are mainly driven by Bitcoin prices, and any shocks in the latter is immediately transmitted to the former. Even by looking at the skewed market capitalization in the cryptocurrency market; with Bitcoin occupying almost 50% of the total market capitalization, it would not be prudent to construct a portfolio that entirely consists of cryptocurrency assets.
Availability of data and materials
The datasets used for estimation is obtained from Coin Market Cap [https://coinmarketcap.com/]
Abbreviations
 ARDL:

Autoregressive Distributed Lag
 MODWT:

Maximal overlap discrete wavelet transform
 OTC:

OvertheCounter
 WLMC:

Wavelet Local multiple correlation
 WMC:

Wavelet multiple correlation
 WMCC:

Wavelet multiple crosscorrelation
References
Ali R, Barrdear J, Clews R, Southgate J (2014) The economics of digital currencies. Bank England Q Bull 54(3):276–286
Baek C, Elbeck M (2015) Bitcoins as an investment or speculative vehicle? A first look. Appl Econ Lett 22(1):30–34
Baur DG, Hong K, Lee AD (2018) Bitcoin: medium of exchange or speculative assets? J Int Financ Mark Inst Money 54:177–189
Blau BM (2017) Price dynamics and speculative trading in bitcoin. Res Int Bus Financ 41:493–499
Bohme R, Chirstin N, Edelman B (2015) Bitcoin: economics, technology, and governance. J Econ Perspect 29(2):213–238
Bouoiyour J, Selmi R (2016) Bitcoin: a beginning of a new phase. Econ Bull 36(3):1430–1440
Bouoiyour, J., & Selmi, R. (2017). Are trump and bitcoin good partners?. arXiv preprint arXiv:1703.00308
Bouoiyour J, Selmi R, Tiwari AK, Olayeni OR (2016) What drives bitcoin price. Econ Bull 36(2):843–850
Catania L, Stefano G, Francesco R (2019) Forecasting cryptocurrencies under model and parameter instability. Int J Forecast 35(2):485–501
Cheah ET, Fry J (2015) Speculative bubbles in bitcoin markets? An empirical investigation into the fundamental value of bitcoin. Econ Lett 130:32–36
Cheung A, Roca E, Su JJ (2015) Cryptocurrency bubbles: an application of the Phillips–Shi–Yu (2013) methodology on Mt. Gox bitcoin prices. Appl Econ 47(23):2348–2358
Chu J, Nadarajah S, Chan S (2015) Statistical analysis of the exchange rate of bitcoin. PLoS One 10(7):e0133678. https://doi.org/10.1371/journal.pone.0133678
Ciaian P, Rajcaniova M (2018) Virtual relationships: shortand longrun evidence from bitcoin and altcoin markets. J Int Financ Mark Inst Money 52:173–195
Ciaian P, Rajcaniova M, Kancs DA (2016) The economics of bitcoin price formation. Appl Econ 48(19):1799–1815
DelfinVidal R, RomeroMeléndez G (2016) The fractal nature of bitcoin: evidence from wavelet power spectra. In: Trends in mathematical economics. Springer, Cham, pp 73–98
Dirican C, Canoz I (2017) The cointegration relationship between bitcoin prices and major world stock indices: an analysis with ARDL model approach. J Econ Financ Acc 4(4):377–392
Dwyer GP (2015) The economics of bitcoin and similar private digital currencies. J Financ Stab 17:81–91
Dyhrberg AH (2016) Bitcoin, gold and the dollar–a GARCH volatility analysis. Financ Res Lett 16:85–92
FernándezMacho, J. (2018). Timelocalized wavelet multiple regression and correlation. Physica A: Statistical Mechanics and its Applications, 492:1226–1238.
Fisher RA (1922) On the mathematical foundations of theoretical statistics. Philos Trans R Soc Lond A 222:309–368
Fry J, Cheah ET (2016) Negative bubbles and shocks in cryptocurrency markets. Int Rev Financ Anal 47:343–352
Gandal N, Hamrick JT, Moore T, Oberman T (2018) Price manipulation in the bitcoin ecosystem. J Monet Econ 95:86–96
Glaser F, Zimmermann K, Haferkorn M, Weber MC, Siering M (2014) Bitcoin – asset or currency? Revealing users’ hidden intentions. In: Proceedings of the European Conference on Information Systems (ECIS). Association for Information Systems, Tel Aviv
Godsiff P (2015) Bitcoin: bubble or Blockchain. In: Jezic G, Howlett R, Jain L (eds) Agent and multiagent systems: technologies and applications. Smart innovation, systems and technologies, vol 38. Springer, Cham
Henriques I, Sadorsky P (2018) Can bitcoin replace gold in an investment portfolio? J Risk Financ Manage 11:48
HotzBehofsits C, Florian H, Thomas OZ (2018) Predicting cryptocurrencies using sparse nonGaussian state space models. J Forecast 37(6):627–640
Jiang Y, Nie H, Ruan W (2017) Timevarying longterm memory in bitcoin market. Financ Res Lett 25:280–284
Johansen S (1992) Determination of cointegration rank in the presence of a linear trend. Oxf Bull Econ Stat 54:383–397
Katsiampa P (2017) Volatility estimation for bitcoin: a comparison of GARCH models. Econ Lett 158:3–6
Khaled G, Samir S, Ilyes A, Zied F (2018) Portfolio diversification with virtual currency: evidence from bitcoin. Int Rev Financ Anal. https://doi.org/10.1016/j.irfa.2018.03.004
Kristoufek L (2015) What are the main drivers of the bitcoin price? Evidence from wavelet coherence analysis. PLoS One. https://doi.org/10.1371/journal.pone.0123923
Macho JF (2012) Wavelet multiple correlation and crosscorrelation: a multiscale analysis of eurozone stock markets. Physica A 391:1097–1104
Macho JF (2018) Timelocalized wavelet multiple regression and correlation. Physica A 492:1226–1238
Moser M, Bohme R, Breuker D (2013) An inquiry into money laundering tools in the Bitcoin ecosystem. In: eCrime Researchers Summit (eCRS), 2013. IEEE, San Francisco pp 1–14
Nadarajah S, Chu J (2017) On the inefficiency of bitcoin. Econ Lett 150:6–9
Narayanan A, Bonneau J, Felten E, Miller A, Goldfeder S (2016) Bitcoin and cryptocurrency technologies: a comprehensive introduction. Princeton University Press, Princeton
Pieters G, Vivanco S (2017) Financial regulations and price inconsistencies across bitcoin markets. Inf Econ Policy 39:1–14
Salman A, Razzaq MGA (2018) Bitcoin and the world of digital currencies. In: Financial Management from an Emerging Market Perspective. InTech. https://doi.org/10.5772/intechopen.71294
Smith C, Kumar A (2018) Cryptocurrencies – an introduction to notsofunny moneys. J Econ Surv. https://doi.org/10.1111/joes.12289
Tony K, Hien PT, Thomas W (2018) Bitcoin is not the new gold – a comparison of volatility, correlation, and portfolio performance. Int Rev Financ Anal 59:105–116
Urquhart A (2016) The inefficiency of bitcoin. Econ Lett 148:80–82
Urquhart A (2017) Price clustering in bitcoin. Econ Lett 159:145–148
Urquhart A (2018) What causes the attention of bitcoin? Econ Lett 166:40–44
Van Alstyne M (2014) Why bitcoin has value. Commun ACM 57(5):30–32
White LH (2015) The market for cryptocurrencies. Cato J 35(2):383–402
Yermack D (2013) Is bitcoin a real currency? An economic appraisal. In: NBER Working Paper No 19747
Zhu Y, Dickinson D, Li J (2017) Analysis on the influence factors of Bitcoin’s price based on VEC model. Financ Innov 3:3. https://doi.org/10.1186/s4085401700540
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Appendix
Appendix
Relationship between r ^{2} and R ^{2}
Let us consider the following where y is the actual series, \( \hat{y} \) is the fitted series and e is the residual. R^{2} is defined as the coefficient of determination. \( {R}^2=\frac{\mathit{\operatorname{var}}\left(\hat{y}\right)}{\mathit{\operatorname{var}}(y)} \)
\( {r}_{y,\hat{y}}=\frac{Cov\left(y,\hat{y}\right)\ }{\surd \mathit{\operatorname{var}}(y)\mathit{\operatorname{var}}\left(\hat{y}\right)} \) where r is the Person correlation coefficient
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S Kumar, A., Ajaz, T. Comovement in cryptocurrency markets: evidences from wavelet analysis. Financ Innov 5, 33 (2019). https://doi.org/10.1186/s4085401901433
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DOI: https://doi.org/10.1186/s4085401901433